{
 "claims": [
  {
   "claim": "For the noninteracted OLS-adjusted estimator of the average treatment effect in a completely randomized experiment, the paper gives a closed-form estimator of the bias that is exactly unbiased in finite samples (including the higher-order terms), so that the corrected estimator is exactly unbiased for the ATE.",
   "claim_id": "P005-H1",
   "related_corrections": [
    "P005-E002",
    "P005-E009",
    "P005-E010",
    "P005-N005"
   ],
   "tied_to": "Theorem 3.2, equations (7)-(8); Theorem 3.1; proof B.2"
  },
  {
   "claim": "The same holds for the interacted (Lin) estimator: a closed-form, exactly unbiased estimator of its bias, giving an exactly unbiased corrected estimator.",
   "claim_id": "P005-H2",
   "related_corrections": [
    "P005-E003",
    "P005-E004",
    "P005-E010",
    "P005-E012",
    "P005-E013",
    "P005-E015",
    "P005-N007"
   ],
   "tied_to": "Theorem 4.2; Theorem 4.1; proof B.4"
  },
  {
   "claim": "The bias of the noninteracted estimator splits into three parts; the leading part is $-1/(n-1)$ times the finite-population covariance between leverage and the individual treatment effect, it vanishes under additive effects, and the third part vanishes in balanced designs.",
   "claim_id": "P005-H3",
   "related_corrections": [
    "P005-E005",
    "P005-E007",
    "P005-N005"
   ],
   "tied_to": "Theorem 3.1, equations (5)-(6); Remark 1; Lemma A.2; proof B.1"
  },
  {
   "claim": "The bias of the interacted estimator has an analogous three-part characterization, with closed forms for the first and third parts.",
   "claim_id": "P005-H4",
   "related_corrections": [
    "P005-E001",
    "P005-E003",
    "P005-E004",
    "P005-N004"
   ],
   "tied_to": "Theorem 4.1; proof B.3 (details omitted in the paper)"
  },
  {
   "claim": "Under Freedman's assumptions, the bias-corrected estimators have the same limiting distributions as the uncorrected ones, so that in large samples the additional variation caused by the correction is negligible.",
   "claim_id": "P005-H5",
   "related_corrections": [
    "P005-E001",
    "P005-E002",
    "P005-N002",
    "P005-N005",
    "P005-N007"
   ],
   "tied_to": "Theorems 3.1, 3.2, 4.1 and 4.2 (stochastic expansions); Lemma A.1; Remarks 3 and 4"
  },
  {
   "claim": "Taken together with Lin (2013) (treatment-by-covariate interactions and robust standard errors), these results show that Freedman's theoretical objections to regression adjustment can be resolved with minor modifications to practice.",
   "claim_id": "P005-H6",
   "related_corrections": [
    "P005-E001",
    "P005-E015"
   ],
   "tied_to": "Theorems 3.2 and 4.2 together with the results of Lin (2013) cited in the introduction"
  },
  {
   "claim": "Earlier closed-form bias corrections (Cochran, Lin, Tan, Lei and Ding, Chiang et al.) are not exactly unbiased; to the authors' knowledge this paper is the first to give exactly unbiased corrections for both the interacted and the noninteracted estimator.",
   "claim_id": "P005-H7",
   "related_corrections": [],
   "tied_to": "Footnote 1 (p. 1504); Remark 5 (p. 1509)"
  }
 ],
 "date_published": "2026-10-25",
 "findings": [
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Listing of lines 606 to 614 of an R function in monospaced type with line numbers. A red box marks the name unbiased.reg.interact_new_formula in line 612, which assigns to debiased_estimator the value of that function at (y,d,z). Line 608 fits lm of y on d times z, and line 614 replaces the coefficient on d by debiased_estimator.",
     "caption": "Replication files, 30_functions2.R, lines 606–614, typeset from the source file with line numbers added. The marked name is the function called at line 612; the replication files define no function of this name.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E015.png"
    },
    {
     "alt": "Listing of lines 345 to 350 in monospaced type with line numbers. A red box marks the name unbiased.reg.interact_appl_new_formula at the start of line 345, where it is assigned a function of y, d and z.",
     "caption": "Replication files, 30_functions2.R, lines 345–350, typeset from the source file with line numbers added. The marked name is the function that the file defines.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E015-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "The function interacted_unbiased_regression calls a function under the name unbiased.reg.interact_new_formula, which the replication files do not define; the name they define is unbiased.reg.interact_appl_new_formula.",
   "id": "P005-E015",
   "location": "Replication files (public repository Debias, commit c9cfb0c1d006), folder 1_main_functions_for_simulations, file 30_functions2.R, function interacted_unbiased_regression (lines 593–658), line 612. No passage of the article",
   "pdf_page": null,
   "printed_page": null,
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [],
   "text": {
    "as_printed": "Line 612 of \\texttt{30\\_functions2.R}:\n\n\\texttt{debiased\\_estimator= \\hl{unbiased.reg.interact\\_new\\_formula}(y,d,z) \\#debiased estimator}",
    "corrected": "Line 612 of \\texttt{30\\_functions2.R}:\n\n\\texttt{debiased\\_estimator= unbiased.reg.interact\\hl{\\_appl}\\_new\\_formula(y,d,z) \\#debiased estimator}",
    "evidence": "This finding rests on a run of the unmodified file and on a search of the replication files. In a new R session I called the function on eight units with two covariates, for which the interacted regression has full rank. The call stops with the message \\texttt{could not find function} followed by the name \\texttt{unbiased.reg.interact\\_new\\_formula}. The name occurs once in the text of the replication files, at line 612, and none of the 43 files of saved R objects contains a function of that name.",
    "problem": "Line 612 calls a function that the replication files do not define. The function that computes the bias-corrected estimator of Theorem 4.2 is defined at line 345 of the same file under the name \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula}, and line 467 calls it by that name. When the file is loaded on its own, \\texttt{interacted\\_unbiased\\_regression} stops at line 612 and returns no estimate, standard error or interval.",
    "what_survives": "The article is not affected. It reports no simulation or application, and its estimators, theorems and proofs do not involve this function. I found no direct call to \\texttt{interacted\\_unbiased\\_regression} in the replication scripts, and the simulation code calls \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula} directly. The change below corrects the name only. With more than one covariate the function then stops at the error described in \\fid{P005-E016}."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E015",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Listing of lines 593 to 606 in monospaced type with line numbers: the header of the function interacted_unbiased_regression, comments that describe its arguments, and three assignments. A red box marks line 603, 'd=as.matrix(d)'. Lines 602 and 604 apply as.matrix to y and to z.",
     "caption": "Replication files, 30_functions2.R, lines 593–606, typeset from the source file with line numbers added. The marked statement at line 603 converts the assignment to a matrix; the comment at line 597 describes d as an assignment vector.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E016.png"
    },
    {
     "alt": "Listing of lines 358 to 370 in monospaced type with line numbers. Line 358 assigns to z.tr the columns of z minus their means. A red box marks the product 'd*z.tr' inside the formula of the regression at line 370, lm of y on d plus z.tr plus I(d*z.tr). The lines between are comments and two constants, CA and CB.",
     "caption": "Replication files, 30_functions2.R, lines 358–370, typeset from the source file with line numbers added. The marked product at line 370 multiplies the assignment by the centered covariate matrix z.tr defined at line 358.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E016-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "The function interacted_unbiased_regression converts the assignment d to an $n\\times1$ matrix, and with more than one covariate the product d*z.tr at line 370 then fails; d should remain a numeric vector.",
   "id": "P005-E016",
   "location": "Replication files (public repository Debias, commit c9cfb0c1d006), folder 1_main_functions_for_simulations, file 30_functions2.R: function interacted_unbiased_regression, lines 602–604 and 612; function unbiased.reg.interact_appl_new_formula, lines 358 and 370. No passage of the article",
   "pdf_page": null,
   "printed_page": null,
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [],
   "text": {
    "as_printed": "Lines 602--604 of \\texttt{30\\_functions2.R}, in \\texttt{interacted\\_unbiased\\_regression}:\n\n\\texttt{y=as.matrix(y)}\n\n\\texttt{d=\\hl{as.matrix}(d)}\n\n\\texttt{z=as.matrix(z)}\n\nLines 358 and 370, in \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula}:\n\n\\texttt{z.tr <- apply(z,2,function(y) y - mean(y))}\n\n\\texttt{ols<-coef(ols.model<-lm(y$\\sim$d+z.tr+I(d*z.tr)))[2]}",
    "corrected": "Line 603 of \\texttt{30\\_functions2.R}:\n\n\\texttt{d=\\hl{as.numeric}(d)}\n\nLines 602 and 604 are unchanged. Line 612 also needs the name given in \\fid{P005-E015}.",
    "evidence": "This finding rests on a run of the unmodified file on twelve units with two covariates and alternating assignment, for which both arm regressions have full rank. With the missing name defined in the session as in \\fid{P005-E015} and the file unchanged, the call of \\texttt{interacted\\_unbiased\\_regression} stops with \\texttt{non-conformable arrays}. The function \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula} stops with the same message when called with \\texttt{as.matrix(d)}, and returns $2.39214301337333$ when called with the vector \\texttt{d}.",
    "problem": "After line 603, \\texttt{d} is an $n\\times1$ matrix. Line 612 passes it to the function that computes the bias-corrected estimate, under the name corrected in \\fid{P005-E015}. That function centers the $k$ covariates in the $n\\times k$ matrix \\texttt{z.tr} and fits a regression whose formula contains the elementwise product \\texttt{d*z.tr}. For $k>1$, R does not multiply an $n\\times1$ matrix by an $n\\times k$ matrix elementwise, and the call stops with the error \\texttt{non-conformable arrays}. This failure is separate from the undefined name and appears once the name is corrected.",
    "what_survives": "The article is not affected. The formulas of the estimators and the function \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula}, called with a vector \\texttt{d}, are unchanged. I found no direct call to \\texttt{interacted\\_unbiased\\_regression} in the replication scripts, and the failure is an error message, not a wrong estimate. I did not test whether the function runs to its end once both changes are made."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E016",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of the top of page 1510. The first line reads 'If kappa log d = o(1),' with the footnote mark 8. The display below gives ATE-hat_I as ATE plus the treated-arm average of y_i(1) minus its mean minus x_i' beta_{I,T}, minus the corresponding control-arm average, plus O_p of the square root of kappa d over n. A red box marks the condition 'kappa log d = o(1)'.",
     "caption": "Theorem 4.1, continued, p. 1510 (PDF p. 9): the condition and the expansion. The marked condition is $\\kappa\\log d=o(1)$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E001.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T7",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T7"
    },
    {
     "id": "P005-T8",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T8"
    },
    {
     "id": "P005-T9",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T9"
    },
    {
     "id": "P005-T20",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T20"
    },
    {
     "id": "P005-T24",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T24"
    },
    {
     "id": "P005-T27",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T27"
    }
   ],
   "headline": "The condition for the expansion in Theorem 4.1 should read $\\kappa\\log\\max\\{d,2\\}=o(1)$: for a single covariate the printed condition $\\kappa\\log d=o(1)$ is empty, and the expansion can fail.",
   "id": "P005-E001",
   "location": "Theorem 4.1, p. 1510 (PDF p. 9), the condition “If $\\kappa\\log d=o(1)$” and the expansion that follows it; the theorem begins on p. 1509 (PDF p. 8)",
   "pdf_page": 9,
   "printed_page": "1510",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T20",
    "P005-T24",
    "P005-T27",
    "P005-T7",
    "P005-T8",
    "P005-T9"
   ],
   "text": {
    "as_printed": "Theorem 4.1 is stated ``Under Assumptions 1--3''. Its last paragraph reads ``If $\\kappa\\hl{\\log d}=o(1)$,'' with footnote 8 attached, and continues with the display\n\\[\n\\widehat{\\mathrm{ATE}}_I=\\mathrm{ATE}+\\frac{1}{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-\\overline{y(1)}-x_i'\\beta_{I,T}\\bigr)-\\frac{1}{n_C}\\sum_{i\\in[C]}\\bigl(y_i(0)-\\overline{y(0)}-x_i'\\beta_{I,C}\\bigr)+O_p\\Bigl(\\sqrt{\\frac{\\kappa d}{n}}\\Bigr).\n\\]\nFootnote 8: ``The upper bound on the stochastic order of the bias of the interacted case is characterized in equation (15) in Lei and Ding (2021).''",
    "corrected": "Theorem 4.1, last paragraph. Let Assumptions 1--3 hold, and let all design matrices be invertible, as footnote 4 assumes. If $\\kappa\\hl{\\log\\max\\{d,2\\}}=o(1)$, then\n\\[\n\\widehat{\\mathrm{ATE}}_I=\\mathrm{ATE}+\\frac{1}{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-\\overline{y(1)}-x_i'\\beta_{I,T}\\bigr)-\\frac{1}{n_C}\\sum_{i\\in[C]}\\bigl(y_i(0)-\\overline{y(0)}-x_i'\\beta_{I,C}\\bigr)+O_p\\Bigl(\\sqrt{\\frac{\\kappa d}{n}}\\Bigr).\n\\]\nEquivalently, the printed condition $\\kappa\\log d=o(1)$ is kept, and $\\kappa=o(1)$ is required in addition when $d=1$.",
    "evidence": "The evidence is an exact counterexample and a derivation. For even $n\\ge6$, let $d=1$, $n_T=n_C=n/2$ and $\\epsilon=n^{-2}$. Let $v_1=0$, and let $v_2,\\ldots,v_n$ be the $n-1$ equally spaced points from $-1$ to $1$. I define $a_1=1$ and $a_i=\\epsilon v_i$ for $i\\ge2$, and I write $x$ for the array $a$ after centering and scaling to $\\overline{x^2}=1$. The potential outcomes are $y_i(1)=y_i(0)=v_i$. Assumptions 1--3 hold, with $K=1$ in Assumption 1. The average treatment effect is zero, and both arm regressions are invertible under every assignment. The maximum leverage is\n\\[\n\\kappa=\\frac{3n(n-1)(n-2)}{3n^2(n-2)+1}\\longrightarrow1,\n\\]\nwhile $\\kappa\\log d=0$ for every $n$. In the arm without unit 1, the relation $y_i=a_i/\\epsilon$ holds exactly, so the fitted value at $x=0$, that is, at $a=1/n$, equals $n$. In the arm with unit 1, the fitted value at $x=0$ is less than $3$ in absolute value. Hence $|\\widehat{\\mathrm{ATE}}_I|\\ge n-3$ under every assignment. The linear term of the expansion is at most $13/6$ in absolute value. Combining these two bounds, I find that the remainder $R_n$ satisfies $|R_n|\\ge n-6$ under every assignment, while the claimed order is $\\sqrt{\\kappa/n}\\le n^{-1/2}$. The ratio is at least $(n-6)\\sqrt n$, which implies that $R_n$ is not $O_p(\\sqrt{\\kappa d/n})$. I enumerated all assignments in exact arithmetic for $n=6,8,10,12,14$, and the results agree with these bounds. At $n=12$, the smallest value of $|R_n|$ over the 924 assignments is $8690712840/752921287$, which is larger than $11$. Note that in this example the estimator and its remainder each have mean zero over the assignments. The failure concerns the stochastic order of the remainder and not the expected bias.\n\nFor the derivation, let $d=1$, and suppose that Assumptions 1--3 hold, that the arm regressions are invertible, and that $\\kappa=o(1)$. Let $S$ be an arm of size $m$ and $w$ a fixed array. Then\n\\[\nE\\bar w_S=\\bar w,\\qquad \\operatorname{Var}(\\bar w_S)=\\frac{n-m}{m(n-1)}\\,\\overline{(w-\\bar w)^2},\n\\]\nand the coefficient in the formula for the variance is $O(1/n)$ by Assumption 3. Since $\\bar x=0$, $\\overline{x^2}=1$ and $\\max_ix_i^2=n\\kappa$, I have $\\bar x_S=O_p(n^{-1/2})$ and $\\overline{x^4}\\le n\\kappa$. This gives $\\overline{x^2}_S=1+O_p(\\sqrt\\kappa)$ and $\\widehat L_S=\\overline{x^2}_S-\\bar x_S^2=1+O_p(\\sqrt\\kappa)$, so that $\\widehat L_S^{-1}=O_p(1)$. Let $y$ be the potential outcome of the arm, $\\beta=\\overline{xy}$ and $e_i=y_i-\\bar y-x_i\\beta$. Then $\\bar e=\\overline{xe}=0$ and $\\overline{e^2}\\le K$. Applying the formula for the variance to the residuals, I find $\\bar e_S=O_p(n^{-1/2})$. The same formula yields $\\overline{xe}_S=O_p(\\sqrt\\kappa)$, since $\\overline{x^2e^2}\\le n\\kappa\\,\\overline{e^2}$. The fitted slope satisfies\n\\[\n\\widehat\\beta_S-\\beta=\\widehat L_S^{-1}\\bigl(\\overline{xe}_S-\\bar x_S\\bar e_S\\bigr)=O_p(\\sqrt\\kappa),\n\\]\nwhere I used that $\\kappa\\ge1/n$. Subtracting the linear term from the estimator, I obtain\n\\[\nR_n=-\\bar x_T\\bigl(\\widehat\\beta_{I,T}-\\beta_{I,T}\\bigr)+\\bar x_C\\bigl(\\widehat\\beta_{I,C}-\\beta_{I,C}\\bigr)=O_p\\Bigl(\\sqrt{\\frac{\\kappa}{n}}\\Bigr).\n\\]\nThis is the stated remainder for $d=1$. For $d\\ge2$ the corrected condition is the printed one; the expansion in that range is the subject of \\fid{P005-N004}.",
    "problem": "The number of covariates $d$ may equal $1$: Assumption 1 allows every $d\\le n$, and the paper gives $\\log$ no special meaning. Since $\\log1=0$, the condition $\\kappa\\log d=o(1)$ holds for every sequence with $d=1$, whatever the maximum leverage $\\kappa$. The theorem therefore asserts the expansion with remainder $O_p(\\sqrt{\\kappa/n})$ for sequences with a single covariate such that $\\kappa$ does not tend to zero. On such sequences the expansion can fail. One unit whose leverage stays away from zero is enough, as the example below shows.",
    "what_survives": "The finite-sample decomposition in Theorem 4.1, the exact bias formulas, the noninteracted results and the case $d\\ge2$ are unaffected. Theorem 4.2 already assumes $\\kappa=o(1)$ for its expansion. Its proof in Appendix B.4 refers to the stochastic orders of Theorem 4.1, but that assumption excludes the example. The condition of Remark 4, a fixed $d$ with bounded fourth moments, also excludes it, since $\\overline{x^4}$ grows at least as $n\\kappa^2$ in the example. In the example the mean of the debiased estimator of Theorem 4.2 over all assignments is exactly zero, which is the average treatment effect. What changes is the domain of the expansion for $d=1$: a sequence in which the leverage of one unit does not vanish is excluded. The estimators, the estimand and the stated remainder do not change."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E001",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of the statement of Lemma A.1: the line 'Lemma A.1: Let t in {T, C} and n at least 4. Then,', the identity for the expectation of the covariance estimator, and the variance bound, followed by the first two lines of the proof. A red box marks the whole right side of the variance bound, from the inequality sign to the sum of the squares b_i^2.",
     "caption": "Lemma A.1, p. 1511 (PDF p. 10). The marked right side of the variance bound is written with the vectors $a$ and $b$ themselves, which the paragraph before the lemma allows to be arbitrary.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E002.png"
    },
    {
     "alt": "Crop of the second paragraph of the proof of Lemma A.1 and the two-line display after it. A red box marks the clause 'we can assume, without loss of generality, a-bar = 0 and b-bar = 0', with its footnote mark 9. The display bounds Var(ab-bar_T minus a-bar_T b-bar_T) by the same right side as in the lemma.",
     "caption": "Proof of Lemma A.1, p. 1511 (PDF p. 10). The marked clause centers $a$ and $b$; the display below it then derives the bound for centered vectors only.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E002-b.png"
    },
    {
     "alt": "Crop of item 2, which begins 'Since the first-order term in (11) is canceled' and ends 'First notice, by Lemma A.1 and Assumption 1,', and of the four-line chain of inequalities for the variance of the treated-arm covariance of h and y(1). A red box marks the first line of the chain, whose terms contain h_i y_i(1) minus the mean of hy(1), y_i(1) squared and h_i squared. The chain ends with O(kappa squared n plus kappa d over n).",
     "caption": "Proof of Theorem 3.2, item 2, p. 1517 (PDF p. 16). The marked line applies Lemma A.1 to the leverage $h$, whose mean is $d$, and the outcome $y(1)$, whose mean need not be zero.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E002-c.png"
    },
    {
     "alt": "Dot plot with three rows, one for each example: arbitrary a and b with n = 6 and n_t = 4; a_i b_i = 1 for all i with n = 14 and n_t = 7; leverage h and outcome y(1) with n = 16 and n_T = 8. The horizontal axis is the bound divided by the exact variance of the estimator, from 0 to about 2.3, with a vertical line at ratio 1 labeled exact variance. In each row a blue circle for the bound as printed lies to the left of the line, at 0.77, 0.90 and 0.93, and an orange square for the centered bound lies to the right, at about 1.89, 2.05 and 2.07.",
     "caption": "The printed and the centered bound of Lemma A.1, each divided by the exact variance of the covariance estimator, in the three examples of the table. A ratio below 1 means that the bound fails. The printed bound has ratios 0.77, 0.90 and 0.93.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E002-bounds.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T1",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T1"
    },
    {
     "id": "P005-T2",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T2"
    },
    {
     "id": "P005-T3",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T3"
    },
    {
     "id": "P005-T4",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T4"
    },
    {
     "id": "P005-T19",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T19"
    },
    {
     "id": "P005-T26",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T26"
    }
   ],
   "headline": "The variance bound of Lemma A.1 holds when its right side is computed from the centered vectors $a-\\bar a$ and $b-\\bar b$, not for arbitrary $a$ and $b$ as printed; with this change, the order $O(\\kappa^2n+\\kappa d/n)$ in the proof of Theorem 3.2 is the same.",
   "id": "P005-E002",
   "location": "Appendix A.2, Lemma A.1, p. 1511 (PDF p. 10), the variance bound and the second paragraph of its proof; applied in Appendix B.2, proof of Theorem 3.2, item 2, p. 1517 (PDF p. 16)",
   "pdf_page": 10,
   "printed_page": "1511",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T1",
    "P005-T19",
    "P005-T2",
    "P005-T26",
    "P005-T3",
    "P005-T4"
   ],
   "text": {
    "as_printed": "P.~1510: ``Let $a=(a_1,\\ldots,a_n)\\in\\mathbb R^n$ and $b=(b_1,\\ldots,b_n)\\in\\mathbb R^n$ be arbitrary $n$-vectors with fixed elements. We define the covariance estimator for the treated group as $\\widehat{\\operatorname{Cov}}_T(a,b)=\\overline{ab}_T-\\bar a_T\\bar b_T$, and similarly for the control group as $\\widehat{\\operatorname{Cov}}_C(a,b)=\\overline{ab}_C-\\bar a_C\\bar b_C$.''\n\nP.~1511: ``LEMMA A.1: Let $t\\in\\{T,C\\}$ and $n\\ge4$. Then,\n\\[\n\\mathbb E\\bigl[\\widehat{\\operatorname{Cov}}_t(a,b)\\bigr]=\\frac{(n_t-1)n}{n_t(n-1)}\\bigl(\\overline{ab}-\\bar a\\bar b\\bigr),\n\\]\n\\[\n\\operatorname{Var}\\bigl(\\widehat{\\operatorname{Cov}}_t(a,b)\\bigr)\\le\\frac{2(n-n_t)}{n_t(n-1)}\\frac1n\\sum_{i=1}^n\\bigl(\\hl{a_ib_i-\\overline{ab}}\\bigr)^2+\\frac{2(n-n_t)n}{n_t^3(n-1)}\\frac1n\\sum_{i=1}^n\\hl{a_i^2}\\times\\frac1n\\sum_{i=1}^n\\hl{b_i^2}.\\text{''}\n\\]\n\nP.~1511, proof: ``To upper-bound the variance, we first note that the covariance estimator is location invariant and we can assume, \\hl{without loss of generality}, $\\bar a=0$ and $\\bar b=0$.$^{9}$''\n\nP.~1517, item 2: ``First notice, by Lemma A.1 and Assumption 1,\n\\[\n\\begin{aligned}\n&\\operatorname{Var}\\bigl[\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\bigr]\\\\\n&\\quad\\le\\frac{2(n-n_T)}{n_T(n-1)}\\frac1n\\sum_{i=1}^n\\bigl(\\hl{h_iy_i(1)-\\overline{hy(1)}}\\bigr)^2+\\frac{2(n-n_T)n}{n_T^3(n-1)}\\frac1n\\sum_{i=1}^n\\hl{y_i^2(1)}\\,\\frac1n\\sum_{i=1}^n\\hl{h_i^2}\\\\\n&\\quad\\le\\frac{2(n-n_T)}{n_T(n-1)}\\frac1n\\sum_{i=1}^n\\hl{h_i^2y_i^2(1)}+\\frac{2(n-n_T)n}{n_T^3(n-1)}\\frac1n\\sum_{i=1}^n\\hl{y_i^2(1)}\\,\\frac1n\\sum_{i=1}^n\\hl{h_i^2}\\\\\n&\\quad\\le\\frac{2(n-n_T)}{n_T(n-1)}n^2\\kappa^2\\frac1n\\sum_{i=1}^ny_i^2(1)+\\frac{2(n-n_T)n}{n_T^3(n-1)}\\frac1n\\sum_{i=1}^ny_i^2(1)\\,\\frac1n\\sum_{i=1}^nh_i\\times n\\kappa\\\\\n&\\quad=O\\Bigl(\\kappa^2n+\\frac{\\kappa d}{n}\\Bigr).\\text{''}\n\\end{aligned}\n\\]",
    "corrected": "Lemma A.1: Let $a$ and $b$ be arbitrary $n$-vectors with fixed elements, and write $a_i^c=a_i-\\bar a$ and $b_i^c=b_i-\\bar b$. Let $t\\in\\{T,C\\}$ and $n\\ge4$. Then,\n\\[\n\\mathbb E\\bigl[\\widehat{\\operatorname{Cov}}_t(a,b)\\bigr]=\\frac{(n_t-1)n}{n_t(n-1)}\\bigl(\\overline{ab}-\\bar a\\bar b\\bigr),\n\\]\n\\[\n\\operatorname{Var}\\bigl(\\widehat{\\operatorname{Cov}}_t(a,b)\\bigr)\\le\\frac{2(n-n_t)}{n_t(n-1)}\\frac1n\\sum_{i=1}^n\\bigl(\\hl{a_i^cb_i^c-\\overline{a^cb^c}}\\bigr)^2+\\frac{2(n-n_t)n}{n_t^3(n-1)}\\frac1n\\sum_{i=1}^n\\hl{(a_i^c)^2}\\times\\frac1n\\sum_{i=1}^n\\hl{(b_i^c)^2}.\n\\]\n\nP.~1517, item 2: ``First notice, by Lemma A.1 applied to $h$ and $y(1)$, whose centered versions are $h-d$ and $y(1)-\\overline{y(1)}$, and by Assumptions 1--3,\n\\[\n\\begin{aligned}\n&\\operatorname{Var}\\bigl[\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\bigr]\\\\\n&\\quad\\le\\frac{2(n-n_T)}{n_T(n-1)}\\frac1n\\sum_{i=1}^n\\Bigl(\\hl{(h_i-d)\\bigl(y_i(1)-\\overline{y(1)}\\bigr)-\\overline{(h-d)\\bigl(y(1)-\\overline{y(1)}\\bigr)}}\\Bigr)^2\\\\\n&\\qquad+\\frac{2(n-n_T)n}{n_T^3(n-1)}\\frac1n\\sum_{i=1}^n\\hl{\\bigl(y_i(1)-\\overline{y(1)}\\bigr)^2}\\,\\frac1n\\sum_{i=1}^n\\hl{(h_i-d)^2}\\\\\n&\\quad\\le\\frac{2(n-n_T)}{n_T(n-1)}n^2\\kappa^2\\hl{K}+\\frac{2(n-n_T)n}{n_T^3(n-1)}n\\kappa\\hl{dK}\\\\\n&\\quad=O\\Bigl(\\kappa^2n+\\frac{\\kappa d}{n}\\Bigr),\n\\end{aligned}\n\\]\nwhere $K$ is the constant of Assumption 1.'' The next sentence of the proof, which gives the order $O(\\kappa^2/n+\\kappa d/n^3)$ for the variance of $n^{-1}(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T)$, is unchanged.",
    "evidence": "The evidence is an exact counterexample to the printed bound and a derivation of the centered bound. All variances below are over the random assignment, in which the group is a uniformly random subset of size $n_t$. For each numerical example, the variance is computed in exact rational arithmetic over every assignment.\n\n\\emph{The lemma.} Let $n=6$, $n_t=4$, $a=(0,-3,-1,2,-4,-3)$ and $b=(2,1,3,-3,1,1)$. Over the 15 assignments, $\\widehat{\\operatorname{Cov}}_t(a,b)$ has mean $-69/40$, in agreement with the expectation identity, and variance $16607/4800$. The printed right side is $3829/1440$, which is smaller. The centered bound is $835/128$; the means of $a$ and $b$ are $-3/2$ and $5/6$.\n\n\\emph{The application.} Let $n=16$, $n_T=8$, $d=1$ and $x=(8c,-8c,c,-c,\\ldots,c,-c)$ with $c=\\sqrt{8/71}$, so that $\\bar x=0$ and $\\overline{x^2}=1$. Then $h_i=x_i^2$ equals $512/71$ for the first two units and $8/71$ for the others, $\\bar h=1=d$ and $\\kappa=32/71$. Let $y(1)=(1/64,1/64,1,\\ldots,1)$ and $y(0)=0$. The mean squares of $x$, $y(1)$ and $y(0)$ are at most 1, and $n_T/n=1/2$. Since every product $h_iy_i(1)$ equals $8/71$, the first term of the printed bound vanishes. Over the 12870 assignments, the variance of $\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T$ is $1678565511/8259174400$. The first line of the display on p.~1517 equals $117645319/619438080$ and the second line equals $334349/1744896$; both are smaller than the variance. The centered bound equals $5550293259/13214679040$. In a third example, with $n=14$, $n_t=7$, $a=(30,1,\\ldots,1)$ and $b_i=1/a_i$, the variance is $707281/240100$, the printed right side is $10683013/4013100$ and the centered bound is $365664277/60505200$. The table collects the three examples.\n\n\\begin{audittable}{lrrr}{Exact variance of $\\widehat{\\operatorname{Cov}}_t(a,b)$ and the two bounds in three examples, rounded to four decimals; the exact values are in the text. A valid upper bound is at least as large as the variance.}\nExample & Exact variance & Bound as printed & Centered bound \\\\\n$n=6$, $n_t=4$, arbitrary $a$ and $b$ & 3.4598 & 2.6590 & 6.5234 \\\\\n$n=14$, $n_t=7$, $a_ib_i=1$ for all $i$ & 2.9458 & 2.6620 & 6.0435 \\\\\n$n=16$, $n_T=8$, $a=h$ and $b=y(1)$ & 0.2032 & 0.1899 & 0.4200 \\\\\n\\end{audittable}\n\n\\emph{The centered bound.} Let $n\\ge4$ and $1\\le m\\le n-1$, where $m=n_t$, let $S$ be the random group, and write $u=a-\\bar a$ and $v=b-\\bar b$. Expanding the sample means shows that $\\widehat{\\operatorname{Cov}}_t(a,b)=\\overline{uv}_S-\\bar u_S\\bar v_S$ for every $S$. By the variance of a sample mean under simple random sampling, I have\n\\[\n\\operatorname{Var}\\bigl(\\overline{uv}_S\\bigr)=\\frac{n-m}{m(n-1)}\\frac1n\\sum_{i=1}^n\\bigl(u_iv_i-\\overline{uv}\\bigr)^2.\n\\]\nFor the product of the two means, set $Z=\\bigl(\\sum_{i\\in S}u_i\\bigr)\\bigl(\\sum_{i\\in S}v_i\\bigr)$, $A=\\sum_iu_i^2$, $B=\\sum_iv_i^2$, $G=\\sum_iu_iv_i$ and $H=\\sum_iu_i^2v_i^2$, and define\n\\[\n\\alpha=\\frac{m(n-m)}{n(n-1)},\\qquad\\ell=\\frac{m(m-1)(n-m)(n-m-1)}{n(n-1)(n-2)(n-3)}.\n\\]\nExpanding $Z^2$, grouping the terms by the number of distinct indices and using $\\sum_iu_i=\\sum_iv_i=0$, I obtain\n\\[\n\\operatorname{Var}Z=(\\alpha-6\\ell)H+\\ell AB+(2\\ell-\\alpha^2)G^2.\n\\]\nHere $0\\le H\\le AB$, $G^2\\le AB$ and $G^2\\le nH$, and $\\ell\\le\\alpha(n-2)/(4(n-3))$ because the factors $m-1$ and $n-m-1$ sum to $n-2$. If $\\alpha\\ge6\\ell$, the identity implies that $\\operatorname{Var}Z\\le(\\alpha-3\\ell)AB\\le\\alpha AB$. If $\\alpha<6\\ell$, using $H\\ge G^2/n$, I find\n\\[\n\\operatorname{Var}Z\\le\\Bigl[\\frac\\alpha n+\\Bigl(3-\\frac6n\\Bigr)\\ell\\Bigr]AB\\le\\alpha\\Bigl[1-\\frac{n-4}{4(n-3)}\\Bigr]AB\\le\\alpha AB.\n\\]\nIn the second inequality, I used the bound on $\\ell$. Since $\\bar u_S\\bar v_S=Z/m^2$, in both cases\n\\[\n\\operatorname{Var}\\bigl(\\bar u_S\\bar v_S\\bigr)\\le\\frac{(n-m)n}{m^3(n-1)}\\Bigl(\\frac1n\\sum_{i=1}^nu_i^2\\Bigr)\\Bigl(\\frac1n\\sum_{i=1}^nv_i^2\\Bigr).\n\\]\nThe centered bound follows from $\\operatorname{Var}(U-V)\\le2\\operatorname{Var}U+2\\operatorname{Var}V$. Both of its sides are unchanged when constants are added to $a$ and $b$. The reduction to $\\bar a=\\bar b=0$ in the printed proof is then legitimate.\n\n\\emph{The order on p.~1517.} By Assumption 2, I have $\\bar h=d$ and $0\\le h_i\\le n\\kappa$. Then $|h_i-d|\\le n\\kappa$ and $n^{-1}\\sum_i(h_i-d)^2\\le n^{-1}\\sum_ih_i^2\\le n\\kappa d$. Assumption 1 gives $n^{-1}\\sum_i(y_i(1)-\\overline{y(1)})^2\\le K$. Subtracting a mean lowers a mean square, so the first sum in the centered bound is at most $n^{-1}\\sum_i(h_i-d)^2(y_i(1)-\\overline{y(1)})^2\\le n^2\\kappa^2K$. Inserting these bounds into the centered bound, and using Assumption 3 for the coefficients, I obtain the chain in the correction below.",
    "problem": "Lemma A.1 is stated for arbitrary fixed vectors $a$ and $b$, and the bars in its variance bound denote their population means. The variance argument begins by assuming $\\bar a=\\bar b=0$, on the ground that the covariance estimator is location invariant. The estimator is unchanged when a constant is added to $a$ or to $b$, but the right side of the bound is not. The proof therefore establishes the bound only when the right side is computed from $a-\\bar a$ and $b-\\bar b$. I refer to the bound with this right side as the centered bound. For vectors that are not centered, the printed right side can be smaller than the variance. Item 2 of the proof of Theorem 3.2 applies the lemma to the leverage $h$, whose population mean is $d$ by Assumption 2, and to the outcome $y(1)$, whose mean need not be zero. The first two purported upper bounds in the display on p.~1517 are not valid in general: both fail for a design that Assumptions 1--3 allow.",
    "what_survives": "The expectation identity of Lemma A.1 is correct as printed. The covariance estimators, the bias corrections and the unbiasedness claims of Theorems 3.2 and 4.2 do not depend on the variance bound. The asymptotic expansions of Theorems 3.2 and 4.2 use the bound only for the order of the variance of the covariance between leverage and outcome. Under Assumptions 1--3 this order is the same with the centered bound, and this variance error does not affect the expansions. This correction requires no change to an assumption, estimand, estimator or theorem conclusion, or to a computation in the replication files."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E002",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of the lower part of Theorem 4.1 on page 1509. Two rows define nu_1T, nu_2T, nu_3T and nu_1C, nu_2C, nu_3C. Here nu_3T is minus x-bar_T times the treated mean of y star of 1, and nu_3C is minus x-bar_C times the control mean of y star of 0. Two displays follow. In the last display, the expectation of x-bar_C prime nu_3C minus the expectation of x-bar_T prime nu_3T is set equal to n_T (n_T - n_C) over (n-1)(n-2) n_C squared, times the covariance term for y(0), minus n_C (n_C - n_T) over (n-1)(n-2) n_T squared, times the covariance term for y(1). Red boxes mark the first coefficient and the second coefficient together with its minus sign.",
     "caption": "Theorem 4.1, p. 1509 (PDF p. 8): the definitions of $\\nu_{3T}$ and $\\nu_{3C}$ and the two displays for the bias components. The marked coefficients in the last display carry the reversed signs.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E003.png"
    },
    {
     "alt": "Chart with three positions on the horizontal axis: n_T = 2 and n_C = 4 with 15 assignments, n_T = 3 and n_C = 3 with 20 assignments, and n_T = 4 and n_C = 2 with 15 assignments. The vertical axis is the third bias component in units of the outcome, from -0.2 to 0.2. Filled blue circles, the exact expectations, are at 217/2500, 0 and -3689/25000. Open orange squares, the printed display, are at -217/2500, 0 and 3689/25000. At each unbalanced allocation the square is the mirror image of the circle about zero, and at the balanced allocation both are zero.",
     "caption": "The third bias component of $\\widehat{\\mathrm{ATE}}_I$ in the six-unit example, for three allocations. Filled circles give the exact expectation over all assignments, which equals the corrected display. Open squares give the last display of Theorem 4.1 as printed.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E003-third-component.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T5",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T5"
    },
    {
     "id": "P005-T6",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T6"
    },
    {
     "id": "P005-T13",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T13"
    },
    {
     "id": "P005-T20",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T20"
    },
    {
     "id": "P005-T24",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T24"
    }
   ],
   "headline": "Both signs on the right-hand side of the last display of Theorem 4.1 are reversed.",
   "id": "P005-E003",
   "location": "Theorem 4.1, p. 1509 (PDF p. 8), last display",
   "pdf_page": 8,
   "printed_page": "1509",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Moderate",
   "subject": "paper",
   "target_ids": [
    "P005-T13",
    "P005-T20",
    "P005-T24",
    "P005-T5",
    "P005-T6"
   ],
   "text": {
    "as_printed": "Theorem 4.1 defines $\\nu_{3T}=-(\\bar x_T\\overline{y^*(1)}_T)$ and $\\nu_{3C}=-(\\bar x_C\\overline{y^*(0)}_C)$, and its last display reads\n\\[\n\\begin{aligned}\nE\\bigl[\\bar x_C'\\nu_{3C}\\bigr]-E\\bigl[\\bar x_T'\\nu_{3T}\\bigr]\n={}&{}\\hl{\\frac{n_T(n_T-n_C)}{(n-1)(n-2)n_C^2}}\\bigl(\\overline{hy(0)}-\\bar h\\times\\overline{y(0)}\\bigr)\\\\\n&{}\\hl{-}\\frac{n_C(n_C-n_T)}{(n-1)(n-2)n_T^2}\\bigl(\\overline{hy(1)}-\\bar h\\times\\overline{y(1)}\\bigr).\n\\end{aligned}\n\\]",
    "corrected": "Theorem 4.1, last display. Let Assumptions 1--3 hold, \\hl{with Assumption 2's normalization holding at the sample size considered}, let $y_i^*(t)=y_i(t)-\\overline{y(t)}$ and $h_i=\\|x_i\\|_2^2$, and let $\\nu_{3T}=-(\\bar x_T\\overline{y^*(1)}_T)$ and $\\nu_{3C}=-(\\bar x_C\\overline{y^*(0)}_C)$, as in the theorem. The expectation is over the complete randomization of $n_T$ of the $n\\ge3$ units to treatment, with $n_C=n-n_T$. Then\n\\[\n\\begin{aligned}\nE\\bigl[\\bar x_C'\\nu_{3C}\\bigr]-E\\bigl[\\bar x_T'\\nu_{3T}\\bigr]\n={}&{}\\hl{-}\\frac{n_T(n_T-n_C)}{(n-1)(n-2)n_C^2}\\bigl(\\overline{hy(0)}-\\bar h\\times\\overline{y(0)}\\bigr)\\\\\n&{}\\hl{+}\\frac{n_C(n_C-n_T)}{(n-1)(n-2)n_T^2}\\bigl(\\overline{hy(1)}-\\bar h\\times\\overline{y(1)}\\bigr).\n\\end{aligned}\n\\]\nIn the notation of Appendix A.1, the right-hand side is $-N_{CCC}S_0+N_{TTT}S_1$. The definitions of $\\nu_{3T}$ and $\\nu_{3C}$ and the estimator of Theorem 4.2 stay as printed.",
    "evidence": "The evidence is a derivation and an exact counterexample. For the derivation, let $A$ be a uniformly chosen subset of size $m$ of the $n\\ge3$ units, and let $a$, $b$ and $c$ be fixed arrays that each sum to zero. I set $s=\\sum_i a_ib_ic_i$. In the sum $\\sum_{i,j,k}a_ib_jc_k$, the terms in which all three indices are equal contribute $s$, and the terms in which exactly two indices are equal contribute $-3s$. The whole sum is zero, so the terms in which the three indices are distinct contribute $2s$. One, two and three distinct units are included in $A$ with probabilities $q_1=m/n$, $q_2=m(m-1)/(n(n-1))$ and $q_3=m(m-1)(m-2)/(n(n-1)(n-2))$. I obtain\n\\[\nE\\bigl[\\bar a_A\\bar b_A\\bar c_A\\bigr]=\\frac{q_1-3q_2+2q_3}{m^3}\\,s=\\frac{(n-m)(n-2m)}{(n-1)(n-2)m^2}\\,\\overline{abc}.\n\\]\nThis is the first identity of Lemma A.2. Note that the coefficient is $N_{TTT}$ for $m=n_T$ and $N_{CCC}$ for $m=n_C$. Let $a=b$ be a coordinate of $x$, which is centered by Assumption 2, and let $c=y^*(t)$. Summing over the coordinates and using $\\overline{hy^*(t)}=S_t$, I have\n\\[\nE\\bigl[\\bar x_T'\\bar x_T\\,\\overline{y^*(1)}_T\\bigr]=N_{TTT}S_1,\\qquad\nE\\bigl[\\bar x_C'\\bar x_C\\,\\overline{y^*(0)}_C\\bigr]=N_{CCC}S_0.\n\\]\nBy the definitions of $\\nu_{3T}$ and $\\nu_{3C}$, each of which has a minus sign, I have $E[\\bar x_C'\\nu_{3C}]=-N_{CCC}S_0$ and $E[\\bar x_T'\\nu_{3T}]=-N_{TTT}S_1$. This implies that the left-hand side of the last display is $-N_{CCC}S_0+N_{TTT}S_1$.\n\nFor the counterexample, let $n=6$, $d=1$, $x=(-8,-5,0,3,4,6)/5$, $y_i(1)=x_i^2$ and $y_i(0)=2x_i^2+3$. Then $\\bar x=0$, $\\overline{x^2}=1$, $S_1=434/625$ and $S_0=868/625$, and every arm regression is invertible. For $n_T=2$ and $n_C=4$, the constants are $N_{TTT}=1/10$ and $N_{CCC}=-1/80$. Enumerating the 15 assignments in exact arithmetic, I find $217/2500$ for the left-hand side, while the right-hand side as printed is $-217/2500$. For $n_T=4$ and $n_C=2$ the two values are $-3689/25000$ and $3689/25000$, and for $n_T=n_C=3$ both are zero. If this population is repeated $r$ times, with $n_T=2r$ and $n_C=4r$, the resulting sequence satisfies Assumptions 1--3. On this sequence the third component is $5S_1/(2(6r-1)(6r-2))>0$, and the printed display is the negative of this value.\n\nA second example shows the effect on the total. Let $n=5$, $x=(-3/2,-1/2,0,1/2,3/2)$, $y(1)=(0,0,1,0,0)$, $y(0)=0$, $n_T=2$ and $n_C=3$. Enumerating the 10 assignments, I obtain the entries of the table. The three components add up to the bias of $\\widehat{\\mathrm{ATE}}_I$ only with the third component as defined.\n\\begin{audittable}{lrr}{Five-unit example: exact expectations of the components of the bias of $\\widehat{\\mathrm{ATE}}_I$.}\nQuantity & Third component as defined & Third component as printed \\\\\nFirst component & $3/40$ & $3/40$ \\\\\nSecond component & $11/80$ & $11/80$ \\\\\nThird component & $-1/80$ & $1/80$ \\\\\nSum of the three components & $1/5$ & $9/40$ \\\\\nBias of $\\widehat{\\mathrm{ATE}}_I$, by enumeration & $1/5$ & $1/5$ \\\\\n\\end{audittable}",
    "problem": "Theorem 4.1 writes the bias of the interacted estimator as a sum of three components, $E[\\bar x_C'\\nu_{jC}]-E[\\bar x_T'\\nu_{jT}]$ for $j=1,2,3$, and its last display states the third component in closed form. The theorem defines $\\nu_{3T}$ and $\\nu_{3C}$ with a minus sign each. With these definitions, the right-hand side of the last display is the negative of the left-hand side. I write $S_t=\\overline{hy(t)}-\\bar h\\,\\overline{y(t)}$ for $t=0,1$, and I let $N_{TTT}$ and $N_{CCC}$ denote the constants of Appendix A.1. The left-hand side is $-N_{CCC}S_0+N_{TTT}S_1$, and the display prints $N_{CCC}S_0-N_{TTT}S_1$. A bias computed by adding the three displayed components is off by twice the third component. The printed and the correct value agree only when the component is zero. This is the case when $n_T=n_C$, so a balanced design does not reveal the error. With unequal arm sizes, the component can also vanish by cancellation between nonzero $S_0$ and $S_1$.",
    "what_survives": "The decomposition of the coefficients in Theorem 4.1 and the display for its first component are unaffected, and no stochastic order changes. Theorem 4.2 is unaffected. Its coefficients $n_T/((n-2)n_C)$ and $-n_C/((n-2)n_T)$ follow from the corrected signs, and the opening display of its proof in Appendix B.4 carries the correct sign through an outer minus. In the six-unit example the mean of the debiased estimator over all assignments equals the average treatment effect, $-4$, for each of the three allocations. The analogous equation (6) for the noninteracted estimator is correct as printed. The interacted correction in the replication files uses the signs of Theorem 4.2. What changes is the last display of Theorem 4.1, and with it any bias computed from that display when the third component is nonzero."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E003",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "clarity_note",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "complete_derivation",
   "exhibits": [
    {
     "alt": "Crop from page 1506. Two lines introduce the interacted OLS regression. Equation (2) follows: Y_i ~ alpha_I + tau_I D_i + x_i' beta_{I,C} + D_i x_i' beta_{I,T}. Two further lines name the OLS estimators of the interacted case. A red box marks the last two terms of the equation, x_i' beta_{I,C} + D_i x_i' beta_{I,T}.",
     "caption": "Equation (2), p. 1506 (PDF p. 5). The marked terms are $x_i'\\beta_{I,C}+D_ix_i'\\beta_{I,T}$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E004.png"
    },
    {
     "alt": "Crop of the opening of Section 4 on page 1509. The first lines define beta-hat I,T as L-hat T inverse times N-hat T and beta-hat I,C as L-hat C inverse times N-hat C. Below the display for the interacted estimator, the sentence reads 'where beta-hat I,T and beta-hat I,C are the OLS coefficients on covariates D_i x_i and x_i, repsectively.' Red boxes mark the words 'OLS coefficients on covariates D_i x_i' and, on the next line, 'and x_i'.",
     "caption": "Section 4, p. 1509 (PDF p. 8): the definitions of $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$, the display for $\\widehat{\\mathrm{ATE}}_I$ and the sentence after it. The marked words call the two estimators the coefficients on $D_ix_i$ and $x_i$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E004-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T22",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T22"
    }
   ],
   "headline": "In Section 4, $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$ are the slopes fitted within the treatment arm and within the control arm; under equation (2) as printed, the coefficient on $D_ix_i$ is the difference of these two slopes.",
   "id": "P005-E004",
   "location": "Equation (2), p. 1506 (PDF p. 5); Section 4, p. 1509 (PDF p. 8), the definitions of $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$ and the sentence after the display for $\\widehat{\\mathrm{ATE}}_I$",
   "pdf_page": 5,
   "printed_page": "1506",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": null,
   "subject": "paper",
   "target_ids": [
    "P005-T22"
   ],
   "text": {
    "as_printed": "Equation (2), p.~1506:\n\\[\nY_i\\sim\\alpha_I+\\tau_ID_i+\\hl{x_i'\\beta_{I,C}+D_ix_i'\\beta_{I,T}}.\\qquad\\text{(2)}\n\\]\nSection 4, p.~1509: ``We write the regression coefficient estimators of the pretreatment covariates in the interacted case as $\\widehat\\beta_{I,T}=\\widehat L_T^{-1}\\widehat N_T$ and $\\widehat\\beta_{I,C}=\\widehat L_C^{-1}\\widehat N_C$ \\ldots'' and, after the display\n\\[\n\\widehat{\\mathrm{ATE}}_I=\\overline{y(1)}_T-\\overline{y(0)}_C-\\bigl(\\bar x_T'\\widehat\\beta_{I,T}-\\bar x_C'\\widehat\\beta_{I,C}\\bigr)\n\\]\n``for the interacted case, where $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$ are \\hl{the OLS coefficients on covariates $D_ix_i$ and $x_i$}, repsectively.''",
    "corrected": "Equation (2):\n\\[\nY_i\\sim\\alpha_I+\\tau_ID_i+\\hl{(1-D_i)}x_i'\\beta_{I,C}+D_ix_i'\\beta_{I,T}.\\qquad\\text{(2)}\n\\]\nSection 4: ``for the interacted case, where $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$ are \\hl{the OLS slopes within the treatment arm and within the control arm, that is, the coefficients on $D_ix_i$ and $(1-D_i)x_i$ in (2)}, respectively.''",
    "intended_meaning": "Section 4 defines the two estimators as $\\widehat L_T^{-1}\\widehat N_T$ and $\\widehat L_C^{-1}\\widehat N_C$. These are the least-squares slopes within the treatment arm and within the control arm. Every formula that follows, including Theorems 4.1 and 4.2, uses these definitions, and the display for $\\widehat{\\mathrm{ATE}}_I$ is correct with them. This is the intended meaning. The labels alone do not match. In equation (2) as printed, the fitted line is $\\alpha_I+x_i'\\beta_{I,C}$ in the control arm and $\\alpha_I+\\tau_I+x_i'(\\beta_{I,C}+\\beta_{I,T})$ in the treatment arm. The OLS coefficient on $x_i$ is the control slope, and the coefficient on $D_ix_i$ is the difference of the two slopes, $\\widehat L_T^{-1}\\widehat N_T-\\widehat L_C^{-1}\\widehat N_C$. Substituting that interaction coefficient for $\\widehat\\beta_{I,T}$ in the display gives a different number. For example, let $x=\\sqrt{3/20}\\,(-3,-2,-1,0,1,5)$ with the first two units in the treatment arm, and let $y_i(0)=x_i$ and $y_i(1)=2x_i$. The coefficients of (2) are $(0,0,1,1)$, and the slopes within the treatment arm and within the control arm are $2$ and $1$. The display equals $0$ with these two slopes and $-\\sqrt{15}/4$ with the two coefficients of (2). The parameterization below makes the labels agree and changes neither the fitted values nor $\\widehat\\tau_I$."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E004",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "complete_derivation",
   "exhibits": [
    {
     "alt": "Crop of the opening of the proof of Lemma A.2 and its first display, which expands the expectation of the sum over i of D_i x_i y_i times the sum over j not equal to i of D_j z_j. A red box marks the bracket [D_i D_j] in the double sum after the first equality sign.",
     "caption": "Proof of Lemma A.2, p. 1511 (PDF p. 10), first display. The marked bracket has no expectation sign; the next equality replaces it by the probability $n_T(n_T-1)/(n(n-1))$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E005.png"
    },
    {
     "alt": "Crop of the last display of the proof of Lemma A.2, which writes E[x-bar_T y-bar_T z-bar_T] as one over n_T cubed times three expectations. A red box marks the capital N above the first summation sign of the third expectation, whose lower limit is i = 1.",
     "caption": "Proof of Lemma A.2, p. 1512 (PDF p. 11), last display. The marked upper limit of the outer sum is $N$; the sums in the lines above run to $n$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E005-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T16",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T16"
    }
   ],
   "headline": "In the proof of Lemma A.2, the bracket $[D_iD_j]$ should read $\\mathbb E[D_iD_j]$, and the upper limit $N$ should read $n$.",
   "id": "P005-E005",
   "location": "Appendix A.2, proof of Lemma A.2: first display, p. 1511 (PDF p. 10); last display, p. 1512 (PDF p. 11)",
   "pdf_page": 10,
   "printed_page": "1511",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T16"
   ],
   "text": {
    "as_printed": "P.~1511:\n\\[\n\\mathbb E\\Bigl[\\sum_{i=1}^nD_ix_iy_i\\sum_{j\\ne i}D_jz_j\\Bigr]=\\sum_{i=1}^n\\sum_{j\\ne i}\\hl{[D_iD_j]}x_iy_iz_j=\\frac{n_T(n_T-1)}{n(n-1)}\\sum_{i=1}^n\\sum_{j\\ne i}x_iy_iz_j\n\\]\n\nP.~1512, last display:\n\\[\n\\begin{aligned}\n\\mathbb E[\\bar x_T\\bar y_T\\bar z_T]=\\frac1{n_T^3}\\Bigl(&\\mathbb E\\Bigl[\\sum_iD_ix_iy_iz_i\\Bigr]+\\mathbb E\\Bigl[\\sum_{i=1}^n\\sum_{j\\ne i}D_iD_j(x_iy_iz_j+x_iy_jz_i+x_jy_iz_i)\\Bigr]\\\\\n&+\\mathbb E\\Bigl[\\sum_{i=1}^{\\hl{N}}D_ix_i\\sum_{j\\ne i}D_jy_j\\sum_{s\\notin\\{i,j\\}}D_sz_s\\Bigr]\\Bigr)\n\\end{aligned}\n\\]",
    "corrected": "P.~1511:\n\\[\n\\mathbb E\\Bigl[\\sum_{i=1}^nD_ix_iy_i\\sum_{j\\ne i}D_jz_j\\Bigr]=\\sum_{i=1}^n\\sum_{j\\ne i}\\hl{\\mathbb E[D_iD_j]}x_iy_iz_j=\\frac{n_T(n_T-1)}{n(n-1)}\\sum_{i=1}^n\\sum_{j\\ne i}x_iy_iz_j\n\\]\n\nP.~1512, last display:\n\\[\n\\begin{aligned}\n\\mathbb E[\\bar x_T\\bar y_T\\bar z_T]=\\frac1{n_T^3}\\Bigl(&\\mathbb E\\Bigl[\\sum_iD_ix_iy_iz_i\\Bigr]+\\mathbb E\\Bigl[\\sum_{i=1}^n\\sum_{j\\ne i}D_iD_j(x_iy_iz_j+x_iy_jz_i+x_jy_iz_i)\\Bigr]\\\\\n&+\\mathbb E\\Bigl[\\sum_{i=1}^{\\hl{n}}D_ix_i\\sum_{j\\ne i}D_jy_j\\sum_{s\\notin\\{i,j\\}}D_sz_s\\Bigr]\\Bigr)\n\\end{aligned}\n\\]",
    "evidence": "The evidence is a check of pp.~1511--1512 and a derivation. With both readings restored, the coefficient of $\\sum_ix_iy_iz_i$ in the last display is\n\\[\n\\frac1{n_T^3}\\Bigl(\\frac{n_T}{n}-\\frac{3n_T(n_T-1)}{n(n-1)}+\\frac{2n_T(n_T-1)(n_T-2)}{n(n-1)(n-2)}\\Bigr)=\\frac{(n-n_T)(n-2n_T)}{n\\,n_T^2(n-1)(n-2)},\n\\]\nwhich equals $N_{\\mathrm{TTT}}/n$ with $N_{\\mathrm{TTT}}$ as defined on p.~1510.",
    "problem": "The first equality on p.~1511 takes the expectation inside the double sum. The bracket then needs the expectation sign, and the next equality replaces it by $n_T(n_T-1)/(n(n-1))$, which is $\\mathbb E[D_iD_j]$ for $i\\ne j$. On p.~1512 the outer sum of the third term runs to $N$. The population has $n$ units, and the same triple sum runs to $n$ in the display above.",
    "what_survives": "Lemma A.2, its constants and the rest of its proof are unchanged."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E005",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "complete_derivation",
   "exhibits": [
    {
     "alt": "Crop of the three-line display that bounds Var[(*)] and of the four lines of text below it. A red box marks, in the third line, the sum over i of n to the minus 1 times the squared norm of x_i times the square of e_j(1) minus e_j(0). The text below ends with the identity for the sum over i and j of (x_i prime x_j a_j) squared, which equals n times the sum over j of a_j squared times the squared norm of x_j.",
     "caption": "Appendix B.1.1, p. 1514 (PDF p. 13), the bound for $\\operatorname{Var}[(*)]$ and the explanation below it. In the marked sum the index of summation and the leverage carry $i$, while the residuals carry $j$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E007.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T17",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T17"
    }
   ],
   "headline": "In the last line of the variance bound for $(*)$, the leverage and the residual difference should carry the same summation index.",
   "id": "P005-E007",
   "location": "Appendix B.1.1, p. 1514 (PDF p. 13), display bounding $\\operatorname{Var}[(*)]$, third line",
   "pdf_page": 13,
   "printed_page": "1514",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T17"
   ],
   "text": {
    "as_printed": "\\[\n=\\Bigl(\\frac1{p_Cn_Tn}\\Bigr)^2n^2\\frac{n_Tn_C}{n(n-1)}\\sum_{\\hl{i}}n^{-1}\\|x_{\\hl{i}}\\|_2^2\\bigl(e_j(1)-e_j(0)\\bigr)^2=O\\Bigl(\\frac\\kappa n\\Bigr),\n\\]\nand, below the display: ``For the second to last equality, we use the fact\n\\[\n\\textstyle\\sum_{i,j}(x_i'x_ja_j)^2=\\sum_ja_j^2x_j'(\\sum_ix_ix_i')x_j=n\\sum_ja_j^2\\|x_j\\|_2^2\n\\]\nby Assumption 2.''",
    "corrected": "\\[\n=\\Bigl(\\frac1{p_Cn_Tn}\\Bigr)^2n^2\\frac{n_Tn_C}{n(n-1)}\\sum_{\\hl{j}}n^{-1}\\|x_{\\hl{j}}\\|_2^2\\bigl(e_j(1)-e_j(0)\\bigr)^2=O\\Bigl(\\frac\\kappa n\\Bigr),\n\\]",
    "evidence": "The evidence is a check of the page and a derivation. I write $\\delta_j=e_j(1)-e_j(0)$ and $h_j=\\|x_j\\|_2^2$. Since $\\sum_ix_ix_i'=nI_d$ by Assumption 2, I have\n\\[\n\\sum_{i,j}(x_i'x_j\\delta_j)^2=\\sum_j\\delta_j^2x_j'\\Bigl(\\sum_ix_ix_i'\\Bigr)x_j=n\\sum_jh_j\\delta_j^2.\n\\]\nWith the index matched, the last line equals $\\overline{h\\delta^2}/(p_Tp_Cn(n-1))$. Since $h_j\\le n\\kappa$, this is at most $\\kappa\\,\\overline{\\delta^2}/(p_Tp_C(n-1))$, which is $O(\\kappa/n)$ by Assumption 3 and the bounds on the residuals stated on p.~1513.",
    "problem": "The sum binds $i$, but the residuals carry $j$, which is then a free index. The identity quoted below the display contracts the double sum over $i$ and $j$ to a single sum in which the leverage and the squared coefficient have the same index.",
    "what_survives": "The contraction identity and the rate $O(\\kappa/n)$ are correct, and only the index changes."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E007",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "page_check",
   "exhibits": [
    {
     "alt": "Crop of the first lines of page 1516: the sentence 'Collecting the constants in front of' the treated-arm covariance with its display, which equals minus 1 over n minus 2, then the sentence 'Collecting the constants in front of' the control-arm expression with its display, which equals 1 over n minus 2. A red box marks the second term of the control-arm expression, a single overline over hy(0)y(0) with subscript C.",
     "caption": "Proof of Theorem 3.2, p. 1516 (PDF p. 15). The marked term is printed as a single mean of $hy(0)y(0)$; the parallel sentence for the treated arm, two lines above, has the product of two sample means.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E009.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T15",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T15"
    }
   ],
   "headline": "The control-arm covariance whose coefficient is collected is $\\overline{hy(0)}_C-\\bar h_C\\,\\overline{y(0)}_C$; the coefficient $1/(n-2)$ is correct.",
   "id": "P005-E009",
   "location": "Appendix B.2, proof of Theorem 3.2, p. 1516 (PDF p. 15), the second sentence that begins “Collecting the constants in front of”",
   "pdf_page": 15,
   "printed_page": "1516",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T15"
   ],
   "text": {
    "as_printed": "``Collecting the constants in front of $\\overline{hy(0)}_C-\\hl{\\overline{hy(0)y(0)}_C}$ gives\n\\[\n\\frac1{n-1}\\frac{n_C(n-1)}{(n_C-1)n}-\\frac{(n_T-n_C)}{(n-1)(n-2)n_T}\\frac{n_T(n-1)}{(n_C-1)n}=\\frac1{n-2}.\\text{''}\n\\]",
    "corrected": "``Collecting the constants in front of $\\overline{hy(0)}_C-\\hl{\\bar h_C\\,\\overline{y(0)}_C}$ gives\n\\[\n\\frac1{n-1}\\frac{n_C(n-1)}{(n_C-1)n}-\\frac{(n_T-n_C)}{(n-1)(n-2)n_T}\\frac{n_T(n-1)}{(n_C-1)n}=\\frac1{n-2}.\\text{''}\n\\]",
    "evidence": "The evidence is a check of the page against equations (7), (11) and (12), which print $\\overline{hy(0)}_C-\\bar h_C\\overline{y(0)}_C$, and a recalculation of the coefficient. With $n=n_T+n_C$, the left side of the display is\n\\[\n\\frac{n_C}{(n_C-1)n}-\\frac{n_T-n_C}{(n-2)(n_C-1)n}=\\frac{n_C(n-2)-n_T+n_C}{(n-2)(n_C-1)n}=\\frac1{n-2}.\n\\]",
    "problem": "The second term is printed as one overline over $hy(0)y(0)$. The sentence collects the coefficient of the control-arm covariance in equations (11) and (12). The second term of that covariance is the product of the sample means of $h$ and $y(0)$, as in the parallel sentence for the treated arm.",
    "what_survives": "The coefficient, the estimator of Theorem 3.2 and the rest of the proof are unchanged."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E009",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "page_check",
   "exhibits": [
    {
     "alt": "Crop of the sentence 'Now we derive the stochastic expansion for the debiased estimator:' and the four-line display for the debiased ATE estimator. One red box marks the factor (x-bar_T minus x-bar_C), printed without a prime, before L-hat inverse N-hat in the first line. A second red box marks the index set 'i in [T]' under the second sum of the third line, the sum of y_i(0) minus x_i prime N with factor one over n_C.",
     "caption": "Proof of Theorem 3.2, p. 1516 (PDF p. 15), the expansion of $\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}$. The first marked factor has no transpose; the second marked index set belongs to a sum of control outcomes with factor $1/n_C$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E010.png"
    },
    {
     "alt": "Crop of the sentence 'We can characterize the stochastic expansion for the debiased estimator of the treated group as' and the three-line display for the treated-arm debiased estimator. Red boxes mark four occurrences of x-bar_T printed without a prime: before L-hat_T inverse N-hat_T in the first line, before N_T and before (N-hat_T minus N_T) in the second line, and before N_T in the third line.",
     "caption": "Proof of Theorem 4.2, p. 1518 (PDF p. 17), last display. The four marked factors $\\bar x_T$ have no transpose; the factor inside the large parentheses of the first line has one.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E010-b.png"
    },
    {
     "alt": "Crop of the heading 'B.2. Proof of Theorem 3.2' and the first three lines of the proof. A red box marks the factor (x-bar_C minus x-bar_T), printed without a prime, in the expectation E[(x-bar_C minus x-bar_T)(nu_1 + nu_2 + nu_3)].",
     "caption": "Proof of Theorem 3.2, p. 1515 (PDF p. 14), first sentence. The marked factor has no transpose; item 1, two lines below, writes $(\\bar x_C-\\bar x_T)'\\nu_1$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E010-c.png"
    },
    {
     "alt": "Crop of Remark 2 with one line of text above and one below. Red boxes mark the symbol v_2, in a Latin letter, in both of its occurrences: in 'The bias in E[(x-bar_C minus x-bar_T) prime v_2] has been discussed previously' and in '(x-bar_C minus x-bar_T) prime v_2 contains no unknowns'.",
     "caption": "Remark 2, p. 1507 (PDF p. 6). Both marked symbols are a Latin $v_2$; Theorem 3.1, above the remark, defines the Greek $\\nu_2$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E010-d.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T10",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T10"
    },
    {
     "id": "P005-T11",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T11"
    },
    {
     "id": "P005-T14",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T14"
    }
   ],
   "headline": "Six covariate means lack a transpose, one control-arm sum runs over $[T]$ where $[C]$ is meant, and Remark 2 prints $v_2$ for $\\nu_2$.",
   "id": "P005-E010",
   "location": "Appendix B.2, proof of Theorem 3.2, p. 1516 (PDF p. 15), display for $\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}$; Appendix B.4, p. 1518 (PDF p. 17), last display; p. 1515 (PDF p. 14), first sentence of the proof of Theorem 3.2; Remark 2, p. 1507 (PDF p. 6)",
   "pdf_page": 15,
   "printed_page": "1516",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T10",
    "P005-T11",
    "P005-T14"
   ],
   "text": {
    "as_printed": "P.~1516, first and third lines of the display:\n\\[\n\\begin{aligned}\n\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}&=\\bigl(\\overline{y(1)}_T-\\overline{y(0)}_C-\\hl{(\\bar x_T-\\bar x_C)}\\widehat L^{-1}\\hat N\\bigr)-(\\bar x_C-\\bar x_T)'\\bigl(\\widehat L^{-1}-I_d^{-1}\\bigr)\\hat N+\\cdots\\\\\n&=\\frac1{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-x_i'N\\bigr)-\\frac1{n_C}\\sum_{\\hl{i\\in[T]}}\\bigl(y_i(0)-x_i'N\\bigr)-\\cdots\n\\end{aligned}\n\\]\n\nP.~1518, last display:\n\\[\n\\begin{aligned}\n\\widehat{\\mathrm{ATE}}_{T,I,\\mathrm{Debiased}}&=\\overline{y(1)}_T-\\hl{\\bar x_T}\\widehat L_T^{-1}\\hat N_T-\\Bigl(-\\bar x_T'\\bigl(\\widehat L_T^{-1}-I_d^{-1}\\bigr)\\hat N_T-\\frac{n_T}{(n-2)n_C}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\Bigr)\\\\\n&=\\overline{y(1)}_T-\\hl{\\bar x_T}N_T-\\hl{\\bar x_T}(\\hat N_T-N_T)+\\frac{n_T}{(n-2)n_C}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\\\\n&=\\overline{y(1)}_T-\\hl{\\bar x_T}N_T+O_p\\Bigl(\\sqrt{\\frac\\kappa n}\\Bigr),\n\\end{aligned}\n\\]\n\nP.~1515: ``We first propose estimators for the bias $\\mathbb E[\\hl{(\\bar x_C-\\bar x_T)}(\\nu_1+\\nu_2+\\nu_3)]$.''\n\nP.~1507, Remark 2: ``The bias in $E[(\\bar x_C-\\bar x_T)'\\hl{v_2}]$ has been discussed previously. $(\\bar x_C-\\bar x_T)'\\hl{v_2}$ contains no unknowns and hence can be subtracted directly for debiasing purposes.''",
    "corrected": "P.~1516, first and third lines of the display:\n\\[\n\\begin{aligned}\n\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}&=\\bigl(\\overline{y(1)}_T-\\overline{y(0)}_C-\\hl{(\\bar x_T-\\bar x_C)'}\\widehat L^{-1}\\hat N\\bigr)-(\\bar x_C-\\bar x_T)'\\bigl(\\widehat L^{-1}-I_d^{-1}\\bigr)\\hat N+\\cdots\\\\\n&=\\frac1{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-x_i'N\\bigr)-\\frac1{n_C}\\sum_{\\hl{i\\in[C]}}\\bigl(y_i(0)-x_i'N\\bigr)-\\cdots\n\\end{aligned}\n\\]\n\nP.~1518, last display: write $\\hl{\\bar x_T'}$ for $\\bar x_T$ before $\\widehat L_T^{-1}\\hat N_T$ in the first line, before $N_T$ and before $(\\hat N_T-N_T)$ in the second line, and before $N_T$ in the third line. The display with these transposes and with the corrected weights is given under \\fid{P005-E013}.\n\nP.~1515: ``We first propose estimators for the bias $\\mathbb E[\\hl{(\\bar x_C-\\bar x_T)'}(\\nu_1+\\nu_2+\\nu_3)]$.''\n\nP.~1507, Remark 2: ``The bias in $E[(\\bar x_C-\\bar x_T)'\\hl{\\nu_2}]$ has been discussed previously. $(\\bar x_C-\\bar x_T)'\\hl{\\nu_2}$ contains no unknowns and hence can be subtracted directly for debiasing purposes.''",
    "evidence": "The evidence is a check of the pages against Section 2 and the statements of Theorems 3.1, 3.2 and 4.2. With the transposes restored, the inverse terms on p.~1516 cancel:\n\\[\n-(\\bar x_T-\\bar x_C)'\\widehat L^{-1}\\hat N-(\\bar x_C-\\bar x_T)'\\bigl(\\widehat L^{-1}-I_d^{-1}\\bigr)\\hat N=-(\\bar x_T-\\bar x_C)'\\hat N.\n\\]\nFurther, $\\overline{y(0)}_C-\\bar x_C'N=n_C^{-1}\\sum_{i\\in[C]}(y_i(0)-x_i'N)$.",
    "problem": "Since the covariates $x_i$ are column vectors (Section 2), each of these scalar adjustments needs the transpose of the covariate mean. The same expressions carry it in Theorems 3.1, 3.2 and 4.2. In the second equality on p.~1516, the sum with factor $1/n_C$ expands $\\overline{y(0)}_C-\\bar x_C'N$ and must run over the control group. Remark 2 refers to the component $\\nu_2$ that Theorem 3.1 defines immediately above it.",
    "what_survives": "No result changes. The weights in the last display on p.~1518 are a separate misprint, corrected under \\fid{P005-E013}."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E010",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of two sentences with their displays: 'Thus, an unbiased estimator for E[minus x-bar_T prime (nu_1T + nu_2T + nu_3T)] is' with the treated-arm estimator, and 'Similarly, an unbiased estimator for E[x-bar_C prime (nu_1C + nu_2C + nu_3C)] is' with the control-arm estimator. A red box marks L-hat_T inverse in the control-arm display, in the factor (L-hat_T inverse minus I_d inverse) before N-hat_C.",
     "caption": "Proof of Theorem 4.2, p. 1518 (PDF p. 17). The marked inverse in the control-arm estimator carries the subscript $T$; the treated-arm estimator above it is correct.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E012.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T12",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T12"
    },
    {
     "id": "P005-T13",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T13"
    }
   ],
   "headline": "The estimator of the control-arm bias in the proof of Theorem 4.2 should have $\\widehat L_C^{-1}$, not $\\widehat L_T^{-1}$.",
   "id": "P005-E012",
   "location": "Appendix B.4, proof of Theorem 4.2, p. 1518 (PDF p. 17), the display after “Similarly, an unbiased estimator for”",
   "pdf_page": 17,
   "printed_page": "1518",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T12",
    "P005-T13"
   ],
   "text": {
    "as_printed": "``Similarly, an unbiased estimator for $\\mathbb E[\\bar x_C'(\\nu_{1C}+\\nu_{2C}+\\nu_{3C})]$ is\n\\[\n\\frac{n_T}{(n-2)n_C}\\bigl(\\overline{hy(0)}_C-\\bar h_C\\overline{y(0)}_C\\bigr)+\\bar x_C'\\bigl(\\widehat L_{\\hl{T}}^{-1}-I_d^{-1}\\bigr)\\hat N_C.\\text{''}\n\\]",
    "corrected": "``Similarly, an unbiased estimator for $\\mathbb E[\\bar x_C'(\\nu_{1C}+\\nu_{2C}+\\nu_{3C})]$ is\n\\[\n\\frac{n_T}{(n-2)n_C}\\bigl(\\overline{hy(0)}_C-\\bar h_C\\overline{y(0)}_C\\bigr)+\\bar x_C'\\bigl(\\widehat L_{\\hl{C}}^{-1}-I_d^{-1}\\bigr)\\hat N_C.\\text{''}\n\\]",
    "evidence": "The evidence is a check of the page against Theorems 4.1 and 4.2 and an exact counterexample. Let $n=6$, $n_T=2$, $d=1$, $x=\\sqrt{3/20}\\,(-3,-2,-1,0,1,5)$ and $y(0)=(9,4,1,0,1,25)$, with $h_i=x_i^2$. Then $\\bar x=0$ and $\\overline{x^2}=1$, and $\\widehat L_T$ and $\\widehat L_C$ are invertible for each of the 15 assignments. The control-arm term $\\bar x_C'\\widehat\\beta_{I,C}=\\bar x_C'\\widehat L_C^{-1}\\hat N_C$ of $\\widehat{\\mathrm{ATE}}_I$ has mean $31085815448171/17062566567774\\approx1.822$ over the assignments. Since $\\mathbb E[\\bar x_C]=0$, this mean is the bias $\\mathbb E[\\bar x_C'(\\nu_{1C}+\\nu_{2C}+\\nu_{3C})]$ to be estimated. The expression with $\\widehat L_C^{-1}$ has the same mean. The expression as printed has mean $12010469/846720\\approx14.185$.",
    "problem": "The display is the control-arm analogue of the treated-arm estimator printed above it. By Theorem 4.1, $\\nu_{2C}=(\\widehat L_C^{-1}-I_d^{-1})\\hat N_C$, so the term that is subtracted directly must use the control-arm matrix $\\widehat L_C$. With $\\widehat L_T^{-1}$ the expression differs from the intended one by $\\bar x_C'(\\widehat L_T^{-1}-\\widehat L_C^{-1})\\hat N_C$. Since the expectation of this difference need not vanish, the expression as printed is not in general unbiased.",
    "what_survives": "Theorem 4.2 prints $\\widehat L_C^{-1}$ in the control-arm term and is unaffected, as is the definition of $\\nu_{2C}$ in Theorem 4.1. Only this display of the proof changes."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E012",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "page_check",
   "exhibits": [
    {
     "alt": "Crop of three lines of text on page 1505, followed by equation (1), Y_i ~ alpha + tau D_i + x_i' beta. The third line reads 'results from a OLS regression:'. A red box marks the words 'a OLS'.",
     "caption": "p. 1505 (PDF p. 4), the sentence before equation (1). The marked words are “a OLS”.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E014.png"
    },
    {
     "alt": "Crop from page 1509. It shows the display for the interacted estimator, the sentence 'for the interacted case, where beta-hat I,T and beta-hat I,C are the OLS coefficients on covariates D_i x_i and x_i, repsectively.', and the first three lines of Theorem 4.1. A red box marks the word 'repsectively'.",
     "caption": "p. 1509 (PDF p. 8), Section 4, the sentence after the display for $\\widehat{\\mathrm{ATE}}_I$. The marked word is “repsectively”.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E014-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "Read “an OLS regression” on p. 1505 and “respectively” on p. 1509.",
   "id": "P005-E014",
   "location": "p. 1505 (PDF p. 4), the sentence before equation (1); p. 1509 (PDF p. 8), Section 4, the sentence after the display for $\\widehat{\\mathrm{ATE}}_I$",
   "pdf_page": 4,
   "printed_page": "1505",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [],
   "text": {
    "as_printed": "p.~1505: ``The first estimator results from \\hl{a} OLS regression:''\n\np.~1509: ``for the interacted case, where $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$ are the OLS coefficients on covariates $D_ix_i$ and $x_i$, \\hl{repsectively}.''",
    "corrected": "p.~1505: ``The first estimator results from \\hl{an} OLS regression:''\n\np.~1509: ``\\ldots\\ on covariates $D_ix_i$ and $x_i$, \\hl{respectively}.''",
    "evidence": "The evidence is a check of the two pages.",
    "problem": "The indefinite article before ``OLS'' should be ``an'', and ``repsectively'' is a misspelling of ``respectively''.",
    "what_survives": "Nothing else changes. The description of the two coefficients in the second sentence is the subject of \\fid{P005-E004}."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E014",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of the sentence 'We can characterize the stochastic expansion for the debiased estimator of the treated group as' and the three-line display for the treated-arm debiased estimator. Red boxes mark the fraction n_T over (n minus 2) n_C in front of the treated-arm covariance of h and y(1), once in the first line and once in the second line.",
     "caption": "Proof of Theorem 4.2, p. 1518 (PDF p. 17), last display. The two marked weights have $n_T$ over $n_C$; the weight derived two displays earlier on the same page, and stated in Theorem 4.2, is $n_C/((n-2)n_T)$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-E013.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T10",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T10"
    },
    {
     "id": "P005-T11",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T11"
    }
   ],
   "headline": "In the final expansion of the treated-arm debiased estimator, the weight on the treated-arm covariance should be $n_C/((n-2)n_T)$, not $n_T/((n-2)n_C)$.",
   "id": "P005-E013",
   "location": "Appendix B.4, proof of Theorem 4.2, p. 1518 (PDF p. 17), last display, first and second lines",
   "pdf_page": 17,
   "printed_page": "1518",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T10",
    "P005-T11"
   ],
   "text": {
    "as_printed": "\\[\n\\begin{aligned}\n\\widehat{\\mathrm{ATE}}_{T,I,\\mathrm{Debiased}}&=\\overline{y(1)}_T-\\bar x_T\\widehat L_T^{-1}\\hat N_T-\\Bigl(-\\bar x_T'\\bigl(\\widehat L_T^{-1}-I_d^{-1}\\bigr)\\hat N_T-\\hl{\\frac{n_T}{(n-2)n_C}}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\Bigr)\\\\\n&=\\overline{y(1)}_T-\\bar x_TN_T-\\bar x_T(\\hat N_T-N_T)+\\hl{\\frac{n_T}{(n-2)n_C}}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\\\\n&=\\overline{y(1)}_T-\\bar x_TN_T+O_p\\Bigl(\\sqrt{\\frac\\kappa n}\\Bigr),\n\\end{aligned}\n\\]\nTwo displays earlier on the same page: ``Collecting the constants in front of $(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T)$ gives\n\\[\n\\frac{n_C}{n(n_T-1)}-\\frac{(n-n_T)(n-2n_T)}{(n-1)(n-2)n_T^2}\\times\\frac{n_T(n-1)}{(n_T-1)n}=\\frac{n_C}{(n-2)n_T}.\\text{''}\n\\]",
    "corrected": "With the weight restored, and with the transposes of \\fid{P005-E010}:\n\\[\n\\begin{aligned}\n\\widehat{\\mathrm{ATE}}_{T,I,\\mathrm{Debiased}}&=\\overline{y(1)}_T-\\bar x_T'\\widehat L_T^{-1}\\hat N_T-\\Bigl(-\\bar x_T'\\bigl(\\widehat L_T^{-1}-I_d^{-1}\\bigr)\\hat N_T-\\hl{\\frac{n_C}{(n-2)n_T}}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\Bigr)\\\\\n&=\\overline{y(1)}_T-\\bar x_T'N_T-\\bar x_T'(\\hat N_T-N_T)+\\hl{\\frac{n_C}{(n-2)n_T}}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr)\\\\\n&=\\overline{y(1)}_T-\\bar x_T'N_T+O_p\\Bigl(\\sqrt{\\frac\\kappa n}\\Bigr).\n\\end{aligned}\n\\]\nAfter the cancellation, the treated component is\n\\[\n\\overline{y(1)}_T-\\bar x_T'\\hat N_T+\\frac{n_C}{(n-2)n_T}\\bigl(\\overline{hy(1)}_T-\\bar h_T\\overline{y(1)}_T\\bigr),\\qquad\\hat N_T=\\overline{y(1)x}_T-\\overline{y(1)}_T\\bar x_T.\n\\]",
    "evidence": "The evidence is a recalculation and an exact counterexample. With $N_{\\mathrm{TTT}}$ as defined on p.~1510, the coefficient collected on p.~1518 is\n\\[\n\\frac{n_C}{n(n_T-1)}-N_{\\mathrm{TTT}}\\frac{n_T(n-1)}{(n_T-1)n}=\\frac{n_C}{n(n_T-1)}\\Bigl(1-\\frac{n_C-n_T}{(n-2)n_T}\\Bigr)=\\frac{n_C}{(n-2)n_T}.\n\\]\nFor the counterexample, let $n=6$, $n_T=2$, $d=1$, $x=\\sqrt{3/20}\\,(-3,-2,-1,0,1,5)$, $y(1)=(9,4,1,0,1,25)$ and $y(0)=0$, with $h_i=x_i^2$. Over the 15 assignments, the second line of the display has mean $4913/1200\\approx4.094$ with the printed weight $1/8$, and mean $20/3$ with the weight $1/2$ derived on the page. The population mean $\\overline{y(1)}$ is $20/3$.",
    "problem": "The display expands the debiased estimator for the treated arm by subtracting the bias estimator derived just above it, whose covariance weight is $n_C/((n-2)n_T)$. Both lines print the weight with $n_T$ and $n_C$ interchanged. The two weights agree only when $n_T=n_C$. In an unbalanced design the expression as printed is not unbiased for $\\overline{y(1)}$.",
    "what_survives": "Theorem 4.2 states the correct weight, and the coefficient derived two displays earlier is correct. Only the two repetitions of the weight in this display change. The same display also lacks four transposes, listed under \\fid{P005-E010}."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-E013",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "clarity_note",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "complete_derivation",
   "exhibits": [
    {
     "alt": "Crop of Assumption 1 on page 1505. The first line reads 'Assumption 1: For all n, there exists a finite constant K such that'. Three displayed bounds follow, each an average of squares that is at most K, and then the line 'for all k = 1, ..., d and d <= n.' A red box marks the words 'For all n, there exists a finite constant K'.",
     "caption": "Assumption 1, p. 1505 (PDF p. 4). The marked words give the order of the quantifiers.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N002.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "In Assumption 1 the constant $K$ is one bound for all $n$; the printed order of the quantifiers lets it depend on $n$.",
   "id": "P005-N002",
   "location": "Assumption 1, p. 1505 (PDF p. 4), opening words",
   "pdf_page": 4,
   "printed_page": "1505",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": null,
   "subject": "paper",
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   "text": {
    "as_printed": "``ASSUMPTION 1: \\hl{For all $n$, there exists a finite constant $K$} such that\n\\[\n\\frac1n\\sum_{i=1}^n y_i(1)^2\\le K,\\qquad \\frac1n\\sum_{i=1}^n y_i(0)^2\\le K,\\qquad \\frac1n\\sum_{i=1}^n x_{ik}^2\\le K,\n\\]\nfor all $k=1,\\ldots,d$ and $d\\le n$.''",
    "corrected": "``ASSUMPTION 1: \\hl{There exists a finite constant $K$ such that, for all $n$,}\n\\[\n\\frac1n\\sum_{i=1}^n y_i(1)^2\\le K,\\qquad \\frac1n\\sum_{i=1}^n y_i(0)^2\\le K,\\qquad \\frac1n\\sum_{i=1}^n x_{ik}^2\\le K,\n\\]\nfor all $k=1,\\ldots,d$ and $d\\le n$.''",
    "intended_meaning": "The intended statement is that there exists a single finite constant $K$ that bounds the three second moments for every $n$. This is the standard form of the assumption and the form that the proofs use. For example, the bounds $n^{-1}\\sum_{i=1}^n e_i^2(1)=O(1)$ and $n^{-1}\\sum_{i=1}^n e_i^2(0)=O(1)$ on p.~1513 need it. Read literally, the printed order lets $K$ depend on $n$, and the condition then holds for every sequence of finite populations. For instance, let $n=4m$, and let the population consist of the four units with $x=(-1,-1,1,1)$ and $q=(-1,1,-1,1)$, repeated $m$ times, with $y(1)=nq$, $y(0)=0$ and $p_T=1/2$. Assumptions 2 and 3 hold, the printed Assumption 1 holds with $K=n^2$, and the second moment of the residuals $e_i(1)$ is $n^2$. Assumption 3, on the same page, places its constants before the words ``for all $n$''. The asymptotic arguments of the paper are made under the uniform bound. The finite-sample identities for the bias and for unbiasedness do not need a bound that is uniform in $n$."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-N002",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "exact_counterexample",
   "exhibits": [
    {
     "alt": "Crop of the top of page 1510. The first line reads 'If kappa log d = o(1),' with the footnote mark 8. The display below gives ATE-hat_I as ATE plus the treated-arm average of y_i(1) minus its mean minus x_i' beta_{I,T}, minus the corresponding control-arm average, and its second line is 'plus O_p of the square root of kappa d over n'. Red boxes mark the condition 'kappa log d = o(1)' and the remainder term.",
     "caption": "Theorem 4.1, continued, p. 1510 (PDF p. 9). The marked terms are the condition $\\kappa\\log d=o(1)$ and the remainder $O_p(\\sqrt{\\kappa d/n})$.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N004.png"
    },
    {
     "alt": "Crop of section B.3, Proof of Theorem 4.1, on page 1517. The section has three sentences: 'The decomposition of the bias is similar to the one in Theorem 3.1. We omit the details. The stochastic order of the bias is derived in Lei and Ding (2021).' A red box marks the last sentence.",
     "caption": "Appendix B.3, p. 1517 (PDF p. 16): the proof of Theorem 4.1 in full. The marked sentence refers the stochastic order to Lei and Ding (2021).",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N004-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T9",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T9"
    }
   ],
   "headline": "The expansion of Theorem 4.1, which the paper cites from Lei and Ding (2021) without proof, holds with the stated remainder for $d\\ge2$ under the printed condition, and for $d=1$ only if $\\kappa=o(1)$ is added.",
   "id": "P005-N004",
   "location": "Theorem 4.1, p. 1510 (PDF p. 9), the expansion with remainder $O_p(\\sqrt{\\kappa d/n})$ and footnote 8; its proof, Appendix B.3, p. 1517 (PDF p. 16)",
   "pdf_page": 9,
   "printed_page": "1510",
   "reaches": [],
   "related_entries": [],
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   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T9"
   ],
   "text": {
    "as_printed": "Theorem 4.1, p.~1510: ``If $\\kappa\\hl{\\log d}=o(1)$,'' with footnote 8 attached, followed by the display\n\\[\n\\widehat{\\mathrm{ATE}}_I=\\mathrm{ATE}+\\frac{1}{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-\\overline{y(1)}-x_i'\\beta_{I,T}\\bigr)-\\frac{1}{n_C}\\sum_{i\\in[C]}\\bigl(y_i(0)-\\overline{y(0)}-x_i'\\beta_{I,C}\\bigr)+O_p\\Bigl(\\sqrt{\\frac{\\kappa d}{n}}\\Bigr).\n\\]\nFootnote 8: ``The upper bound on the stochastic order of the bias of the interacted case is characterized in equation (15) in Lei and Ding (2021).''\n\nAppendix B.3, p.~1517: ``The decomposition of the bias is similar to the one in Theorem 3.1. We omit the details. The stochastic order of the bias is derived in Lei and Ding (2021).''",
    "corrected": "Theorem 4.1, last paragraph. Let Assumptions 1--3 hold, and let all design matrices be invertible, as footnote 4 assumes. If $\\kappa\\hl{\\log\\max\\{d,2\\}}=o(1)$, then\n\\[\n\\widehat{\\mathrm{ATE}}_I=\\mathrm{ATE}+\\frac{1}{n_T}\\sum_{i\\in[T]}\\bigl(y_i(1)-\\overline{y(1)}-x_i'\\beta_{I,T}\\bigr)-\\frac{1}{n_C}\\sum_{i\\in[C]}\\bigl(y_i(0)-\\overline{y(0)}-x_i'\\beta_{I,C}\\bigr)+O_p\\Bigl(\\sqrt{\\frac{\\kappa d}{n}}\\Bigr).\n\\]\nThis is the statement given under \\fid{P005-E001}. The condition $\\kappa\\log(2d)=o(1)$, under which the derivation above is written, is equivalent to it: both reduce to the printed condition for $d\\ge2$ and to $\\kappa=o(1)$ for $d=1$. The reference to Lei and Ding (2021) in Appendix B.3 and in footnote 8 can stay, with the condition as corrected.",
    "evidence": "The evidence is a derivation and an exact counterexample. For the derivation, suppose that Assumptions 1--3 hold and that $\\kappa\\log(2d)=o(1)$. Let $S$ be an arm of size $m$, and define $G_S=m^{-1}\\sum_{i\\in S}x_ix_i'$. Note that $0\\preceq x_ix_i'\\preceq n\\kappa I_d$ and $\\overline{xx'}=I_d$. By a Chernoff bound for sums of positive semidefinite matrices, which also holds for sampling without replacement, I have\n\\[\nP\\bigl\\{\\lambda_{\\min}(G_S)\\le\\tfrac12\\bigr\\}\\le d\\exp\\Bigl(-\\frac{m/n}{8\\kappa}\\Bigr),\n\\]\nand the right-hand side tends to zero, because $\\kappa\\log(2d)=o(1)$ and $m/n$ is bounded below by Assumption 3. Since $E\\|\\bar x_S\\|^2=O(d/n)$ and $d/n\\le\\kappa$, I have $\\widehat L_S=G_S-\\bar x_S\\bar x_S'\\succeq I_d/4$ with probability tending to one. Let $y$ be the potential outcome of the arm, $\\beta=\\overline{xy}$ and $e_i=y_i-\\bar y-x_i'\\beta$, so that $\\bar e=0$, $\\overline{xe}=0$ and $\\overline{e^2}\\le K$. The fitted intercept of the arm is\n\\[\n\\bar y+\\bar e_S-\\bar x_S'\\widehat L_S^{-1}\\bigl(\\overline{xe}_S-\\bar x_S\\bar e_S\\bigr),\n\\]\nwith $\\|\\bar x_S\\|=O_p(\\sqrt{d/n})$, $\\bar e_S=O_p(n^{-1/2})$ and $\\|\\overline{xe}_S\\|=O_p(\\sqrt\\kappa)$. The last term is $O_p(\\sqrt{\\kappa d/n})+O_p(d/n^{3/2})=O_p(\\sqrt{\\kappa d/n})$. Since $\\widehat{\\mathrm{ATE}}_I$ is the difference of the two fitted intercepts, I obtain the expansion. For $d\\ge2$, the inequality $\\log(2d)\\le2\\log d$ shows that the printed condition suffices.\n\nThe counterexample for $d=1$ is a second sequence, different from the one in \\fid{P005-E001}. Let $r=2,4,6,\\ldots$, $n=r^2+1$ and $\\ell=(n-1)/2$. One unit has the covariate value $n-1$ before scaling and both potential outcomes equal to $0$. The other $2\\ell$ units have the labels $t_i\\in\\{\\pm1/\\ell,\\pm2/\\ell,\\ldots,\\pm1\\}$, the covariate values $-1+\\epsilon t_i$ before scaling and the potential outcomes $y_i(1)=y_i(0)=t_i$. Here $\\epsilon=2rn^{-3}/(1-qn^{-6})$ with $q=(\\ell+1)(2\\ell+1)/(3n\\ell)$, so that $\\epsilon$ is asymptotic to $2n^{-5/2}$. The arm sizes are $n_T=\\ell$ and $n_C=\\ell+1$. Assumptions 1--3 hold with $K=1$, every regression is invertible, and $\\kappa\\to1$. Under every assignment the remainder satisfies $|R_n|\\ge1/\\epsilon-6$. At $n=5$, where $\\epsilon=1000/31249$, the bound is $25249/1000$, and enumeration of the 10 assignments agrees. At $n=17$ the bound is $191213957/314432$, and enumeration of the 24,310 assignments agrees.\n\nThe identities and inequalities that the proofs take from the other cited results were derived directly: the mean and the variance of the quadratic forms under sampling without replacement that are used on pp.~1511, 1514 and 1517, the mean identities behind equation (5), and the leverage inequality on p.~1517. I did not compare these with the cited papers, and I do not confirm the wording or the numbering of the cited results.",
    "problem": "The paper gives no proof of this expansion. Appendix B.3 omits the details and refers to Lei and Ding (2021), and footnote 8 does the same. The question is whether the cited order holds under Assumptions 1--3 with the condition $\\kappa\\log d=o(1)$. It holds for $d\\ge2$. It does not hold for $d=1$, where the condition is empty. This is the defect described in \\fid{P005-E001}, and it is the only failure of this expansion that I found. The proofs also rely on results from other papers: Lemma A.5 and (B.6) of Lei and Ding (2021), Proposition 1 of Freedman (2008b) and Proposition 1 of Wu and Ding (2021). I found no failure in the use of these.",
    "what_survives": "The algebraic decomposition of the bias in Theorem 4.1, the expansion for $d\\ge2$ under the printed condition, and the exact unbiasedness of the two corrections are unaffected. The asymptotic statements for the debiased estimators already assume $\\kappa=o(1)$, which excludes the example. What changes is the condition for $d=1$, as in \\fid{P005-E001}. This entry adds no second error."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-N004",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "complete_derivation",
   "exhibits": [
    {
     "alt": "Crop of the sentence 'We bound the stochastic order of (*):' and the three-line display below it. Each line is one over p_C times x-bar_T prime times a bracketed sum over the treated group. A red box marks the small closing parenthesis at the very end of the second line, after the two large closing parentheses.",
     "caption": "Appendix B.1.1, p. 1514 (PDF p. 13), the three-line display that rewrites the term $(*)$. The marked parenthesis at the end of the second line closes nothing.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N005.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [
    {
     "id": "P005-T18",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T18"
    }
   ],
   "headline": "The second line of the display that rewrites the term $(*)$ has one closing parenthesis too many.",
   "id": "P005-N005",
   "location": "Appendix B.1.1, p. 1514 (PDF p. 13), first display, second line",
   "pdf_page": 13,
   "printed_page": "1514",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [
    "P005-T18"
   ],
   "text": {
    "as_printed": "\\[\n=\\frac1{p_C}\\bar x_T'\\Bigl(\\frac1n\\sum_{i\\in[T]}\\Bigl(x_i\\bigl(e_i(1)-e_i(0)\\bigr)+\\frac1{p_T}\\frac1n\\sum_{i=1}^nx_ie_i(0)\\Bigr)\\Bigr)\\hl{)}\n\\]",
    "corrected": "The second line, with its last parenthesis deleted:\n\\[\n=\\frac1{p_C}\\bar x_T'\\Bigl(\\frac1n\\sum_{i\\in[T]}\\Bigl(x_i\\bigl(e_i(1)-e_i(0)\\bigr)+\\frac1{p_T}\\frac1n\\sum_{i=1}^nx_ie_i(0)\\Bigr)\\Bigr)\\del{)}\n\\]",
    "evidence": "The evidence is a check of the page and a derivation. Let $\\delta_i=e_i(1)-e_i(0)$, $A=n^{-1}\\sum_{i=1}^nx_i\\delta_i$, $B=n^{-1}\\sum_{i=1}^nx_ie_i(0)$ and $U=n^{-1}\\sum_{i\\in[T]}x_i\\delta_i$. The relation $p_T\\sum_ix_ie_i(1)+p_C\\sum_ix_ie_i(0)=0$, quoted below the display, gives $B=-p_TA$. The three bracketed expressions are $U+B$, $n^{-1}\\sum_{i\\in[T]}(x_i\\delta_i+B/p_T)$ and $n^{-1}\\sum_{i\\in[T]}(x_i\\delta_i-A)$. The last two equal $U+B$ because $n_T/n=p_T$.",
    "problem": "The line closes one parenthesis more than it opens. Nothing else in the display is wrong. On the second and third lines the population average stands inside the parenthesis that opens after the sum over $i\\in[T]$. It is added $n_T$ times and multiplied by $1/n$, which supplies the factor $p_T$.",
    "what_survives": "The algebra for $(*)$, its expectation and its stated order are unchanged, and no factor needs to be added."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-N005",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "page_check",
   "exhibits": [
    {
     "alt": "Crop of the running head of page 1519 and the two lines that end the proof of Theorem 4.2: 'using the stochastic order estimates we derived in the proof of Theorem 4.1 and the fact that kappa is in [d/n, 1].' A red box marks 'Theorem 4.1'.",
     "caption": "End of the proof of Theorem 4.2, first line of p. 1519 (PDF p. 18). The marked reference points to Theorem 4.1, whose proof derives no stochastic order estimates.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N007.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "The stochastic order estimates used at the end of the proof of Theorem 4.2 are derived in the proof of Theorem 3.2, not of Theorem 4.1.",
   "id": "P005-N007",
   "location": "Appendix B.4, end of the proof of Theorem 4.2, first line of p. 1519 (PDF p. 18)",
   "pdf_page": 18,
   "printed_page": "1519",
   "reaches": [],
   "related_entries": [],
   "revisions": [],
   "same_defect_as": [],
   "severity": "Minor",
   "subject": "paper",
   "target_ids": [],
   "text": {
    "as_printed": "``using the stochastic order estimates we derived in the proof of \\hl{Theorem 4.1} and the fact that $\\kappa\\in[\\frac dn,1]$.''",
    "corrected": "``using the stochastic order estimates we derived in the proof of \\hl{Theorem 3.2} and the fact that $\\kappa\\in[\\frac dn,1]$.''",
    "evidence": "The evidence is a check of pp.~1516--1519.",
    "problem": "The proof of Theorem 4.1 (Appendix B.3, p.~1517) is three sentences long. It omits the details and refers to Lei and Ding (2021) for the stochastic order of the bias; it derives no estimates. The estimates used here are items 1--3 of the proof of Theorem 3.2 (Appendix B.2, pp.~1516--1517).",
    "what_survives": "The estimates and the step that uses them are unaffected, and only the reference changes."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-N007",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  },
  {
   "before_review": null,
   "class": "error",
   "date_modified": "2026-10-25",
   "date_published": "2026-10-25",
   "evidence_type": "page_check",
   "exhibits": [
    {
     "alt": "Crop of three entries of the reference list: Tan (2014), the entry 'Tibshirani, Robert J., and Bradley Efron (1993): An Introduction to the Bootstrap, Monographs on statistics and applied probability, 57, 1-436. [1504]', and White (1980). A red box marks the author heading 'Tibshirani, Robert J., and Bradley Efron'.",
     "caption": "Reference list, p. 1519 (PDF p. 18). The marked heading gives Tibshirani before Efron; the entry stands between Tan and White.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N008.png"
    },
    {
     "alt": "Crop of four lines of the Introduction, at the start of the paragraph on the practice of debiasing estimators. A red box marks the citation 'Tibshirani and Efron (1993)' in the sentence 'Tibshirani and Efron (1993) have warned that the bias correction could have costs in practice due to its high variability in finite samples.'",
     "caption": "Introduction, p. 1504 (PDF p. 3). The marked citation gives the two authors in the same reversed order.",
     "url": "https://pmaronow.github.io/llm-audit/works/P005/exhibits/P005-N008-b.png"
    }
   ],
   "formal_release": null,
   "formal_statements": [],
   "headline": "The authors of An Introduction to the Bootstrap are Efron and Tibshirani, in that order; the citation and the reference entry reverse them.",
   "id": "P005-N008",
   "location": "References, p. 1519 (PDF p. 18), the entry for An Introduction to the Bootstrap; cited in the Introduction, p. 1504 (PDF p. 3)",
   "pdf_page": 18,
   "printed_page": "1519",
   "reaches": [],
   "related_entries": [],
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   "severity": "Minor",
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    "as_printed": "P.~1519, reference list: \\hl{TIBSHIRANI, ROBERT J., AND BRADLEY EFRON} (1993): ``An Introduction to the Bootstrap,'' \\emph{Monographs on statistics and applied probability}, 57, 1--436. [1504]\n\nP.~1504: ``\\hl{Tibshirani and Efron} (1993) have warned that the bias correction could have costs in practice due to its high variability in finite samples.''",
    "corrected": "P.~1519, reference list, between the entries for Deaton and Cartwright (2018) and for Finucan, Galbraith, and Stone (1974): \\hl{EFRON, BRADLEY, AND ROBERT J. TIBSHIRANI} (1993): ``An Introduction to the Bootstrap,'' \\emph{Monographs on statistics and applied probability}, 57, 1--436. [1504]\n\nP.~1504: ``\\hl{Efron and Tibshirani} (1993) have warned that the bias correction could have costs in practice due to its high variability in finite samples.''",
    "evidence": "The evidence is a check of pp.~1504 and 1519 and the WorldCat catalogue listing of the book (OCLC 481704221), which gives Bradley Efron before Robert J. Tibshirani. I read the listing at \\url{https://search.worldcat.org/title/An-introduction-to-the-bootstrap/oclc/481704221}. The catalogue does not show whether the book contains the warning that the Introduction attributes to it; I did not check that.",
    "problem": "The book \\emph{An Introduction to the Bootstrap} (Chapman \\& Hall, 1993, Monographs on Statistics and Applied Probability 57) is by Bradley Efron and Robert J. Tibshirani, in that order. The reference entry and the citation in the Introduction give the two authors in the reverse order. With the order corrected, the entry belongs between Deaton and Finucan in the alphabetical list.",
    "what_survives": "The book is identified by its title and year, and nothing in the argument depends on the order of its authors. Only the citation and the reference list change."
   },
   "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-N008",
   "work": {
    "arxiv_id": "2110.08425",
    "doi": "10.3982/ECTA20289",
    "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
    "url": "https://pmaronow.github.io/llm-audit/works/P005/"
   },
   "work_id": "P005"
  }
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     "body": "<p>Appendix A.2, Lemma A.1, pp. 1510–1511 (PDF pp. 9–10). The six-unit counterexample has all the stated means, coefficients, moments, expectation, variance, bound and positive gap. Covariance and its variance are unchanged by constant shifts; the printed bound changes under centering, and its centered value bounds the variance.</p>",
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     "body": "Appendix A.2, Lemma A.1, pp. 1510–1511 (PDF pp. 9–10). The six-unit counterexample has all the stated means, coefficients, moments, expectation, variance, bound and positive gap. Covariance and its variance are unchanged by constant shifts; the printed bound changes under centering, and its centered value bounds the variance.",
     "headline": "Lemma A.1, the variance bound, as printed for arbitrary $n$-vectors $a$, $b$. The witness is the validator's and is not in the paper",
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     "body": "<p>Appendix A.2, Lemma A.1, p. 1511 (PDF p. 10). For either nonempty arm, the printed expectation and the variance bound with both vectors centered hold. Covariance is location invariant, the centered sample-product mean has the simple-random-sampling variance, the product of centered sums has the stated exact expectation and variance and their bound, and the generic variance-difference inequality gives the repaired bound. The printed bound is recovered when both population means are zero.</p>",
     "headline": "Lemma A.1, as repaired: the variance bound with centred vectors (Sol&#x27;s smallest repair and the validator&#x27;s derivation)",
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     "body": "Appendix A.2, Lemma A.1, p. 1511 (PDF p. 10). For either nonempty arm, the printed expectation and the variance bound with both vectors centered hold. Covariance is location invariant, the centered sample-product mean has the simple-random-sampling variance, the product of centered sums has the stated exact expectation and variance and their bound, and the generic variance-difference inequality gives the repaired bound. The printed bound is recovered when both population means are zero.",
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     "body": "<p>Appendix B.2, item 2, p. 1517 (PDF p. 16). The standardized regular sixteen-unit counterexample satisfies all stated moment and allocation conditions. Its leverage vector, mean and constant leverage-product, three-category probabilities and covariance values, exact variance, both failed bounds and positive gaps, and the valid third-expression and centered-bound comparisons have the stated numerical values.</p>",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), item 2: the chain “First notice, by Lemma A.1 and Assumption 1, …”, as printed. The witness is the validator&#x27;s and is not in the paper",
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     "body": "Appendix B.2, item 2, p. 1517 (PDF p. 16). The standardized regular sixteen-unit counterexample satisfies all stated moment and allocation conditions. Its leverage vector, mean and constant leverage-product, three-category probabilities and covariance values, exact variance, both failed bounds and positive gaps, and the valid third-expression and centered-bound comparisons have the stated numerical values.",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), item 2: the chain “First notice, by Lemma A.1 and Assumption 1, …”, as printed. The witness is the validator's and is not in the paper",
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     "body": "<p>Appendix B.2, item 2, p. 1517 (PDF p. 16). For either arm the centered leverage and outcome moments give every inequality in the repaired finite variance chain, including the intermediate raw leverage second moment. The two allocation coefficients obey the stated bounds. Under Assumptions 1–3 the numerical right-hand side and the actual variance are O(nκ²+κd/n), and the variance after division by n is O(κ²/n+κd/n³). Dimension zero is allowed, including along a sequence.</p>",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), item 2, as repaired: the variance chain with <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>h</mi></mrow><annotation encoding=\"application/x-tex\">h</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.6944em;\"></span><span class=\"mord mathnormal\">h</span></span></span></span> and <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>y</mi><mo stretchy=\"false\">(</mo><mn>1</mn><mo stretchy=\"false\">)</mo></mrow><annotation encoding=\"application/x-tex\">y(1)</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0359em;\">y</span><span class=\"mopen\">(</span><span class=\"mord\">1</span><span class=\"mclose\">)</span></span></span></span> centred (Sol&#x27;s smallest repair and the validator&#x27;s derivation)",
     "location": "p. 1517 (PDF p. 16), Appendix B.2, item 2"
    },
    "id": "P005-T4",
    "text": {
     "body": "Appendix B.2, item 2, p. 1517 (PDF p. 16). For either arm the centered leverage and outcome moments give every inequality in the repaired finite variance chain, including the intermediate raw leverage second moment. The two allocation coefficients obey the stated bounds. Under Assumptions 1–3 the numerical right-hand side and the actual variance are O(nκ²+κd/n), and the variance after division by n is O(κ²/n+κd/n³). Dimension zero is allowed, including along a sequence.",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), item 2, as repaired: the variance chain with $h$ and $y(1)$ centred (Sol's smallest repair and the validator's derivation)",
     "location": "p. 1517 (PDF p. 16), Appendix B.2, item 2"
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     "body": "<p>Theorem 4.1, last display, p. 1509 (PDF p. 8). The printed claim is false: the specified six-unit population satisfies the finite-sample assumptions, has positive variances under all fifteen assignments, and gives 217/2500 for the third bias component while the printed formula gives -217/2500. All individual means, moments, coefficients and expectations are included; reversing both printed signs gives the actual component.</p>",
     "headline": "Theorem 4.1, last display on p. 1509 (the third bias component <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>E</mi><mo stretchy=\"false\">[</mo><msubsup><mover accent=\"true\"><mi>x</mi><mo>ˉ</mo></mover><mi>C</mi><mo mathvariant=\"normal\" lspace=\"0em\" rspace=\"0em\">′</mo></msubsup><msub><mi>ν</mi><mrow><mn>3</mn><mi>C</mi></mrow></msub><mo stretchy=\"false\">]</mo><mo>−</mo><mi>E</mi><mo stretchy=\"false\">[</mo><msubsup><mover accent=\"true\"><mi>x</mi><mo>ˉ</mo></mover><mi>T</mi><mo mathvariant=\"normal\" lspace=\"0em\" rspace=\"0em\">′</mo></msubsup><msub><mi>ν</mi><mrow><mn>3</mn><mi>T</mi></mrow></msub><mo stretchy=\"false\">]</mo></mrow><annotation encoding=\"application/x-tex\">E[\\bar x_C&#x27;\\nu_{3C}] - E[\\bar x_T&#x27;\\nu_{3T}]</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0272em;vertical-align:-0.2753em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0576em;\">E</span><span class=\"mopen\">[</span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.5678em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">x</span></span><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"accent-body\" style=\"left:-0.2222em;\"><span class=\"mord\">ˉ</span></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.7519em;\"><span style=\"top:-2.4247em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span><span style=\"top:-3.063em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">′</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2753em;\"><span></span></span></span></span></span></span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0637em;\">ν</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0637em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">3</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mclose\">]</span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span><span class=\"mbin\">−</span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0272em;vertical-align:-0.2753em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0576em;\">E</span><span class=\"mopen\">[</span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.5678em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">x</span></span><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"accent-body\" style=\"left:-0.2222em;\"><span class=\"mord\">ˉ</span></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.7519em;\"><span style=\"top:-2.4247em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span><span style=\"top:-3.063em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">′</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2753em;\"><span></span></span></span></span></span></span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0637em;\">ν</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0637em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">3</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mclose\">]</span></span></span></span>), as printed. The witness is the validator&#x27;s and is not in the paper",
     "location": "p. 1509 (PDF p. 8), Section 4, Theorem 4.1, last display on the page"
    },
    "id": "P005-T5",
    "text": {
     "body": "Theorem 4.1, last display, p. 1509 (PDF p. 8). The printed claim is false: the specified six-unit population satisfies the finite-sample assumptions, has positive variances under all fifteen assignments, and gives 217/2500 for the third bias component while the printed formula gives -217/2500. All individual means, moments, coefficients and expectations are included; reversing both printed signs gives the actual component.",
     "headline": "Theorem 4.1, last display on p. 1509 (the third bias component $E[\\bar x_C'\\nu_{3C}] - E[\\bar x_T'\\nu_{3T}]$), as printed. The witness is the validator's and is not in the paper",
     "location": "p. 1509 (PDF p. 8), Section 4, Theorem 4.1, last display on the page"
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     "body": "<p>Theorem 4.1, last display, p. 1509 (PDF p. 8). For centered covariates, both third-moment identities, their signed bias components and the corrected control-minus-treatment formula hold exactly.</p>",
     "headline": "Theorem 4.1, last display on p. 1509, as repaired: both signs of the right-hand side reversed (Sol&#x27;s smallest repair)",
     "location": "p. 1509 (PDF p. 8), Section 4, Theorem 4.1, last display on the page"
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    "text": {
     "body": "Theorem 4.1, last display, p. 1509 (PDF p. 8). For centered covariates, both third-moment identities, their signed bias components and the corrected control-minus-treatment formula hold exactly.",
     "headline": "Theorem 4.1, last display on p. 1509, as repaired: both signs of the right-hand side reversed (Sol's smallest repair)",
     "location": "p. 1509 (PDF p. 8), Section 4, Theorem 4.1, last display on the page"
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     "body": "<p>Theorem 4.1, pp. 1509--1510 (PDF pp. 8--9), footnote 8. The printed claim is false: the explicit one-covariate spike sequence satisfies Assumptions 1--3 and every-assignment regularity, yet its remainder is not of the printed stochastic order. The statement includes all grid identities, pointwise bounds, exact leverage and slopes, fitted-line calculations, sharp bounds, probability-one even-size tails and both exact finite minima.</p>",
     "headline": "Theorem 4.1, final paragraph: the stochastic expansion under “<span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>κ</mi><mi>log</mi><mo>⁡</mo><mi>d</mi><mo>=</mo><mi>o</mi><mo stretchy=\"false\">(</mo><mn>1</mn><mo stretchy=\"false\">)</mo></mrow><annotation encoding=\"application/x-tex\">\\kappa\\log d = o(1)</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.8889em;vertical-align:-0.1944em;\"></span><span class=\"mord mathnormal\">κ</span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mop\">lo<span style=\"margin-right:0.0139em;\">g</span></span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mord mathnormal\">d</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span><span class=\"mrel\">=</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\">o</span><span class=\"mopen\">(</span><span class=\"mord\">1</span><span class=\"mclose\">)</span></span></span></span>”, as printed, at <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>d</mi><mo>=</mo><mn>1</mn></mrow><annotation encoding=\"application/x-tex\">d = 1</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.6944em;\"></span><span class=\"mord mathnormal\">d</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span><span class=\"mrel\">=</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.6444em;\"></span><span class=\"mord\">1</span></span></span></span>. The sequence is the validator&#x27;s and is not in the paper",
     "location": "p. 1510 (PDF p. 9), continuation of Theorem 4.1 (the theorem begins on p. 1509, PDF p. 8), with footnote 8"
    },
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    "text": {
     "body": "Theorem 4.1, pp. 1509--1510 (PDF pp. 8--9), footnote 8. The printed claim is false: the explicit one-covariate spike sequence satisfies Assumptions 1--3 and every-assignment regularity, yet its remainder is not of the printed stochastic order. The statement includes all grid identities, pointwise bounds, exact leverage and slopes, fitted-line calculations, sharp bounds, probability-one even-size tails and both exact finite minima.",
     "headline": "Theorem 4.1, final paragraph: the stochastic expansion under “$\\kappa\\log d = o(1)$”, as printed, at $d = 1$. The sequence is the validator's and is not in the paper",
     "location": "p. 1510 (PDF p. 9), continuation of Theorem 4.1 (the theorem begins on p. 1509, PDF p. 8), with footnote 8"
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     "body": "<p>No current theorem is supplied for this target.</p>",
     "headline": "Theorem 4.1, final paragraph, as repaired: the condition <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>κ</mi><mi>log</mi><mo>⁡</mo><mi>max</mi><mo>⁡</mo><mo stretchy=\"false\">{</mo><mi>d</mi><mo separator=\"true\">,</mo><mn>2</mn><mo stretchy=\"false\">}</mo><mo>=</mo><mi>o</mi><mo stretchy=\"false\">(</mo><mn>1</mn><mo stretchy=\"false\">)</mo></mrow><annotation encoding=\"application/x-tex\">\\kappa\\log\\max\\{d,2\\} = o(1)</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\">κ</span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mop\">lo<span style=\"margin-right:0.0139em;\">g</span></span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mop\">max</span><span class=\"mopen\">{</span><span class=\"mord mathnormal\">d</span><span class=\"mpunct\">,</span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mord\">2</span><span class=\"mclose\">}</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span><span class=\"mrel\">=</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\">o</span><span class=\"mopen\">(</span><span class=\"mord\">1</span><span class=\"mclose\">)</span></span></span></span> (Sol&#x27;s smallest repair for <code class=\"fid\">P005-E001</code>)",
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     "body": "No current theorem is supplied for this target.",
     "headline": "Theorem 4.1, final paragraph, as repaired: the condition $\\kappa\\log\\max\\{d,2\\} = o(1)$ (Sol's smallest repair for P005-E001)",
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     "body": "<p>Theorem 4.1, p. 1510 (PDF p. 9), and Appendix B.3, p. 1517 (PDF p. 16). Under Assumptions 1--3 and every-assignment invertibility, the repaired condition kappa log(2d) tending to zero implies the full interacted expansion with remainder O_p(sqrt(kappa d/n)). The two repaired logarithms have the stated inequalities and equivalent limits. The repaired condition implies vanishing leverage and the printed condition, and is equivalent to the printed condition plus vanishing leverage on the dimension-one subsequence.</p>",
     "headline": "Theorem 4.1, final paragraph, as repaired in the form given by the validator of <code class=\"fid\">P005-N004</code>: the condition <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>κ</mi><mi>log</mi><mo>⁡</mo><mo stretchy=\"false\">(</mo><mn>2</mn><mi>d</mi><mo stretchy=\"false\">)</mo><mo>=</mo><mi>o</mi><mo stretchy=\"false\">(</mo><mn>1</mn><mo stretchy=\"false\">)</mo></mrow><annotation encoding=\"application/x-tex\">\\kappa\\log(2d) = o(1)</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\">κ</span><span class=\"mspace\" style=\"margin-right:0.1667em;\"></span><span class=\"mop\">lo<span style=\"margin-right:0.0139em;\">g</span></span><span class=\"mopen\">(</span><span class=\"mord\">2</span><span class=\"mord mathnormal\">d</span><span class=\"mclose\">)</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span><span class=\"mrel\">=</span><span class=\"mspace\" style=\"margin-right:0.2778em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord mathnormal\">o</span><span class=\"mopen\">(</span><span class=\"mord\">1</span><span class=\"mclose\">)</span></span></span></span>, with its equivalence to the form of <code class=\"fid\">P005-T8</code>",
     "location": "p. 1510 (PDF p. 9), continuation of Theorem 4.1, with footnote 8; proof B.3 on p. 1517 (PDF p. 16)"
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    "id": "P005-T9",
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     "body": "Theorem 4.1, p. 1510 (PDF p. 9), and Appendix B.3, p. 1517 (PDF p. 16). Under Assumptions 1--3 and every-assignment invertibility, the repaired condition kappa log(2d) tending to zero implies the full interacted expansion with remainder O_p(sqrt(kappa d/n)). The two repaired logarithms have the stated inequalities and equivalent limits. The repaired condition implies vanishing leverage and the printed condition, and is equivalent to the printed condition plus vanishing leverage on the dimension-one subsequence.",
     "headline": "Theorem 4.1, final paragraph, as repaired in the form given by the validator of P005-N004: the condition $\\kappa\\log(2d) = o(1)$, with its equivalence to the form of P005-T8",
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    "html": {
     "body": "<p>Appendix B.4, last display, pp. 1518--1519 (PDF pp. 17--18). The printed claim is false: the six-unit standardized regular population has printed treated expectation 4913/1200 instead of 20/3, while the derived weight is unbiased. All fifteen-assignment positivity, leverage, population covariance, assignmentwise and expected gaps, and rational scaling identities are included.</p>",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), last display on p. 1518: the weight <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mfrac><msub><mi>n</mi><mi>T</mi></msub><mrow><mo stretchy=\"false\">(</mo><mi>n</mi><mo>−</mo><mn>2</mn><mo stretchy=\"false\">)</mo><msub><mi>n</mi><mi>C</mi></msub></mrow></mfrac></mrow><annotation encoding=\"application/x-tex\">\\frac{n_T}{(n-2)n_C}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2317em;vertical-align:-0.52em;\"></span><span class=\"mord\"><span class=\"mopen nulldelimiter\"></span><span class=\"mfrac\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.7117em;\"><span style=\"top:-2.655em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mopen mtight\">(</span><span class=\"mord mathnormal mtight\">n</span><span class=\"mbin mtight\">−</span><span class=\"mord mtight\">2</span><span class=\"mclose mtight\">)</span><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\">n</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3448em;\"><span style=\"top:-2.3567em;margin-left:0em;margin-right:0.0714em;\"><span class=\"pstrut\" style=\"height:2.5em;\"></span><span class=\"katex-sizing reset-size3 size1 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1433em;\"><span></span></span></span></span></span></span></span></span></span><span style=\"top:-3.23em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"frac-line\" style=\"border-bottom-width:0.04em;\"></span></span><span style=\"top:-3.4103em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\">n</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3448em;\"><span style=\"top:-2.3567em;margin-left:0em;margin-right:0.0714em;\"><span class=\"pstrut\" style=\"height:2.5em;\"></span><span class=\"katex-sizing reset-size3 size1 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1433em;\"><span></span></span></span></span></span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.52em;\"><span></span></span></span></span></span><span class=\"mclose nulldelimiter\"></span></span></span></span></span> on the treated-arm covariance, as printed. The witness is the validator&#x27;s and is not in the paper",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, last display (it ends on p. 1519, PDF p. 18)"
    },
    "id": "P005-T10",
    "text": {
     "body": "Appendix B.4, last display, pp. 1518--1519 (PDF pp. 17--18). The printed claim is false: the six-unit standardized regular population has printed treated expectation 4913/1200 instead of 20/3, while the derived weight is unbiased. All fifteen-assignment positivity, leverage, population covariance, assignmentwise and expected gaps, and rational scaling identities are included.",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), last display on p. 1518: the weight $\\frac{n_T}{(n-2)n_C}$ on the treated-arm covariance, as printed. The witness is the validator's and is not in the paper",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, last display (it ends on p. 1519, PDF p. 18)"
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      "status": "proved",
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      "status": "proved",
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     "target_id": "P005-T11"
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    "html": {
     "body": "<p>Appendix B.4, corrected last display, pp. 1518--1519 (PDF pp. 17--18). The corrected arm expressions cancel the inverse assignmentwise, have the exact generic expectation, and are unbiased with the derived arm-size weights. The cancelling treated weight equals its unsimplified expression and is unique for arms of size at least two; singleton expectations require no division by s-1. The printed treated weight has the stated bias. Standardization gives d/n &lt;= kappa &lt;= 1 and h_i &lt;= n. Under Assumptions 1--3 both corrected arm remainders are O_p(sqrt(kappa/n)), from any starting size, with no extra rate assumption.</p>",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), last display on p. 1518, as repaired: weight <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mfrac><msub><mi>n</mi><mi>C</mi></msub><mrow><mo stretchy=\"false\">(</mo><mi>n</mi><mo>−</mo><mn>2</mn><mo stretchy=\"false\">)</mo><msub><mi>n</mi><mi>T</mi></msub></mrow></mfrac></mrow><annotation encoding=\"application/x-tex\">\\frac{n_C}{(n-2)n_T}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2317em;vertical-align:-0.52em;\"></span><span class=\"mord\"><span class=\"mopen nulldelimiter\"></span><span class=\"mfrac\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.7117em;\"><span style=\"top:-2.655em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mopen mtight\">(</span><span class=\"mord mathnormal mtight\">n</span><span class=\"mbin mtight\">−</span><span class=\"mord mtight\">2</span><span class=\"mclose mtight\">)</span><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\">n</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3448em;\"><span style=\"top:-2.3567em;margin-left:0em;margin-right:0.0714em;\"><span class=\"pstrut\" style=\"height:2.5em;\"></span><span class=\"katex-sizing reset-size3 size1 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1433em;\"><span></span></span></span></span></span></span></span></span></span><span style=\"top:-3.23em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"frac-line\" style=\"border-bottom-width:0.04em;\"></span></span><span style=\"top:-3.4103em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\">n</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3448em;\"><span style=\"top:-2.3567em;margin-left:0em;margin-right:0.0714em;\"><span class=\"pstrut\" style=\"height:2.5em;\"></span><span class=\"katex-sizing reset-size3 size1 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1433em;\"><span></span></span></span></span></span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.52em;\"><span></span></span></span></span></span><span class=\"mclose nulldelimiter\"></span></span></span></span></span> (<code class=\"fid\">P005-E013</code>), with the transposes of <code class=\"fid\">P005-E010</code> restored",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, last display, and its last line on p. 1519 (PDF p. 18)"
    },
    "id": "P005-T11",
    "text": {
     "body": "Appendix B.4, corrected last display, pp. 1518--1519 (PDF pp. 17--18). The corrected arm expressions cancel the inverse assignmentwise, have the exact generic expectation, and are unbiased with the derived arm-size weights. The cancelling treated weight equals its unsimplified expression and is unique for arms of size at least two; singleton expectations require no division by s-1. The printed treated weight has the stated bias. Standardization gives d/n <= kappa <= 1 and h_i <= n. Under Assumptions 1--3 both corrected arm remainders are O_p(sqrt(kappa/n)), from any starting size, with no extra rate assumption.",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), last display on p. 1518, as repaired: weight $\\frac{n_C}{(n-2)n_T}$ (P005-E013), with the transposes of P005-E010 restored",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, last display, and its last line on p. 1519 (PDF p. 18)"
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      "credit_reason": "This is a witness for T12, not proof that all printed formulas are unbiased. The scalar outcome is used as yC; weightPopulation, which places it in yT for another target, is not used in this statement. Centering gives E[xbar_C]=0, so the slope-product expectation is the nuisance bias specified by the target.",
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    "html": {
     "body": "<p>Appendix B.4, display introduced by “Similarly”, p. 1518 (PDF p. 17). The printed claim is false: for the six-unit population with a=(-3,-2,-1,0,1,5), x=sqrt(3/20)a, y(1)=0 and y(0)=a², all 15 assignments have positive treated and control Gram matrices. The population is standardized, has bounded second moments and allocation 1/3, and has h_i=(3/20)a_i² and mean leverage one. The control slope decomposes into its population slope and the three nu terms; the mean control covariate and its population-slope product have expectation zero. The nuisance-product and fitted-slope-product expectations both equal 31085815448171/17062566567774 (approximately 1.822). The printed estimator has expectation 12010469/846720 (approximately 14.18), so is biased; replacing the treated inverse by the control inverse gives exactly the nuisance expectation. The arm sizes, variance scaling, coefficient 1/8 and all rational-coordinate identities hold assignment by assignment.</p>",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), the display after “Similarly, an unbiased estimator for <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi mathvariant=\"bold\">E</mi><mo stretchy=\"false\">[</mo><msubsup><mover accent=\"true\"><mi>x</mi><mo>ˉ</mo></mover><mi>C</mi><mo mathvariant=\"normal\" lspace=\"0em\" rspace=\"0em\">′</mo></msubsup><mo stretchy=\"false\">(</mo><msub><mi>ν</mi><mrow><mn>1</mn><mi>C</mi></mrow></msub><mo>+</mo><msub><mi>ν</mi><mrow><mn>2</mn><mi>C</mi></mrow></msub><mo>+</mo><msub><mi>ν</mi><mrow><mn>3</mn><mi>C</mi></mrow></msub><mo stretchy=\"false\">)</mo><mo stretchy=\"false\">]</mo></mrow><annotation encoding=\"application/x-tex\">\\mathbf{E}[\\bar x_C&#x27;(\\nu_{1C}+\\nu_{2C}+\\nu_{3C})]</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0272em;vertical-align:-0.2753em;\"></span><span class=\"mord mathbf\">E</span><span class=\"mopen\">[</span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.5678em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">x</span></span><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"accent-body\" style=\"left:-0.2222em;\"><span class=\"mord\">ˉ</span></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.7519em;\"><span style=\"top:-2.4247em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span><span style=\"top:-3.063em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">′</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2753em;\"><span></span></span></span></span></span></span><span class=\"mopen\">(</span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0637em;\">ν</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0637em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">1</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span><span class=\"mbin\">+</span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.7333em;vertical-align:-0.15em;\"></span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0637em;\">ν</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0637em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">2</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span><span class=\"mbin\">+</span><span class=\"mspace\" style=\"margin-right:0.2222em;\"></span></span><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0637em;\">ν</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0637em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">3</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mclose\">)]</span></span></span></span> is”, as printed with <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msubsup><mover accent=\"true\"><mi>L</mi><mo stretchy=\"true\">^</mo></mover><mi>T</mi><mrow><mo>−</mo><mn>1</mn></mrow></msubsup></mrow><annotation encoding=\"application/x-tex\">\\widehat L_T^{-1}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2169em;vertical-align:-0.2935em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">L</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.0556em);margin-left:0.0556em;top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.8542em;\"><span style=\"top:-2.4065em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span><span style=\"top:-3.1031em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">−</span><span class=\"mord mtight\">1</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2935em;\"><span></span></span></span></span></span></span></span></span></span>. The witness is the validator&#x27;s and is not in the paper",
     "location": "p. 1518 (PDF p. 17), Appendix B.4"
    },
    "id": "P005-T12",
    "text": {
     "body": "Appendix B.4, display introduced by “Similarly”, p. 1518 (PDF p. 17). The printed claim is false: for the six-unit population with a=(-3,-2,-1,0,1,5), x=sqrt(3/20)a, y(1)=0 and y(0)=a², all 15 assignments have positive treated and control Gram matrices. The population is standardized, has bounded second moments and allocation 1/3, and has h_i=(3/20)a_i² and mean leverage one. The control slope decomposes into its population slope and the three nu terms; the mean control covariate and its population-slope product have expectation zero. The nuisance-product and fitted-slope-product expectations both equal 31085815448171/17062566567774 (approximately 1.822). The printed estimator has expectation 12010469/846720 (approximately 14.18), so is biased; replacing the treated inverse by the control inverse gives exactly the nuisance expectation. The arm sizes, variance scaling, coefficient 1/8 and all rational-coordinate identities hold assignment by assignment.",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), the display after “Similarly, an unbiased estimator for $\\mathbf{E}[\\bar x_C'(\\nu_{1C}+\\nu_{2C}+\\nu_{3C})]$ is”, as printed with $\\widehat L_T^{-1}$. The witness is the validator's and is not in the paper",
     "location": "p. 1518 (PDF p. 17), Appendix B.4"
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     "body": "<p>Appendix B.4, corrected display introduced by “Similarly”, p. 1518 (PDF p. 17). The control bias estimator with the control inverse has the required expectation chain, component expectations and coefficient identities.</p>",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), the control-arm bias estimator, as repaired: <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msubsup><mover accent=\"true\"><mi>L</mi><mo stretchy=\"true\">^</mo></mover><mi>C</mi><mrow><mo>−</mo><mn>1</mn></mrow></msubsup></mrow><annotation encoding=\"application/x-tex\">\\widehat L_C^{-1}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2169em;vertical-align:-0.2935em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">L</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.0556em);margin-left:0.0556em;top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.8542em;\"><span style=\"top:-2.4065em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span><span style=\"top:-3.1031em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">−</span><span class=\"mord mtight\">1</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2935em;\"><span></span></span></span></span></span></span></span></span></span> in place of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msubsup><mover accent=\"true\"><mi>L</mi><mo stretchy=\"true\">^</mo></mover><mi>T</mi><mrow><mo>−</mo><mn>1</mn></mrow></msubsup></mrow><annotation encoding=\"application/x-tex\">\\widehat L_T^{-1}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2169em;vertical-align:-0.2935em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\">L</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.0556em);margin-left:0.0556em;top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.8542em;\"><span style=\"top:-2.4065em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span><span style=\"top:-3.1031em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\">−</span><span class=\"mord mtight\">1</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2935em;\"><span></span></span></span></span></span></span></span></span></span> (<code class=\"fid\">P005-E012</code>)",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, the display introduced by “Similarly”"
    },
    "id": "P005-T13",
    "text": {
     "body": "Appendix B.4, corrected display introduced by “Similarly”, p. 1518 (PDF p. 17). The control bias estimator with the control inverse has the required expectation chain, component expectations and coefficient identities.",
     "headline": "Proof of Theorem 4.2 (Appendix B.4), the control-arm bias estimator, as repaired: $\\widehat L_C^{-1}$ in place of $\\widehat L_T^{-1}$ (P005-E012)",
     "location": "p. 1518 (PDF p. 17), Appendix B.4, the display introduced by “Similarly”"
    },
    "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T13"
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      "status": "proved",
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      "status": "proved",
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      "credit_reason": "The function is chosen before the population. Although the proof can ignore some hypotheses, they remain in the theorem statement; unused hypotheses do not themselves export a stronger theorem.",
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      "status": "proved",
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      "used_in_solution": true
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      "source": "https://github.com/pmaronow/llm-audit-lean/blob/b9e9df44831afed4f2b8f63be5c0cc9169a5fda4/AronowAudit/P005/Wave1/Gap/GP005B2.lean#L790",
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    "html": {
     "body": "<p>Appendix B.2, pp. 1515–1516 (PDF pp. 14–15), and Remark 2, p. 1507 (PDF p. 6). The corrected debiased expansion, inverse cancellation, arbitrary-vector residual identities, centered arm-mean identities and actual bias decomposition hold. A standardized everywhere regular four-unit example shows that the printed treated-set control sum can differ from the control residual mean. One function of the assignment, covariates and observed outcomes, chosen before the potential outcomes, gives the inverse bias component.</p>",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), the expansion of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover><mrow><mi mathvariant=\"normal\">D</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">b</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">d</mi></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0733em;vertical-align:-0.15em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3361em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\"><span class=\"mord mathrm mtight\">Debiased</span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span></span></span></span> on p. 1516, as repaired: transpose restored and the control sum taken over <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mo stretchy=\"false\">[</mo><mi>C</mi><mo stretchy=\"false\">]</mo></mrow><annotation encoding=\"application/x-tex\">[C]</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1em;vertical-align:-0.25em;\"></span><span class=\"mopen\">[</span><span class=\"mord mathnormal\" style=\"margin-right:0.0715em;\">C</span><span class=\"mclose\">]</span></span></span></span> (<code class=\"fid\">P005-E010</code>); with the same finding&#x27;s corrections on pp. 1515 and 1507",
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     "body": "Appendix B.2, pp. 1515–1516 (PDF pp. 14–15), and Remark 2, p. 1507 (PDF p. 6). The corrected debiased expansion, inverse cancellation, arbitrary-vector residual identities, centered arm-mean identities and actual bias decomposition hold. A standardized everywhere regular four-unit example shows that the printed treated-set control sum can differ from the control residual mean. One function of the assignment, covariates and observed outcomes, chosen before the potential outcomes, gives the inverse bias component.",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), the expansion of $\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}$ on p. 1516, as repaired: transpose restored and the control sum taken over $[C]$ (P005-E010); with the same finding's corrections on pp. 1515 and 1507",
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     "body": "<p>Appendix B.2, p. 1516 (PDF p. 15), using (11)–(12) on p. 1515. The corrected control covariance and the treatment covariance have coefficients 1/(n-2) and -1/(n-2), including the printed intermediate fraction and their combined expression.</p>",
     "headline": "Proof of Theorem 3.2 (Appendix B.2), the second sentence “Collecting the constants in front of …” on p. 1516, as repaired: the control-arm covariance <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi>h</mi><mi>y</mi><mo stretchy=\"false\">(</mo><mn>0</mn><mo stretchy=\"false\">)</mo></mrow><mo stretchy=\"true\">‾</mo></mover><mi>C</mi></msub><mo>−</mo><msub><mover accent=\"true\"><mi>h</mi><mo>ˉ</mo></mover><mi>C</mi></msub><msub><mover accent=\"true\"><mrow><mi>y</mi><mo stretchy=\"false\">(</mo><mn>0</mn><mo stretchy=\"false\">)</mo></mrow><mo stretchy=\"true\">‾</mo></mover><mi>C</mi></msub></mrow><annotation encoding=\"application/x-tex\">\\overline{hy(0)}_C - \\bar h_C\\overline{y(0)}_C</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" 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style=\"top:-3.2634em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"accent-body\" style=\"left:-0.25em;\"><span class=\"mord\">ˉ</span></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:0em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mord\"><span class=\"mord katex-overline\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.95em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" 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     "body": "<p>proof of Lemma A.2, pp. 1511–1512 (PDF pp. 10–11). The corrected finite indicator calculations, coefficient simplification, and complement relation give both the treated third moment and the mixed treated-control third moment.</p>",
     "headline": "Proof of Lemma A.2, as repaired: <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi mathvariant=\"bold\">E</mi><mo stretchy=\"false\">[</mo><msub><mi>D</mi><mi>i</mi></msub><msub><mi>D</mi><mi>j</mi></msub><mo stretchy=\"false\">]</mo></mrow><annotation encoding=\"application/x-tex\">\\mathbf{E}[D_iD_j]</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0361em;vertical-align:-0.2861em;\"></span><span class=\"mord mathbf\">E</span><span class=\"mopen\">[</span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0278em;\">D</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3117em;\"><span style=\"top:-2.55em;margin-left:-0.0278em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\">i</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span><span class=\"mord\"><span class=\"mord mathnormal\" style=\"margin-right:0.0278em;\">D</span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3117em;\"><span style=\"top:-2.55em;margin-left:-0.0278em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0572em;\">j</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2861em;\"><span></span></span></span></span></span></span><span class=\"mclose\">]</span></span></span></span> in the first display (p. 1511) and upper limit <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mi>n</mi></mrow><annotation encoding=\"application/x-tex\">n</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.4306em;\"></span><span class=\"mord mathnormal\">n</span></span></span></span> in the last display (p. 1512) (<code class=\"fid\">P005-E005</code>)",
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     "body": "proof of Lemma A.2, pp. 1511–1512 (PDF pp. 10–11). The corrected finite indicator calculations, coefficient simplification, and complement relation give both the treated third moment and the mixed treated-control third moment.",
     "headline": "Proof of Lemma A.2, as repaired: $\\mathbf{E}[D_iD_j]$ in the first display (p. 1511) and upper limit $n$ in the last display (p. 1512) (P005-E005)",
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     "body": "<p>The printed claim is false: both the universal third-component sign identity and the stochastic expansion under the literal logarithm condition fail; the stated exact slope decompositions, bias expression, and first-component moments hold. Theorem 4.1, pp. 1509–1510 (PDF pp. 8–9).</p>",
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     "location": "pp. 1509–1510 (PDF pp. 8–9), Section 4; proof B.3 on p. 1517 (PDF p. 16)"
    },
    "id": "P005-T20",
    "text": {
     "body": "The printed claim is false: both the universal third-component sign identity and the stochastic expansion under the literal logarithm condition fail; the stated exact slope decompositions, bias expression, and first-component moments hold. Theorem 4.1, pp. 1509–1510 (PDF pp. 8–9).",
     "headline": "Theorem 4.1, as printed",
     "location": "pp. 1509–1510 (PDF pp. 8–9), Section 4; proof B.3 on p. 1517 (PDF p. 16)"
    },
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      "credit_reason": "The target explicitly incorporates n>=3, nonempty arms, fixed-n Assumption 2 and footnote-4 all-assignment invertibility; none is an added restriction. The separate generalized-inverse extension in the footnote is outside the nonsingular component credited to this row.",
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      "status": "proved",
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     "body": "<p>Theorem 3.2, pp. 1508–1509 (PDF pp. 7–8); proof in Appendix B.2. The printed noninteracted bias estimator is exactly unbiased for the bias, and its correction is exactly unbiased for the ATE. The closed-form coefficients are the unique OLS minimizer. The inverse-free formula, bias decomposition, inverse-component identity and both population component expectations hold for all nonempty arms. Expressions (11) and (12), their expectations and their collection into (7) require only their presupposed nonzero arm-size denominators.</p>",
     "headline": "Theorem 3.2, first part: exact unbiasedness of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">B</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi></mrow><mo stretchy=\"true\">^</mo></mover></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{Bias}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.9233em;\"></span><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">Bias</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span></span></span></span> and of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover><mrow><mi mathvariant=\"normal\">D</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">b</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">d</mi></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0733em;vertical-align:-0.15em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3361em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\"><span class=\"mord mathrm mtight\">Debiased</span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span></span></span></span> (noninteracted case)",
     "location": "pp. 1508–1509 (PDF pp. 7–8), Section 3, equations (7)–(8); proof in Appendix B.2, pp. 1515–1516 (PDF pp. 14–15)"
    },
    "id": "P005-T21",
    "text": {
     "body": "Theorem 3.2, pp. 1508–1509 (PDF pp. 7–8); proof in Appendix B.2. The printed noninteracted bias estimator is exactly unbiased for the bias, and its correction is exactly unbiased for the ATE. The closed-form coefficients are the unique OLS minimizer. The inverse-free formula, bias decomposition, inverse-component identity and both population component expectations hold for all nonempty arms. Expressions (11) and (12), their expectations and their collection into (7) require only their presupposed nonzero arm-size denominators.",
     "headline": "Theorem 3.2, first part: exact unbiasedness of $\\widehat{\\mathrm{Bias}}$ and of $\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}$ (noninteracted case)",
     "location": "pp. 1508–1509 (PDF pp. 7–8), Section 3, equations (7)–(8); proof in Appendix B.2, pp. 1515–1516 (PDF pp. 14–15)"
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     "body": "<p>Theorem 4.2, p. 1510 (PDF p. 9). The interacted bias correction and corrected ATE are exactly unbiased, with the inverse-free identity and both armwise expectations, including the stated weaker centered-covariate hypotheses.</p>",
     "headline": "Theorem 4.2, first part: exact unbiasedness of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">B</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi></mrow><mo stretchy=\"true\">^</mo></mover><mi>I</mi></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{Bias}}_I</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0733em;vertical-align:-0.15em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">Bias</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0785em;\">I</span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span></span></span></span> and of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover><mrow><mi>I</mi><mo separator=\"true\">,</mo><mrow><mi mathvariant=\"normal\">D</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">b</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">d</mi></mrow></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}_{I,\\mathrm{Debiased}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2094em;vertical-align:-0.2861em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3361em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0785em;\">I</span><span class=\"mpunct mtight\">,</span><span class=\"mord mtight\"><span class=\"mord mathrm mtight\">Debiased</span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2861em;\"><span></span></span></span></span></span></span></span></span></span> (interacted case)",
     "location": "p. 1510 (PDF p. 9), Section 4; proof in Appendix B.4, p. 1518 (PDF p. 17)"
    },
    "id": "P005-T22",
    "text": {
     "body": "Theorem 4.2, p. 1510 (PDF p. 9). The interacted bias correction and corrected ATE are exactly unbiased, with the inverse-free identity and both armwise expectations, including the stated weaker centered-covariate hypotheses.",
     "headline": "Theorem 4.2, first part: exact unbiasedness of $\\widehat{\\mathrm{Bias}}_I$ and of $\\widehat{\\mathrm{ATE}}_{I,\\mathrm{Debiased}}$ (interacted case)",
     "location": "p. 1510 (PDF p. 9), Section 4; proof in Appendix B.4, p. 1518 (PDF p. 17)"
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     "body": "<p>Theorem 3.1 and Remark 1, p. 1507 (PDF p. 6). The exact noninteracted slope and bias decompositions give (5), (6), the covariance interpretation, and the two stated vanishing consequences of Remark 1.</p>",
     "headline": "Theorem 3.1, exact part: the decomposition of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mover accent=\"true\"><mi>β</mi><mo stretchy=\"true\">^</mo></mover></mrow><annotation encoding=\"application/x-tex\">\\widehat\\beta</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.1289em;vertical-align:-0.1944em;\"></span><span class=\"mord katex-accent\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9344em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0528em;\">β</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.1667em);margin-left:0.1667em;top:-3.6944em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1944em;\"><span></span></span></span></span></span></span></span></span> and the bias components (5) and (6); with the two exact consequences stated in Remark 1",
     "location": "p. 1507 (PDF p. 6), Section 3; proof in Appendix B.1, pp. 1512–1513 (PDF pp. 11–12), and B.2, p. 1515 (PDF p. 14)"
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     "body": "Theorem 3.1 and Remark 1, p. 1507 (PDF p. 6). The exact noninteracted slope and bias decompositions give (5), (6), the covariance interpretation, and the two stated vanishing consequences of Remark 1.",
     "headline": "Theorem 3.1, exact part: the decomposition of $\\widehat\\beta$ and the bias components (5) and (6); with the two exact consequences stated in Remark 1",
     "location": "p. 1507 (PDF p. 6), Section 3; proof in Appendix B.1, pp. 1512–1513 (PDF pp. 11–12), and B.2, p. 1515 (PDF p. 14)"
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      "source": "https://github.com/pmaronow/llm-audit-lean/blob/b9e9df44831afed4f2b8f63be5c0cc9169a5fda4/AronowAudit/P005/P005_Formalization.lean#L1535",
      "status": "proved",
      "support_scope": "historical declaration",
      "used_in_solution": true
     }
    ],
    "formalization": {
     "claim_revision_id": "catalog:43328987c47c5d6f08d8faeb6c298bbc8436cede57b4e1bc5e7e8590d80d90a9",
     "crosswalk_url": "../../data/lean-crosswalk.json#/targets/P005-T24",
     "decision": "whole",
     "release_id": "sap-2026-11-08-assured-release",
     "target_id": "P005-T24"
    },
    "html": {
     "body": "<p>Theorem 4.1, p. 1509 (PDF p. 8), its valid exact part. Both interacted slopes decompose as printed, and the bias expression and separate first-component expectations give their stated difference.</p>",
     "headline": "Theorem 4.1, exact part that stands as printed: the decompositions of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mi>β</mi><mo stretchy=\"true\">^</mo></mover><mrow><mi>I</mi><mo separator=\"true\">,</mo><mi>T</mi></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat\\beta_{I,T}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2205em;vertical-align:-0.2861em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9344em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0528em;\">β</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.1667em);margin-left:0.1667em;top:-3.6944em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1944em;\"><span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0528em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0785em;\">I</span><span class=\"mpunct mtight\">,</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.1389em;\">T</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2861em;\"><span></span></span></span></span></span></span></span></span></span> and <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mi>β</mi><mo stretchy=\"true\">^</mo></mover><mrow><mi>I</mi><mo separator=\"true\">,</mo><mi>C</mi></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat\\beta_{I,C}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2205em;vertical-align:-0.2861em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9344em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord mathnormal\" style=\"margin-right:0.0528em;\">β</span></span><span class=\"svg-align\" style=\"width:calc(100% - 0.1667em);margin-left:0.1667em;top:-3.6944em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.1944em;\"><span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3283em;\"><span style=\"top:-2.55em;margin-left:-0.0528em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0785em;\">I</span><span class=\"mpunct mtight\">,</span><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0715em;\">C</span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2861em;\"><span></span></span></span></span></span></span></span></span></span>, the expression of the bias, and the first bias component",
     "location": "p. 1509 (PDF p. 8), Section 4; proof B.3 on p. 1517 (PDF p. 16) omits the details"
    },
    "id": "P005-T24",
    "text": {
     "body": "Theorem 4.1, p. 1509 (PDF p. 8), its valid exact part. Both interacted slopes decompose as printed, and the bias expression and separate first-component expectations give their stated difference.",
     "headline": "Theorem 4.1, exact part that stands as printed: the decompositions of $\\widehat\\beta_{I,T}$ and $\\widehat\\beta_{I,C}$, the expression of the bias, and the first bias component",
     "location": "p. 1509 (PDF p. 8), Section 4; proof B.3 on p. 1517 (PDF p. 16) omits the details"
    },
    "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T24"
   },
   {
    "declarations": [
     {
      "claim_revision_id": "catalog:7e44f8b6f0c09ea443e0e50e7a6584574378c215b25dff1f9aa00640a7c5ee19",
      "conditional_on": [],
      "credit_reason": "The target definitions explicitly require 1<=d_n, so the positive-dimension field is not an added assumption. Uniform K, eventual standardization and eventual regularity have the required all-sequence meaning; finitely many initial sizes do not affect O_p.",
      "credit_status": "ok",
      "fidelity_status_baseline": "ok",
      "lean_name": "AronowAudit.P005.Wave1.noninteracted_stochastic_expansion_proof",
      "manifest_use": "used",
      "named_axioms": [],
      "says": null,
      "source": "https://github.com/pmaronow/llm-audit-lean/blob/b9e9df44831afed4f2b8f63be5c0cc9169a5fda4/AronowAudit/P005/Wave1/Gap/GP005B3b.lean#L847",
      "status": "proved",
      "support_scope": "historical declaration",
      "used_in_solution": true
     }
    ],
    "formalization": {
     "claim_revision_id": "catalog:7e44f8b6f0c09ea443e0e50e7a6584574378c215b25dff1f9aa00640a7c5ee19",
     "crosswalk_url": "../../data/lean-crosswalk.json#/targets/P005-T25",
     "decision": "whole",
     "release_id": "sap-2026-11-08-assured-release",
     "target_id": "P005-T25"
    },
    "html": {
     "body": "<p>last part of Theorem 3.1, p. 1507 (PDF p. 6). The noninteracted regression remainder is O_p(sqrt(kappa*d/n)) when d/n tends to zero. The dimension convention 1 &lt;= d_n &lt;= n agrees with the canonical order-symbol definitions. No conclusion is omitted.</p>",
     "headline": "Theorem 3.1, last part: the stochastic expansion of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:0.9233em;\"></span><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span></span></span></span> (noninteracted case)",
     "location": "p. 1507 (PDF p. 6), Section 3; proof in Appendix B.1.1, pp. 1513–1515 (PDF pp. 12–14)"
    },
    "id": "P005-T25",
    "text": {
     "body": "last part of Theorem 3.1, p. 1507 (PDF p. 6). The noninteracted regression remainder is O_p(sqrt(kappa*d/n)) when d/n tends to zero. The dimension convention 1 <= d_n <= n agrees with the canonical order-symbol definitions. No conclusion is omitted.",
     "headline": "Theorem 3.1, last part: the stochastic expansion of $\\widehat{\\mathrm{ATE}}$ (noninteracted case)",
     "location": "p. 1507 (PDF p. 6), Section 3; proof in Appendix B.1.1, pp. 1513–1515 (PDF pp. 12–14)"
    },
    "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T25"
   },
   {
    "declarations": [
     {
      "claim_revision_id": "catalog:67ec9f0dfa9acc19273241cedede466b72a9ba4038ce231fcbe9fce372866b82",
      "conditional_on": [],
      "credit_reason": "{'source': 'adjudication+second review', 'adjudicator': 'At P005/Wave1/DebiasedLinearTailC.lean:130, the declaration assumes hκ (κ_n → 0) and concludes only that R_n = debiasedATE − ate − commonLeading is o_p(n^−1/2). The final sentence of the supplied P005-T26 claim additionally asserts R_n = O_p(√(κ_n/n)) without that assumption, and identifies R_n exactly with the printed term (*) on p. 1516. Neither the stronger rate without hκ nor the exact identity is included in this declaration’s conclusion. The printed Theorem 3.2 little-o formula is matched, but the supplied target and the row’s full-coverage description assert more.', 'suggested_fix': 'Extend the statement to export stochasticO m R (fun n => Real.sqrt (kappa (P n) / n)) under standingAssumptions and eventual noninteractedRegular without hκ, with the existing stochasticLittleO conclusion conditional on hκ. Also export the fixed-n identity R = −dot (xMean P S − xMean P (control S)) (Nhat P m S − N P m) + (sampleCov S (leverage P) P.yT − sampleCov (control S) (leverage P) P.yC) / (n−2) for n ≥ 3, standardized P, valid arm sizes, S in design n m and nonzero determinant of Lhat.', 'second_review': \"P005/Wave1/DebiasedLinearTailC.lean:130 assumes κ_n → 0 and exports only stochasticLittleO at scale sqrt(1/n), with the residual and randomization interpretation matching the printed expansion through P005/P005_Formalization.lean:310 and P005/P005_Formalization.lean:325. P005-T26's claim text additionally asserts O_p(sqrt(κ_n/n)) without κ_n → 0 and an exact identification with (*); neither conclusion is exported. The little-o conclusion cannot recover that finer rate or cover nonvanishing-leverage sequences, so this is a major statement omission, even though the printed Theorem 3.2 formula itself is represented correctly.\", 'severity': 'major'}",
      "credit_status": "narrower",
      "fidelity_status_baseline": "narrower",
      "lean_name": "AronowAudit.P005.Wave1.noninteracted_debiased_linear_expansion_proof",
      "manifest_use": "used",
      "named_axioms": [],
      "says": null,
      "source": "https://github.com/pmaronow/llm-audit-lean/blob/b9e9df44831afed4f2b8f63be5c0cc9169a5fda4/AronowAudit/P005/Wave1/DebiasedLinearTailC.lean#L130",
      "status": "proved",
      "support_scope": "limited",
      "used_in_solution": true
     }
    ],
    "formalization": {
     "claim_revision_id": "catalog:67ec9f0dfa9acc19273241cedede466b72a9ba4038ce231fcbe9fce372866b82",
     "crosswalk_url": "../../data/lean-crosswalk.json#/targets/P005-T26",
     "decision": "whole",
     "release_id": "sap-2026-11-08-assured-release",
     "target_id": "P005-T26"
    },
    "html": {
     "body": "<p>Theorem 3.2, p. 1509 (PDF p. 8); Appendix B.2, pp. 1516–1517. The debiased noninteracted remainder equals the p. 1516 term (*) exactly and is O_p(sqrt(kappa/n)) under Assumptions 1–3, without leverage decay. If kappa tends to zero, this gives the printed common-slope expansion with o_p(n^(-1/2)) error.</p>",
     "headline": "Theorem 3.2, second part: the asymptotic linear expansion of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover><mrow><mi mathvariant=\"normal\">D</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">b</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">d</mi></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.0733em;vertical-align:-0.15em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3361em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mtight\"><span class=\"mord mathrm mtight\">Debiased</span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.15em;\"><span></span></span></span></span></span></span></span></span></span>",
     "location": "p. 1509 (PDF p. 8), Section 3 (the theorem begins on p. 1508, PDF p. 7); proof in Appendix B.2, pp. 1516–1517 (PDF pp. 15–16)"
    },
    "id": "P005-T26",
    "text": {
     "body": "Theorem 3.2, p. 1509 (PDF p. 8); Appendix B.2, pp. 1516–1517. The debiased noninteracted remainder equals the p. 1516 term (*) exactly and is O_p(sqrt(kappa/n)) under Assumptions 1–3, without leverage decay. If kappa tends to zero, this gives the printed common-slope expansion with o_p(n^(-1/2)) error.",
     "headline": "Theorem 3.2, second part: the asymptotic linear expansion of $\\widehat{\\mathrm{ATE}}_{\\mathrm{Debiased}}$",
     "location": "p. 1509 (PDF p. 8), Section 3 (the theorem begins on p. 1508, PDF p. 7); proof in Appendix B.2, pp. 1516–1517 (PDF pp. 15–16)"
    },
    "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T26"
   },
   {
    "declarations": [
     {
      "claim_revision_id": "catalog:88011ec1b109ee929518f754f0f34f6f8a2a152edc2046b72f99a6a1944a14cd",
      "conditional_on": [],
      "credit_reason": "{'source': 'adjudication+second review', 'adjudicator': 'At P005/Wave1/DebiasedLinearTailC.lean:195, the declaration assumes hκ (κ_n → 0) and concludes only that R_n = interactedDebiasedATE − ate − armLeading is o_p(n^−1/2). The final sentence of the supplied P005-T27 claim also asserts R_n = O_p(√(κ_n/n)) without assuming κ_n → 0. That stronger rate and its wider sequence domain are absent from the declaration, although the printed Theorem 4.2 little-o formula is represented correctly.', 'suggested_fix': 'Extend the statement to export stochasticO m R (fun n => Real.sqrt (kappa (P n) / n)) under standingAssumptions and eventual interactedRegular without hκ, retaining the existing stochasticLittleO conclusion as conditional on hκ.', 'second_review': \"P005/Wave1/DebiasedLinearTailC.lean:195 assumes κ_n → 0 and concludes only stochasticLittleO for interactedDebiasedATE − ate − armLeading at scale sqrt(1/n); armLeading uses the target's two population arm slopes (P005/P005_Formalization.lean:302 and P005/P005_Formalization.lean:313). P005-T27's claim text also requires O_p(sqrt(κ_n/n)) without the decay assumption. That finer rate on the wider sequence domain does not follow from the exported little-o statement, so the target needs a substantive additional statement rather than a description edit.\", 'severity': 'major'}",
      "credit_status": "narrower",
      "fidelity_status_baseline": "narrower",
      "lean_name": "AronowAudit.P005.Wave1.interacted_debiased_linear_expansion_proof",
      "manifest_use": "used",
      "named_axioms": [],
      "says": null,
      "source": "https://github.com/pmaronow/llm-audit-lean/blob/b9e9df44831afed4f2b8f63be5c0cc9169a5fda4/AronowAudit/P005/Wave1/DebiasedLinearTailC.lean#L197",
      "status": "proved",
      "support_scope": "limited",
      "used_in_solution": true
     }
    ],
    "formalization": {
     "claim_revision_id": "catalog:88011ec1b109ee929518f754f0f34f6f8a2a152edc2046b72f99a6a1944a14cd",
     "crosswalk_url": "../../data/lean-crosswalk.json#/targets/P005-T27",
     "decision": "whole",
     "release_id": "sap-2026-11-08-assured-release",
     "target_id": "P005-T27"
    },
    "html": {
     "body": "<p>Theorem 4.2, p. 1510 (PDF p. 9); Appendix B.4, pp. 1518–1519. The debiased interacted remainder is O_p(sqrt(kappa/n)) under Assumptions 1–3, without leverage decay. If kappa tends to zero, the printed arm-specific linear expansion has o_p(n^(-1/2)) error.</p>",
     "headline": "Theorem 4.2, second part: the asymptotic linear expansion of <span class=\"katex\"><span class=\"katex-mathml\"><math xmlns=\"http://www.w3.org/1998/Math/MathML\"><semantics><mrow><msub><mover accent=\"true\"><mrow><mi mathvariant=\"normal\">A</mi><mi mathvariant=\"normal\">T</mi><mi mathvariant=\"normal\">E</mi></mrow><mo stretchy=\"true\">^</mo></mover><mrow><mi>I</mi><mo separator=\"true\">,</mo><mrow><mi mathvariant=\"normal\">D</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">b</mi><mi mathvariant=\"normal\">i</mi><mi mathvariant=\"normal\">a</mi><mi mathvariant=\"normal\">s</mi><mi mathvariant=\"normal\">e</mi><mi mathvariant=\"normal\">d</mi></mrow></mrow></msub></mrow><annotation encoding=\"application/x-tex\">\\widehat{\\mathrm{ATE}}_{I,\\mathrm{Debiased}}</annotation></semantics></math></span><span class=\"katex-html\" aria-hidden=\"true\"><span class=\"katex-base\"><span class=\"katex-strut\" style=\"height:1.2094em;vertical-align:-0.2861em;\"></span><span class=\"mord\"><span class=\"mord katex-accent\"><span class=\"vlist-t\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.9233em;\"><span style=\"top:-3em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span class=\"mord\"><span class=\"mord mathrm\">ATE</span></span></span><span class=\"svg-align\" style=\"top:-3.6833em;\"><span class=\"pstrut\" style=\"height:3em;\"></span><span style=\"height:0.24em;\"><svg xmlns=\"http://www.w3.org/2000/svg\" width=\"100%\" height=\"0.24em\" viewBox=\"0 0 1062 239\" preserveAspectRatio=\"none\"><path d=\"M529 0h5l519 115c5 1 9 5 9 10 0 1-1 2-1 3l-4 22\nc-1 5-5 9-11 9h-2L532 67 19 159h-2c-5 0-9-4-11-9l-5-22c-1-6 2-12 8-13z\"/></svg></span></span></span></span></span></span><span class=\"msupsub\"><span class=\"vlist-t vlist-t2\"><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.3361em;\"><span style=\"top:-2.55em;margin-right:0.05em;\"><span class=\"pstrut\" style=\"height:2.7em;\"></span><span class=\"katex-sizing reset-size6 size3 mtight\"><span class=\"mord mtight\"><span class=\"mord mathnormal mtight\" style=\"margin-right:0.0785em;\">I</span><span class=\"mpunct mtight\">,</span><span class=\"mord mtight\"><span class=\"mord mathrm mtight\">Debiased</span></span></span></span></span></span><span class=\"vlist-s\">​</span></span><span class=\"vlist-r\"><span class=\"vlist\" style=\"height:0.2861em;\"><span></span></span></span></span></span></span></span></span></span>",
     "location": "p. 1510 (PDF p. 9), Section 4; proof in Appendix B.4, pp. 1518–1519 (PDF pp. 17–18)"
    },
    "id": "P005-T27",
    "text": {
     "body": "Theorem 4.2, p. 1510 (PDF p. 9); Appendix B.4, pp. 1518–1519. The debiased interacted remainder is O_p(sqrt(kappa/n)) under Assumptions 1–3, without leverage decay. If kappa tends to zero, the printed arm-specific linear expansion has o_p(n^(-1/2)) error.",
     "headline": "Theorem 4.2, second part: the asymptotic linear expansion of $\\widehat{\\mathrm{ATE}}_{I,\\mathrm{Debiased}}$",
     "location": "p. 1510 (PDF p. 9), Section 4; proof in Appendix B.4, pp. 1518–1519 (PDF pp. 17–18)"
    },
    "url": "https://pmaronow.github.io/llm-audit/works/P005/#P005-T27"
   }
  ]
 },
 "missing_sources": [],
 "reproduction": {
  "agreement": "not_applicable",
  "status": "not_applicable",
  "targets": []
 },
 "summary": "The article addresses Freedman's objection that regression adjustment is biased in completely randomized experiments. It derives closed-form estimators of the bias of the noninteracted and interacted OLS estimators of the average treatment effect. Its results are that the bias-corrected estimators are exactly unbiased and, under Freedman's assumptions, have the limiting distributions of the uncorrected ones. 16 entries are classified as errors (1 Moderate, 15 Minor), and 2 are clarity notes. These are counts of entries: \\fid{P005-N004} expands the discussion of the same defect as \\fid{P005-E001} and adds no separate error. The most consequential error is in the last display of Theorem 4.1, which prints the third component of the bias with both signs reversed (\\fid{P005-E003}). The bias correction of Theorem 4.2 has the correct signs.",
 "what_was_checked": "I checked the following points, which held up. This list is not a statement that the article is correct, and the absence of a correction elsewhere is not a finding of correctness.\n\\begin{itemize}\n\\item The bias estimators of Theorems 3.2 and 4.2 were derived again from the moments of simple random sampling. Enumeration of every assignment confirmed unbiasedness to numerical precision in several small designs and in the twelve designs with $n=24$ and $n_T=8$ of the replication files.\n\\item In Theorem 3.1, the decomposition $\\widehat\\beta=\\beta^*+\\nu_1+\\nu_2+\\nu_3$ and equations (5) and (6) were derived again and agree with enumeration. In Theorem 4.1, the same holds for the decomposition and the first display. The last display is corrected in \\fid{P005-E003}.\n\\item The expectation identity of Lemma A.1 was derived again for vectors that need not be centered. Lemma A.2 and each step of its proof were checked, apart from the misprints corrected in \\fid{P005-E005}, and so were the constants $N_{\\mathrm{TTT}}$, $N_{\\mathrm{CCC}}$ and $N_{\\mathrm{TTC}}$.\n\\item The stochastic expansions of Theorems 3.1, 3.2 and 4.2 were followed step by step through Appendices B.1.1, B.2 and B.4. The stated rates hold once Lemma A.1 is used in its centered form (\\fid{P005-E002}). The expansion of Theorem 4.1 was derived for $d\\ge2$; the case $d=1$ is corrected in \\fid{P005-E001}, and \\fid{P005-N004} concerns the same defect.\n\\item Remarks 1 and 4, the calculation with one covariate on pp.~1507--1508, and footnotes 3 and 4.\n\\item In the replication files, the functions \\texttt{unbiased.reg.noninteract\\_new\\_formula} and \\texttt{unbiased.reg.interact\\_appl\\_new\\_formula} agree with the estimators of Theorems 3.2 and 4.2 on the enumerated designs.\n\\end{itemize}\n\nThe cited works were not among the sources and were not checked. The statements taken from Lei and Ding (2021), Freedman (2008b), Wu and Ding (2021), Finucan, Galbraith and Stone (1974) and Lin (2013) were derived again or checked numerically where the argument needs them, and they were not compared with their sources. The results of Lin (2013) on which the conclusion of the article relies were not examined. The statement in footnote 1 and Remark 5 that earlier corrections are not exactly unbiased was not checked. The simulations of the replication files were not run in full, the designs with $n=36$ were not enumerated, and the scripts in the folder of old files were examined through their differences from the current scripts and targeted checks.\n\nThe article contains no table, figure, simulation or empirical estimate, so there was no numerical result to reproduce. No supplement or correction notice was among the sources. The replication files are a snapshot, dated June 2023, of a public repository of research code. The repository is not a journal replication package and predates publication, and its simulations and applications do not appear in the article. My checks of that code cover the selected formulas and implementation errors reported here.",
 "work": {
  "arxiv_id": "2110.08425",
  "audit_complete": true,
  "authors": [
   "Haoge Chang",
   "Joel A. Middleton",
   "P. M. Aronow"
  ],
  "category": "Articles - Theory and Methodology",
  "citation": "Haoge Chang, Joel A. Middleton, and P. M. Aronow (2024). Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials. Econometrica 92(5):1503–1519.",
  "doi": "10.3982/ECTA20289",
  "edition": {
   "pages_in_audited_file": 18,
   "sha256": "3dab5dd9d1c112bb75028fa4f81cf1e9da3142d48327697e24a4f1c0778e3f38",
   "source_url": "https://doi.org/10.3982/ECTA20289",
   "venue": "Econometrica",
   "year": "2024"
  },
  "id": "P005",
  "later_materials": null,
  "title": "Exact Bias Correction for Linear Adjustment of Randomized Controlled Trials",
  "type": "Journal article",
  "url": "https://pmaronow.github.io/llm-audit/works/P005/",
  "venue": "Econometrica",
  "year": "2024"
 }
}
