Methods review: C1 minor_issues; C2 minor_issues; C3 minor_issues; C4 major_issues; C5 minor_issues. All five have moderate significance if established as appropriately qualified population associations; distinguishing care patterns from measured outcomes is useful, but the study is not a clinical trial. I read the paper, preregistration, deviations, analysis and extraction code, supplied cells and outputs. My earlier independent execution of the exact declared environment reproduced every output. This review does not claim an independent rebuild of20GB of microdata.

C1 is unusually clear in preserving the failed falsification rule: estimate1.19pp with interval[.70,1.68], but primary verdict inconclusive. This operational statement is supported. The observed nulliparity-share jump is a real warning under the plan, not something to dismiss merely because the primary sample restricts nulliparity: differential classification/selection can affect that restricted sample. Retain inconclusive in title/summary and avoid downstream causal language that bypasses it. Failure of other covariates to reject is not proof of balance. Several tests use data-dependent, very wide curvature bounds and are admitted to be uninformative. Their nonrejection should not be counted as positive validation.

C2 reproduces2.86pp[2.05,3.67] and the rule confirms. Call this confirmation of a prespecified statistical rule conditional on assumptions, not identification of an age-label effect. No observed covariate rejection cannot establish continuity of all potential outcomes. Age-at-delivery differs from age at due date, and delivery timing itself can move pregnancies across a birthday; this need not be classical nondifferential misclassification or necessarily bias only toward zero. Administrative age and term-only sample selection can depend on intervention timing. Report these as identification limits and seek finer dates or a design aligning assignment age before treatment. Neither a large national sample nor a narrow sampling SE resolves systematic selection.

Honest intervals: the stated bound B=M/2 sum|w|x^2 follows from Taylor remainders for point evaluations f(x) with bounded second derivative on each side and local-linear moment restrictions. These inputs are means over whole-year bins treated as centre values. To target the discontinuity in continuous age, justify the relation between bin means and f at the centre. Uniform within-bin age and bounded curvature would supply an additional averaging error bound; unknown nonuniform within-bin distributions can add slope-related error, even when the underlying curve is linear. Alternatively define the estimand and smoothness restriction directly on a chosen interpolation of the discrete conditional means, and acknowledge it is assumption-dependent. This is a requested clarification/sensitivity, not a demonstrated reversal of the reported associations. Kolesar and Rothe's original abstract explicitly conditions coverage on restrictions on the conditional expectation function: https://pubs.aeaweb.org/doi/10.1257/aer.20160945 . Merely citing discrete-RD theory does not validate any chosen M or a rounded-age measurement model.

The M=.1pp/year-squared bound is justified using five-year age-group averages; low curvature of such averages is not an upper bound on local curvature near a cutoff. It is a substantive assumption. The reported M sensitivity is helpful. Expand it to show the M at which each positive interval first includes zero and justify outcome-specific bounds. Placebo windows that cross the actual35/40 thresholds are contaminated by the treatment hypothesis and cannot cleanly calibrate untreated curvature. The rule was operationalized in deviations and retained M here; do not present it as independent assurance of coverage. Rounding p values to eight decimals creates reported zeros; use scientific notation or inequalities.

C3's39-week differences reproduce. Interpret as associated changes in delivery timing within singleton nulliparous term births under the same RD assumptions, with the35 falsification issue carried forward. Selection on37-44week delivery excludes any effect shifting delivery into/out of that interval. Distinguish individual95% intervals from simultaneous family coverage: Holm-adjusted p values are provided but do not turn all displayed marginal intervals into simultaneous intervals.

C4 major_issues: no detected discontinuity is not no discontinuity. No equivalence margins were defined for these outcomes and the stated intervals allow changes that may matter. At40 the cesarean interval is about[-.24,+1.40]pp; NICU[-.78,+.29]pp. At35 cesarean is[-.23,+.76]pp and NICU[-.52,+.18]pp. These bounds cannot support saying the label changes timing without changing outcomes, or that extra induction is neither offset nor amplified by outcomes. Report estimates and uncertainty, use no statistically detectable jump, and define outcome-specific clinically meaningful equivalence bounds before any no-effect claim. Individual outcomes have different baselines and unknown-record denominators; a single envelope across outcomes is not an equivalence test. A shared age threshold association also cannot isolate the effect of induction from other changes in care without additional exclusion/relevance assumptions.

C5 is appropriately explicit that intervals are wide relative to baseline; replace shows no discontinuity with no discontinuity detected. The term fetal-death proportion among deliveries is not a prospective stillbirth hazard among ongoing pregnancies, nor the perinatal-mortality endpoint in the cited commercial-claims study. Excluding a-.39pp benchmark for a different endpoint/population does not demonstrate absence of benefit. Nulliparity as no previous live births is not first pregnancy; prior fetal losses are not excluded by priorlive/priordead (the latter code is priordead, prior live births now dead). Correct first pregnancies to no prior live births. The registered morbidity composite mentions severe perineal tear whereas the implementation uses mm_plac with other flags; verify the official field definitions, align the planned composite or explicitly log the outcome change. I have not independently checked every year's codebook and do not claim a specific reestimated effect.

Public-use counts and transparent preregistration are strengths of the audit trail. Recommended revisions preserve the reproducible descriptive estimates and the primary inconclusive decision while separating them from causal and no-effect conclusions. No publisher identity was sought or learned.