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Whether antidepressants raise suicidal behaviour in adults is disputed: the FDA's pooled trials found no increase past young adulthood, and re-analyses of approval data on newer drugs found more suicide attempts. We tested this in the serious adverse events placebo-controlled trials posted to ClinicalTrials.gov, under a registered plan. This version corrects the first, which counted a participant listed under two of an outcome's terms twice. With the posted tables and the trials' public reports, serious suicidal behaviour affected 43 adults on antidepressants and 17 to 18 on placebo (risk ratio 1.86 to 1.96): nominally significant, but at the least favourable count not after the registered correction for two endpoints. Without the trials the re-analyses also used, the excess is similar but less certain. Pediatric trials showed more serious suicidality on antidepressants, as the FDA found. These data lean toward more suicidal behaviour in adults but cannot establish it.

• Published, Reproduced.Published, Reproduced: Of the 932 interventional studies naming an antidepressant with results posted on ClinicalTrials.gov on 2026-10-13, 393 randomized trials compare an antidepressant with placebo in 413 comparisons with 99,730 participants at risk in their adverse-event tables. In the 306 adult trials that randomized participants from the start (71,643 participants), nausea is more frequent on antidepressants in the 207 comparisons whose non-serious tables list it (57,580 participants; Mantel-Haenszel risk ratio 2.08, 95% CI 1.98 to 2.18), as these drugs' known side effects predict.
• Published, Reproduced.Published, Reproduced: In those adult trials, the posted tables bound the participants with serious suicidal behaviour (completed suicide, suicide attempt, intentional self-harm or intentional overdose) at 43 to 46 of 40,564 on antidepressants and 16 to 19 of 31,079 on placebo, and those with any serious suicidality at 71 to 81 against 36 to 43, because a participant listed under two of an outcome's terms may be one person or two. Across every count the tables allow, the Mantel-Haenszel risk ratio is 1.76 to 2.20 for serious suicidal behaviour (p 0.0097 to 0.0502) and 1.29 to 1.73 for any serious suicidality (p 0.0078 to 0.20). At the counts least favourable to an increase neither is significant after the registered Holm correction across the two co-primary endpoints (adjusted p 0.10 and 0.20); at the most favourable both are (0.016 and 0.016).
• Published, Reproduced.Published, Reproduced: Public reports of the trials (their publications, regulators' reviews and the sponsors' documents) settle how many participants share terms in 11 of the 17 adverse-event groups the tables leave open and narrow it in 3 more. With them, serious suicidal behaviour affected 43 of 40,564 adults on antidepressants and 17 to 18 of 31,079 on placebo (Mantel-Haenszel risk ratio 1.86 to 1.96; p 0.025 to 0.036), and any serious suicidality 72 to 77 against 40 to 41 (1.38 to 1.51; p 0.041 to 0.12). After the registered Holm correction across the two, the adjusted p-values are 0.071 and 0.12 at the counts least favourable to an increase and 0.0496 for both at the most favourable.

6 more claims

Foster and Rahmstorf (2026) remove El Niño, volcanic and solar influences from five global temperature records with a regression fitted to those records. They then report high confidence that warming accelerated, using critical values that treat the adjusted series as raw data. We ran their whole procedure, adjustment and tests together, on 2000 records per dataset, simulated under their own null: a straight-line trend since 1970 plus stationary noise. With noise fitted under that null, their changepoint test at nominal level 0.05 rejected 0.059 to 0.07 of null records, and the observed statistics had full-pipeline p of 0.0005 to 0.0025 in every record. Their quadratic test fared worse, with full-pipeline p up to 0.054. Under long-memory noise the changepoint evidence weakened, to p of at most 0.04, but held. The acceleration finding rests on the changepoint test.

• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: A numpy port of Foster and Rahmstorf's 2026 adjustment for El Niño, volcanic and solar influences reproduces their published adjusted NASA, NOAA, HadCRU, Berkeley and ERA5 series to within 0.0001 °C, and the changepoint test of Beaulieu et al. (2024) on the adjusted annual means for 1970-2024 gives maximum slope-change statistics from 4.91 to 6.68 with the change in 2013 or 2014 and nominal AR(1) Monte Carlo p-values from 0.00014 to 0.0033, against 0.041 to 0.19 for the unadjusted series.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: When 2,000 records per dataset are simulated under Foster and Rahmstorf's null hypothesis (a linear trend since 1970, their fitted exogenous terms, and ARMA(1,1) noise fitted under the null) and passed through their whole adjustment and changepoint test, the nominal 5% test rejects 5.9% to 7.0% of null records, and the observed statistics have full-pipeline p-values from 0.0005 to 0.0025 in all five records, so the changepoint finding is robust by the pre-registered rule.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Under the same full-pipeline null, Foster and Rahmstorf's quadratic test with the ARMA(1,1) correction of Foster and Rahmstorf (2011) rejects 5.8% to 8.0% of null records at nominal 5% on monthly values and 7.2% to 9.2% on annual means, and the observed quadratic terms have full-pipeline p-values from 0.0015 to 0.054 (monthly) and 0.0005 to 0.032 (annual), below 0.02 in only three records for monthly values and two for annual means, so the reported confidence above 98% in all five records does not hold and the finding is mixed by the pre-registered rule.

1 more claim

Ketamine relieves depression within a day, but patients feel its psychoactive effects, so its benefit could depend on that experience. We asked whether ketamine and esketamine lower depressive symptoms when every dose is given under general anesthesia. Under a registered plan, we coded randomized trials' dosing from their Methods alone and pooled effects (Hedges' g) one to three days after surgery or childbirth. In 23 masked trials (3202 participants), depressive symptoms were lower with the drug than with an inert control (g -0.61, confidence interval -0.81 to -0.4; Holm-adjusted p < 0.001), though trials varied widely. Across trials in surgery, awake dosing did not show a larger effect (difference 0.12, -0.24 to 0.48), but this compares trials, and the one trial that randomized timing favored awake dosing. Masked doses also lowered pain. Ketamine can lower depressive symptoms after surgery without reaching an awake patient; whether experiencing the drug adds to that, these trials can't say. This version corrects counts, checks, and a reading that the first version's reviews found wrong.

• Published, Reproduced.Published, Reproduced: In 23 randomized trials (3,202 participants) that gave every dose of ketamine or esketamine under general anesthesia, between its induction and the end of surgery or cesarean delivery, depressive symptoms 1 to 3 days after the procedure were lower than with an inert control (Hedges' g −0.61, 95% CI −0.81 to −0.40; Holm-adjusted p < 0.001), though the trials varied widely (95% prediction interval −1.51 to 0.29). The difference remained among the 17 of these trials that passed the pre-registered integrity screen (g −0.48, −0.63 to −0.33), among the 13 whose last dose is known to have ended more than 30 minutes before the end of surgery (g −0.67, −1.04 to −0.30), among the 19 whose doses all began after induction rather than with it (g −0.60, −0.85 to −0.36), and with any single trial left out (largest p < 0.001).
• Published, Reproduced.Published, Reproduced: The masked doses were pharmacologically active: masked ketamine lowered pain scores on day 1 or 2 after the procedure (g −0.55, 95% CI −0.97 to −0.14; 22 trials; g −0.38, −0.54 to −0.22 without the one trial whose printed dispersions can't be standard deviations), as awake ketamine did (g −0.33, −0.54 to −0.11; 32 trials; awake minus masked in surgery +0.32, −0.21 to 0.86). Masked ketamine still raised the odds of each trial's most frequent psychotomimetic adverse event (Mantel–Haenszel odds ratio 2.11, 1.48 to 2.99, in 22 trials), and awake ketamine raised them more (3.63, 2.97 to 4.43, in 40 trials): p = 0.0083 for the difference in the registered comparison, and p = 0.21 when the odds ratio may vary between trials (ratio of odds ratios 1.69, 0.74 to 3.84).
• Published, Reproduced.Published, Reproduced: The masked effect was also present in the 7 masked trials that enrolled only patients with depression or depressive symptoms (g −0.78, 95% CI −1.24 to −0.31), and later after the procedure: on days 4 to 14 (g −0.51, −0.90 to −0.13; 18 trials) and days 15 to 90 (g −0.54, −0.75 to −0.33; 11 trials). Among the masked trials whose doses all began after induction, the days 4 to 14 interval included zero (g −0.61, −1.33 to 0.12; 10 trials).

4 more claims

Many papers relate one National Health and Nutrition Examination Survey (NHANES) variable to one condition without correcting for multiple testing (Suchak et al. (2025)). We sampled 40 associations, reproduced each on its paper's cycles, and under a registered plan re-ran it on 2021–2023. There, 14 replicated as computed, and 10 with the survey design where papers ignored it. Most tests lacked power, but were every association true, 19 would replicate; counts this low are rare (0.047, or 0.011 with the design), so many effects are smaller than published or absent. In 36 papers the computation reproducing the estimate differs in some respect from the one described; as described, 6 fall outside the published interval.

• Published.Published: Of 40 associations sampled at random from those eligible among 341 papers that each relate one NHANES variable to one health condition (eligible meaning, among other rules, that its full text was open and that NHANES August 2021 to August 2023 could build its exposure, outcome, and population), 14 (35%; exact 95% confidence interval 21% to 52%, which treats the associations as independent) replicated in that cycle, meaning their estimate there has the published sign and a Benjamini-Hochberg-corrected p below 0.05, with each analysis computed as its paper's was. Of the 40, 15 were analyzed unweighted, ignoring the survey design, as their papers were; with those 15 fitted with the survey weights and design, as the plan also registered, 10 of the 40 replicated (25%; exact 95% confidence interval 13% to 41%).
• Published.Published: At an unadjusted two-sided alpha of 0.05, which bounds the power of the corrected replication decision from above, 13 of the 40 replication tests had at least 80% power to detect the published effect, taken as true, in the 2021 to 2023 cycle, and 10 of those replicated (77%; exact 95% confidence interval 46% to 95%); at the Bonferroni level of 0.05 over 40, which bounds it from below, 8 had that power, and 5 of them replicated. With the variance of the analyses re-run unweighted taken from the survey design, 13 tests had that power at the unadjusted level, 12 of them among the 13 above, and 9 of them replicated.
• Published.Published: On the analysis scale (log odds ratio or regression coefficient), the 2021 to 2023 effects are a median 0.77 times the published ones over all 40 associations (distribution-free 95% confidence interval 0.32 to 1.05) and 0.91 times (0.32 to 1.16) over the 13 informative ones; the intervals treat the associations as independent. The median is 0.53 over the 15 analyses re-run unweighted and 0.79 over the others; with the registered weighted fits in place of the unweighted ones, it is 0.85 (0.35 to 1.08).

12 more claims

An observational atlas linked GLP-1 receptor agonists to dozens of outcomes beyond glucose, weight and the heart. We pooled the serious adverse events that 234 placebo-controlled trials, with 161309 participants, posted to ClinicalTrials.gov, coded blind to the results under a registered plan. Reports of serious bacterial infection (ratio 0.88, confidence interval 0.83 to 0.93) and pneumonia (0.87) were less frequent on the drugs, as were pneumonia counted in people and death. The reductions held under random effects, with any trial left out, if infection terms overlapped within participants as all serious events do in each comparison, and in trials not coded as recording only on treatment. Of the atlas's associations with enough events to test, the trials found three in its direction with no difference from it detected, contradicted none, and left most inconclusive, among them every neurological and psychiatric one; its large hazard of drug-induced pancreatitis concerns a subtype the trials don't separate.

• Published, Reproduced.Published, Reproduced: Of the 539 interventional studies of GLP-1 receptor agonists with results on ClinicalTrials.gov on 2026-10-12, 234 randomized trials compare a GLP-1 receptor agonist with placebo, in 257 comparisons with 161,309 participants in their adverse-event tables (93,765 on the drugs and 67,544 on placebo). In them, reports of serious gallbladder and biliary disease, counting a participant once for each of the outcome's terms they had, are more frequent on the drugs (Mantel-Haenszel ratio 1.38, 95% CI 1.21 to 1.57), and so are reports of serious nausea and vomiting (2.02, 1.52 to 2.68), as the trials' own publications and the drugs' labels lead one to expect.
• Published, Reproduced.Published, Reproduced: Reports of serious bacterial infection, counting a participant once for each of the outcome's terms they had, are less frequent on GLP-1 receptor agonists in these trials (2,409 among 93,765 participants against 2,532 among 67,544 on placebo; Mantel-Haenszel ratio 0.88, 95% CI 0.83 to 0.93, q < 0.001), and so are reports of serious pneumonia (1,442 against 1,568; 0.87, 0.81 to 0.93, q = 0.0020); both stay significant under random effects and with any single trial left out. Counted in participants, pneumonia under its own preferred term, which no group reports in more than one row, is less frequent (807 against 880; 0.86, 0.79 to 0.95). If infection terms overlapped within a participant as all serious terms do in the same arm of the same comparison, bacterial infection would be 0.89 (0.82 to 0.97).
• Published, Reproduced.Published, Reproduced: In the registered scan without hypotheses of 27 organ systems and 518 preferred terms, with the same variance as the other claims, four organ systems (cardiac disorders; infections and infestations; metabolism and nutrition disorders; respiratory, thoracic and mediastinal disorders) and two preferred terms (acute myocardial infarction and cellulitis) are lower on the drugs with q < 0.05 in a random half of the trials and p < 0.05 in the held-out half, and one organ system, hepatobiliary disorders, is higher (1.36 in the first half, 1.24 in the second), as the gallbladder positive control leads one to expect. Among those lower are serious infection reports as a whole (0.88 and 0.89) and cellulitis (0.64 and 0.75); cardiac disorders and myocardial infarction are events many trials record as adjudicated end points rather than in these tables.

6 more claims

Primes other than $2$ fall into two classes modulo $4$, congruent to $1$ or to $3$, equally common in the long run, yet the class of $3$ is almost always ahead: Chebyshev's bias. Following the race exactly at every integer $x \le 10^8$, the class of $1$ first leads at x = 26861, and leads at only 30624 of the hundred million integers, in 128 stretches, none after x = 12382326. Weighting each $x$ by $1/x$, the class of $1$ leads on a share 0.00040587 of the race, about a tenth of the limiting share Rubinstein and Sarnak (1994) computed under two standard hypotheses, so the race is still short of its limiting behavior this far out. Modulo $3$, primes congruent to $2$ lead those congruent to $1$ strictly at every $x$ from $2$ to $10^8$, consistent with the first reversal Bays and Hudson (1978) found near $6.1 \times 10^{11}$.

• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: The least x at which the primes up to x congruent to 1 modulo 4 outnumber those congruent to 3 modulo 4 is 26861.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Of the integers x from 1 to 100000000, the primes congruent to 1 modulo 4 lead at exactly 30624, in 128 separate stretches, the last ending at x = 12382326, and the two classes are tied at exactly 3866 integers, the last being x = 12424002.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Weighting each integer x from 1 to 100000000 by 1/x, the primes congruent to 1 modulo 4 lead on a share 0.00040587 of the race, about a tenth of the limiting share of about 0.0041 implied by Rubinstein and Sarnak's logarithmic density of 0.9959 for the other side.

2 more claims

A nominal $95\%$ confidence interval for a binomial proportion should contain the true proportion $p$ in about $95\%$ of samples. Computed exactly, with nothing simulated, for every sample size $5 \le n \le 100$ and every $p$ on a grid of step $0.001$, the textbook Wald interval covers $p$ less than $0.93$ of the time at a fraction 0.463088 of the 95904 $(n, p)$ pairs, and averages 0.88228. The Wilson score interval falls below $0.93$ at a fraction 0.032981 of them, and the Agresti-Coull interval at 0.003681. The Clopper-Pearson interval never covers less than $0.95$, but averages 0.970942, so it is wider than it needs to be. Adding one observation can lower the Wald interval's coverage by more than a tenth. These values reproduce, on a fine grid and with every value declared, the behavior Brown, Cai and DasGupta (2001) described.

• Published, Reproduced, Reviewed, Replicated.Published, Reproduced, Reviewed, Replicated: Over every sample size n from 5 to 100 and every true proportion p from 0.001 to 0.999 in steps of 0.001, the exact coverage of the nominal 95% Wald interval for a binomial proportion is below 0.93 at a fraction 0.463088 of the 95904 (n, p) pairs and below 0.95 at a fraction 0.923027 of them.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Over the same 95904 pairs, the coverage of the nominal 95% Wilson score interval is below 0.93 at a fraction 0.032981 of them and that of the Agresti-Coull interval at a fraction 0.003681, with mean coverages of 0.952036 and 0.958695 against the Wald interval's 0.88228.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: The nominal 95% Clopper-Pearson interval covers at least 0.95 at every one of the 95904 pairs, with a lowest coverage of 0.9502, and its mean coverage of 0.970942 exceeds the nominal level by about 0.021.

2 more claims

Adding floating-point numbers one after another loses a little at each step, and how much depends on the order of the additions. For sums of up to a million doubles, drawn uniformly from $[0, 1)$ and from $[-1, 1)$, this study measures how far four common methods land from the correctly rounded sum, in units in the last place (ulps). Adding left to right, the error averages 196.86 ulps for a million positive values and grows with their number $n$ as about $n^{\alpha}$ with fitted $\alpha$ = 0.545, close to the square root that independent rounding errors predict. Pairwise summation stays within 2 ulps at every length. Kahan's and Neumaier's compensated sums return the correctly rounded sum in all 400 draws, including mixed-sign sums that nearly cancel. Every value is reproducible exactly, on any machine and Python version.

• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Adding 1000000 doubles drawn uniformly from [0, 1) from left to right lands a mean of 196.86 units in the last place (at most 589) from the correctly rounded sum over 50 draws, and the mean error grows as about n to the power 0.545 for n from 1000 to 1000000, near the square-root growth that independent rounding errors predict.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Pairwise summation of the same positive draws stays within 2 units in the last place of the correctly rounded sum in all 200 draws for n from 1000 to 1000000, with a mean error of 0.4 units at n = 1000000.
• Published, Reproduced, Reviewed.Published, Reproduced, Reviewed: Kahan's and Neumaier's compensated sums equal the correctly rounded sum in all 400 draws, positive and mixed-sign, including mixed-sign sums of 1000000 values whose median condition number is 991.

1 more claim

How often do stars like the Sun release superflares of $10^{34}$ erg or more? A recent Kepler analysis found once per century, far more often than earlier ones. We tested this with TESS: a pre-registered search of the two-minute light curves of 32908 stars selected as that analysis selected its Sun-like stars, with flares of known energy injected into every light curve to measure what it finds. It counted 78 superflares where the once-per-century rate predicts 23.4: 3.33 times that rate (interval 2.63 to 4.15), one per 33 years per star, far above the earlier rates. Every planned subset and sensitivity analysis gives a ratio above one. An exploratory emulation of the Kepler search suggests its correction for missed flares, measured with the profile it injected, understates the rate of flares shaped as assumed here by a factor of 1.79 between $10^{34}$ and $10^{35}$ erg; its published rates don't follow from its own figures, so how much of the gap is Kepler's remains open. All of it rests on the stars selected and the flare energies and shapes assumed.

• Published.Published: In 94,747 TESS 2-minute light curves of 32,908 stars of 5000 to 6500 K with absolute G magnitudes of 4 to 6 and RUWE below 1.4 (5,605 star-years), the pre-registered search, with its SAP test corrected after registration to require the uncorrected flux to rise, counted 78 flares of bolometric energy 10^34 erg or more where the rate Vasilyev et al. (2024) measured with Kepler predicts 23.4 under the search's measured completeness and the assumed flare durations: 3.33 times that rate (95% CI 2.63 to 4.15), about once per 33 years per star; the registered code counted 79 (3.37 times, 2.67 to 4.20).
• Published.Published: The same TESS data are incompatible with the earlier Kepler rate of one superflare of 10^34 erg or more per 2,500 years on Sun-like stars, which under the same completeness predicts 1.04 counted flares where 78 were found (Poisson probability below 10^-100).
• Published.Published: Among the 18,203 stars of 5500 to 6000 K whose median TESS variability range is below 0.3%, the 50 counted superflares are 3.63 times (95% CI 2.70 to 4.79) the 13.8 that the rate Vasilyev et al. (2024) give for their Sun-like stars predicts.

5 more claims

Guaranteed income, regular cash with no conditions, has been tested in many American cities and in national pilots, and its advocates expect it to improve mental health without reducing work. We pre-registered a meta-analysis of randomized trials of flat, unconditional cash in high-income countries, searching databases, registries, and the reports most pilots publish outside journals; 62 trials were eligible and 53 had results. About a year into payments, mental health was better in the cash arms by 0.09 standard deviations (CI 0.041 to 0.139) across 34 comparisons in a random-effects model, but the common-effect estimate, which weights the largest trials most, was -0.002 (-0.023 to 0.018), and smaller trials reported larger effects. Employment changed by 0.599 percentage points (-2.533 to 3.731), and the mental-health effect did not fade during payments. Any mental-health benefit of guaranteed income is small and confirmed only in small trials, and about a year in it does not detectably reduce employment.

• Published, Reproduced.Published, Reproduced: In 34 comparisons from 32 randomized trials of recurring unconditional cash in high-income countries (16,834 people analysed), mental health about 12 months into payments was better in the cash arms by a pooled standardized mean difference of 0.090 (95% CI 0.041 to 0.139; Holm-corrected p = 0.002) in the pre-registered random-effects model, but the pre-registered robustness checks failed: the common-effect estimate, which weights the largest trials most, was -0.002 (-0.023 to 0.018), the estimate among the 6 comparisons that kept at least 60% of those randomized was 0.043 (-0.077 to 0.163), and smaller comparisons reported larger effects (Egger's regression slope 1.54, 95% CI 0.75 to 2.33; p < 0.001).
• Published, Reproduced.Published, Reproduced: In exploratory analyses added after registration, the larger mental-health benefits came from small comparisons and from shares above a cut-off: the 7 comparisons with at least 500 people analysed pooled to 0.041 standard deviations (95% CI -0.079 to 0.161) against 0.107 (0.052 to 0.163) for the other 27, and estimates from scale scores pooled to 0.051 (0.007 to 0.096) against 0.233 (0.084 to 0.381) for shares above a cut-off converted to standard deviations (difference 0.147, 0.037 to 0.258).
• Published, Reproduced.Published, Reproduced: Of the 32 eligible registered trials of unconditional cash whose primary completion or end date was at least 12 months before 2026-10-17, 8 had reported no results this review could find, among them the Chicago Resilient Communities Pilot (AEARCTR-0009656), registered with 11,915 participants.

4 more claims

The World Health Organization's 2020 guideline recommended giving mass azithromycin, which lowers child mortality in high-mortality settings of sub-Saharan Africa, only to infants, to limit antibiotic resistance; no trial had then tested that. Under a pre-registered plan we pooled every randomized trial by whom it treated. Treating all children under five lowered their mortality by 14.1% (CI 7.4% to 20.3%), consistently across trials. In the three trials that treated only infants, infant mortality was not detectably lower (rate ratio 0.971, CI 0.867 to 1.086), an interval that excludes the effect of treating all children. Infants had lower mortality when all children were treated, though a between-trial comparison of the two strategies fell short of significance, and giving azithromycin to individual infants at clinic visits showed no effect. The infant-only approach has not lowered mortality in any trial that tested it; treating all children under five has.

• Published, Reproduced.Published, Reproduced: In 5 placebo-controlled comparisons from 3 cluster-randomized trials (MORDOR in Niger, Malawi and Tanzania; AVENIR in Niger; CHAT in Burkina Faso), twice-yearly mass azithromycin to every child 1 to 59 months old lowered mortality among children 1 to 59 months by 14.1% (rate ratio 0.859, 95% CI 0.797 to 0.926; Holm-corrected p = 0.015; I² = 0%), and the reduction held with a common-effect model (0.859, 0.813 to 0.908) and with any one comparison left out (largest p = 0.044).
• Published, Reproduced.Published, Reproduced: Infant mortality was lower when all children 1 to 59 months were treated (rate ratio 0.823, 95% CI 0.707 to 0.958; 3 comparisons) than when only infants were (0.971), but the pre-registered meta-regression comparing the two strategies across trials did not establish a difference (ratio of rate ratios 1.187, 95% CI 0.974 to 1.447; p = 0.074; Holm-corrected p = 0.148); AVENIR's within-trial contrast of its all-children arm against its infant arm, estimated after registration from the two arms' printed mortality rates, was 0.830 (0.717 to 0.959).
• Published, Reproduced.Published, Reproduced: Across the 8 mass-distribution comparisons against placebo, mortality fell more where the control arm's mortality rate was higher: the log rate ratio changed by -0.078 per unit of the log control rate (95% CI -0.144 to -0.013; p = 0.027), allowing for strategy, in a pre-specified descriptive analysis resting on few comparisons, one of whose rates comes from birth histories.

4 more claims