The shelf life of LLM findings
Stanford University
November 2, 2026
How long does a published finding about LLMs remain true? We revisited 50 widely cited findings about LLMs across 20 models. Within 15 months of publication, most of the LLM claims we tested either no longer held or showed substantially diminished effects. What we know about AI may have a surprisingly short shelf life.
Fitted effects on September 30, 2026. How we classify claims.
In 2023, Walters and Wilder asked ChatGPT to write short literature reviews and then tried to find every work it cited. At the time, ChatGPT used GPT-3.5, and 55% of its citations were fake (C11). We sent the same prompts to recent models (GPT-6.1-Sol and Claude Sonnet 5.5) and found that they rarely output fabricated citations, though some models still do. We cannot assume claims made on yesterday’s LLMs hold on today’s more capable models.
We test a broad range of 50 LLM claims, from sycophancy and jailbreaks to long-context capabilities and cultural biases. By analyzing 20 models, released from July 2024 to September 2026 across eight different model developers, we see how claims change as a function of model release date. Our models span large and small, open- and closed-weight. For each claim, we run the same setup across our panel of modern models and fit trend lines to how the effect changes over time.
We classify claims as expired, weakened, persists, or strengthened, according to how much of the original effect remains by September 2026. A relative effect size (e) of 1 means the effect is as strong as in the paper, and 0 means it is gone. An expired claim describes an effect that has largely disappeared in newer models. We use a fifth of the paper’s effect or less as the expiration zone; a claim can expire even if the effect remains strong in some individual models. For expired claims, we estimate how long after publication the effect crossed into this expiration zone. The results below show which findings have faded, which hold up, and how long they last. Reproduction checks and metric definitions follow in How we measure claim persistence.
Results
Almost half (44%) of our tested claims are now expired in today’s models. Another 34% have weakened significantly, 16% persist, and 6% have strengthened relative to the original claim. Persistence varies by topic. Five of nine reasoning claims and six of eleven sycophancy-and-deception claims are classified as expired. Three of ten claims about models as judges, reviewers, and raters persist or strengthen. The three strengthened claims concern judges’ self-preference (C28), praise that follows a user’s preference (C17), and nonuniform random-number generation (C29).
The pie shows the percentage of all claims in each category; the bars count claims within each research area. Select an area or segment to browse its claims.
Which claims expire, and when
- Expired 22 claims Mostly capability failures that newer models no longer make: counting letters, arithmetic in other bases, finding facts in the middle of long contexts, fabricating citations, and abandoning correct answers when challenged. Other findings also faded: leaking private details from meeting summaries, more nonanswers in Arabic than in English, and preferring AI-written abstracts. The last of these reverses direction in the fitted trend, rather than merely fading to zero.
- Weakened 17 claims Weaker but still existent: structural limits such as the reversal curse, two-hop questions and multi-turn instructions, plus residual social biases, judges’ preference for longer answers, invented package names, niche-domain hallucinations, and susceptibility to jailbreaks and prompt injection.
- Persists or strengthened 8 persist · 3 strengthened Mostly preferences and judgment rather than capability: flattering and agreeing with users, judges that favor their own answers, near-identical answers to open prompts, a left political lean, and answering when they should abstain.
How to read this plot
One row per claim, in order of publication by default. The circle marks when the paper came out and is colored by the claim’s verdict in September 2026; for expired claims, a line runs to the estimated expiration date.
Select Lifetime to put the longest estimated lifetimes first; claims without an estimated expiration date follow in publication order. Select Publication date to restore the original order. The active sorting button is highlighted in black. Select Show uncertainty to show an error bar for each expiration: the 95% interval of the fitted date, or, for a claim already expired on the first model released after its paper, the whole window between the paper and that model (the tick is then the window’s midpoint). A wide interval means the effect declined gradually. Select a claim to open its card.
How long do claims last before they expire?
Across all 50 claims, the estimated share that had expired was 4% six months after publication, 16% after one year, and 39% after two years. These estimates account for claims not yet expired at the end of observation. The share of claims still at full strength (e ≥ 0.8) falls from 64% six months after publication to 47% after one year and 31% after two years.
Among the 22 claims with an estimated expiration date shown in the timeline, time from publication to expiration averaged 15.7 months (median: 14.7 months). These summaries exclude claims that have not expired. Lifetimes vary widely, even within the same research area.
Select a dot to explore the claim. The chart groups the 22 expired claims by research area.
Areas that expire faster on average tend to be those optimized for in post-training pipelines, and those that take longer to expire are those more centered around bias and judgment. This roughly tracks the percentage of claims that are expired per research area. Note that the “Science, research ideas & peer review” area contains only one expired point, the fake citation claim (C11).
How we calculate these durations
We subtract the paper’s publication date from the expiration date shown in the timeline, converting days to months using 365.25 / 12 days per month. Nineteen claims have a dated expiration after publication. Two of these, premise-order proofs (C22) and Arabic nonanswers (C50), are dated from the newest-model count because their fitted curves do not reach the expiration line. Three more claims have only an expiration window; we use the timeline’s displayed estimate within that window.
For blackmail (C44), the fitted curve retains all reliable models, including those flagged as outliers by the standard procedure. Its estimated expiration date is September 9, 2026 (95% interval: April 8–September 26), about 15 months after its first public release by Anthropic on June 20, 2025. Support for this verdict is weak, and several recent models still blackmail frequently. For strawberry letter counting (C35), the starting date is the closest published evidence, not the first appearance of the informal claim.
The plot uses estimated expiration dates rather than exact observed failure times. It does not propagate uncertainty in those dates; you can see their intervals with the timeline’s uncertainty toggle. Publication also occurs after the underlying experiments, so these durations measure how long a published claim remains supported by this panel, rather than time since the original experiment.
The shares at the start of this section (4%, 16% and 39% expired after six months, one year and two years) use the Kaplan–Meier estimator over all 50 claims. Claims not yet expired are right-censored at the time from publication to September 30, 2026. The mean and median time to expiration above use only claims with an estimated expiration date shown in the timeline, including the displayed midpoint for expiration windows. The full-strength shares use only the claims old enough to be measured at each interval (47, 45, and 36 claims). Older findings have had longer to age: 11 of 21 claims from 2022–23 and 9 of 19 from 2024 are expired, compared with 2 of 10 from 2025.
The life of LLM claims
The claim cards show which claims have expired and how fast, ordered by when the original paper was released. Each card pairs the original paper’s evidence with the same test across model releases. Select a paper visual to enlarge it, and use dropdowns to filter by research area and verdict.
About the card: plots, methods & data
Reading the model-release plots
Dots show individual models; colored curves show the fitted trend. Black diamonds mark our reproductions on original or substitute models. Bands and whiskers show 95% intervals; hollow points are excluded from the fit. Switch to Relative to compare with the reference effect (1) and the expiration value (0). The reference is the paper’s effect, except for strawberry (C35), which uses our original-model reproduction.
Outliers and inclusion
We flag and exclude up to 20% of eligible panel points as outliers before filtering by release date. Outliers can therefore account for a larger share of the models eligible by date. Strawberry letter counting (C35) and blackmail (C44) retain all trend outliers. Strawberry retains control failures; the additional newest-model count keeps outliers for all claims. Including the outliers in the curve changes no labels.
Limits of the panel
This analysis combines saved outputs with October 2026 runs. Four 2024 models anchor the early release cohorts, so early expiration dates rest on few observations. Each claim uses one minimal design. Retired original models or judges require labeled substitutes, which provide weaker reproduction evidence.
Scoring and response lengths
Peer-review scoring (C31) uses explicit recommendation fields in saved reviews; two-hop scoring (C1) extracts final answers after reasoning preambles. Both use the original paper scorers. Strawberry’s control accuracy (C35) is reported as a diagnostic and does not determine inclusion. Haiku’s two-hop evaluation and DeepSeek V3’s letter-counting evaluation use higher output-token caps to accommodate longer responses.
The premise-order checker (C22) accepts a valid proof whether it states the conclusion first or last. The MCQ position-bias test (C12) compares each model with its own chance spread, from shuffling answer positions within each question. Social sycophancy (C40) subtracts each model’s false-positive rate, against the paper’s matching value.
How much of each effect remains today?
Claims in the same category can still have very different effect sizes. Among weakened claims, for example, the fitted effect is about one-quarter of its reference magnitude for basic prompt injection (C2) and implicit word-association bias (C48), about one-half for the reversal curse (C13), and nearly three-quarters for legal hallucinations (C20). All are weaker than the original finding, but they are far from equally diminished. To illustrate this, we show where each claim stands as of September 30, 2026 (the last date that any of our tested models were released).
Fitted effect on September 30, 2026, with 95% intervals. e = 0 means no effect; e = 1 is the paper’s effect. Select a row to open its claim card above.
A larger e means more of the original effect remains, but it does not necessarily mean the behavior is more common or more harmful.
Interpreting effect sizes and uncertainty
Each dot is the fitted release-date trend evaluated at September 30, 2026, using 9–20 eligible panel models per claim across release dates. It is not a measurement on a single recent model or an average of only the newest models. The 95% bootstrap intervals reflect uncertainty in the fitted trend, including the reproduction anchor, rather than the spread of individual models’ effects.
At the other end, the three strengthened findings are self-preference in LLM judges (C28), praise that follows the user’s stated preference (C17), and nonuniform random-number generation (C29). Their fitted effects are about 2.36, 1.85, and 1.70 times their reference magnitudes, respectively. For self-preference, the reference is a small 4.6-percentage-point difference between GPT-4’s preference for its own summaries and GPT-3.5’s preference for those same summaries.
The intervals also vary across claims. For judges’ preference for longer answers (C27), the fitted effect is 0.65, but its interval spans 0.32–1.16; the point estimate suggests weakening, while the original magnitude remains compatible with the fit’s uncertainty.
What changes from model to model?
From GPT-4o mini (earliest model we tested, released in July 2024) to GPT-6.1 Sol (latest model we tested, released in September 2026), we see big shifts in the persistence of claims. The number of claims in the expiration zone rises from 5 to 30 out of 50, while the number that still hold or are stronger falls from 30 to 11. This gives a model-level view of the broad decline seen in the fitted trends. Each model’s claims are sorted from lowest to highest effect, so a claim’s horizontal position can change when you switch models; use its label or the category lists below the plot to follow it.
For each reliably scored model–claim pair, we apply the thresholds to that model’s measured effect e. Expired means e ≤ 0.2, without requiring its interval to lie below that threshold. Persists means 0.8 ≤ e < 1.5 and the lower bound of the 95% interval exceeds 0.2. Strengthened means e ≥ 1.5 with the same interval requirement. All remaining pairs are labeled weakened (“weaker” in the chart), including large point estimates whose intervals still reach the expiration zone. These labels describe one model on one claim, so they do not use the fitted release-date trend.
One model, all 50 claims. Points show effects and 95% intervals; black ticks mark our reproductions. Choose a model above the chart or inspect a category below it.
Release date alone does not determine the pattern. Among models released in July–September 2026, the expired count ranges from 11 for DeepSeek V4 Pro to 30 for GPT-6.1 Sol. Qwen3.7-Flash has 14, GLM-5.3-Flash 19, and GPT-6 Luna 25. The patterns are also not perfectly aligned with model providers or model size. Hollow points are not scored reliably and are excluded from the category counts.
Refusals or unscorable responses
Eight of the 1,000 model–claim points are flagged because frequent refusals, incomplete responses, or answer-extraction problems prevent a reliable comparison. These include political-test and decoding refusals, too few usable paired verdicts, and answers our parser cannot consistently extract. We show these points in the plots, but do not use them in the trend fits or model-level category counts.
The totals hide the quirks unique to individual models. Claude Sonnet 5.5’s self-preference effect (C28) is close to the paper’s magnitude (e = 1.09), whereas GPT-6.1 Sol’s is larger (e = 2.88). The pattern reverses for preference for longer answers (C27): Sonnet retains that effect (e = 1.12), while Sol’s point estimate is near the expiration value (e = 0.09). Neither model has lost every tendency: both show stronger-than-reference praise following a user’s preference (C17) (e = 1.85), and both remain highly nonuniform when asked for random numbers (C29) (e = 1.87).
A claim’s panel-wide verdict can therefore differ from what you see on one model. Citation fabrication (C11) is classified as expired overall, yet Qwen3.7-Flash fabricated 69% of references in this test, compared with about 1% for Sonnet 5.5 and 0% for Sol. The plot is most useful for finding such exceptions and opening the corresponding claim card to inspect the original metric and protocol. It is a profile of measured behaviors, rather than a general-purpose model leaderboard.
Case Study on Hallucinated References
The citation example (C11) lets us examine what a declining effect looks like in the generated text. Here, the measured outcome is the share of references that cite nonexistent works. Errors in the bibliographic details of real publications are a separate outcome.
Share of cited works that were fabricated, by type of work, from Walters & Wilder (2023), Table 3.
The original results show why fabricated references could be difficult to spot. Among the invented articles from both GPT-3.5 and GPT-4, only 2% named a nonexistent journal. The rest named real journals, giving readers plausible-looking citations to works that did not exist. Fabrication also varied by publication type: 73% of GPT-3.5’s cited journal articles were invented. GPT-4 improved on GPT-3.5 but still fabricated 18% of its references overall.
We repeated the paper’s literature-review prompts across 42 topics, using GPT-3.5 Turbo as the closest available reproduction model and each model in our panel. We checked the generated references against bibliographic databases. GPT-3.5 Turbo fabricated 59% of its 210 references, close to the paper’s 55%, giving us a comparable starting point for measuring change.
A struck-through reference has no matching record in the databases; a ticked one matches a real publication. The tabs show three selected prompts from the 42 topics.
On the gap-year prompt, all 5 of GPT-3.5 Turbo’s references were invented: generic author names, real journals, and papers that do not exist. The recent models shown cite real studies, such as Martin (2010) in the Journal of Educational Psychology. These selected examples illustrate the difference in the outputs, and the plot below measures fabrication across all topics for each model.
The shaded expiration zone is a relative effect size (e) of 0.2 or less, a fifth of the paper’s effect. The shaded alive zone is the 95% interval of our reproduction on the paper’s model.
The decline extends beyond the displayed examples. Across all topics, Claude Sonnet 5.5 fabricated 1% of its references and GPT-6.1 Sol 0%. The high fabrication rate in the original study has largely disappeared in most recent models under these prompts, although the model-level exceptions shown above remain.
This observation has motivated a number of policies where hallucinated references serve as a primary metric for detecting AI-generated work, a prominent concern in conferences and journals. ICLR 2026 reported desk-rejecting papers with hallucinated references, and ICML 2026 lists hallucinated references among its grounds for desk rejection. However, our results suggest that these phenomena might not occur at as high of a frequency as with older models, making such policies a poor direction to discourage AI-generated writing without human oversight. Beliefs formed around an earlier generation of models need to be tested again, and our investigation here is an example of how priors about LLM behavior must be updated with future model releases.
How we measure claim persistence
For the claims shown and cited in the Results section, we first take a key metric from each paper and put it on a common scale that measures change relative to the paper’s result. Second, we check that we can reproduce the paper’s central result within some tolerance. Third, we run the same setup across our panel of modern models and fit trend lines to how the effect changes over time. The sections below detail these steps.
Paper release dates
We date a paper from its earliest publicly accessible version, including preprints and full reports released by the authors. For arXiv, we use the first posting (v1), not the latest revision or the later conference or journal date. A verified earlier public release takes precedence: the blackmail report (C44), for example, was released by Anthropic on June 20, 2025, before its October arXiv posting. Each claim’s source details link to the evidence for its date.
The strawberry date (C35) belongs to the related letter-counting paper, not the first appearance of the informal claim. For Artificial Hivemind (C45), October 27, 2025 is the earliest verified paper date; we could not establish whether its OpenReview version was publicly accessible earlier.
Standardizing claims to a single scale
Each claim comes with its own metric, such as fabrication rate, gap between two conditions, or entropy of a random draw. To compare them, we rescale each claim to a relative effect size e, where 1 means the effect is as strong as in the paper and 0 means it is gone. The anchor for 0 is a claim-specific expiration value: the metric value at which the claimed effect is absent.
e = (model value − expiration value) / (paper value − expiration value)
When the expiration value is higher than the paper value, the denominator is negative, so the scale automatically reverses direction. Moving toward the expiration value still lowers e from 1 to 0, while moving beyond the paper value in the claimed direction raises e above 1.
For citation fabrication (C11), the metric is the share of fabricated references: the paper value is 55%, and the expiration value is 0% (no fabricated references). Claude Sonnet 5.5 fabricated 1.37% of its references, giving e = (0.0137 − 0) / (0.55 − 0) ≈ 0.025, or about 2.5% of the paper’s effect. GPT-6.1 Sol fabricated none in our evaluation, giving e = 0.
The category cut-offs are on this scale. An effect at or below 0.2, a fifth of the paper’s, is in the expiration zone. At or above 0.8, it retains at least 80% of the paper’s effect. At or above 1.5 it meets the magnitude threshold for strengthened. The final categories also account for uncertainty and trend, as detailed below. Between 0.2 and 0.8 it has weakened.
The shaded alive zone in the model-release plots is the 95% interval of our reproduction on the paper’s model, rescaled to e. Its bounds vary by claim and show the reproduced reference effect and its uncertainty. The 0.8 cut-off above is used for classification; the shaded band follows the reproduction’s interval.
Choosing the expiration value
Expiration values are defined per claim: for example, zero fabricated citations (C11), 50% stereotype-congruent choices (C9), or the entropy of a uniform random draw (C29). For peer review (C31), the reference is the gap between accepted and rejected papers scored by human reviewers.
For two claims the expiration value differs by model, because chance itself depends on the model’s answers. For answer-position bias in multiple-choice questions (C12), it is the accuracy spread across answer slots that a permutation test expects by chance for that model. For fake references swaying an LLM judge (C23), it is the attack success a judge voting at random would reach on that model’s votes.
Direction and uncertainty
A drop in performance can still give a positive e. For example, if shuffling premises lowers proof accuracy (C22), a model showing that same drop has a positive e.
We rescale each model’s 95% interval using the same formula. Before fitting, values are clipped to the range −1 to 3, so one extreme model cannot dominate a fit.
Validating reproduction
We compare reproduced effects with the paper’s reported values on the same relative-effect scale used for the panel, i.e., the paper’s effect is 1 and the claim-absent value is 0. Of the 48 claims in the numerical reproduction comparison, 25 use an exact model match while the others use substitutes or proxies. For papers whose original models were no longer available via API endpoints, we use a close match with a similar release date. We apply the same reproduction criteria to exact models, substitutes and proxies. We use agents (Claude Code and Codex) to implement the analysis pipelines and check whether they reproduce values similar to those reported in the papers.
Of the 48 claims in the reproduction check below, 43 reproduce within our magnitude or uncertainty tolerance and 5 show stronger effects. (See caveats below for 2 claims not included in this count.)
Reproduction criteria and examples
We count two kinds of reproduction. Both require a 95% interval entirely above 0 on the relative-effect scale, establishing an effect in the paper’s direction. A reproduction is two-sided if its point estimate is between 0.75 and 1.25, inclusive, or its 95% interval contains 1. If neither condition holds, it is one-sided when the point estimate exceeds 1.25. These names describe magnitude tolerances, not one- or two-sided statistical tests. An interval containing 1 means the paper’s magnitude is compatible with our uncertainty; it does not establish that the effects are equal.
A smaller point estimate can therefore meet the two-sided criterion. The African American English effect (C24) is 0.57 of the paper’s effect, with a 95% interval of [0.08, 1.08]; the lost-in-the-middle effect (C7) is 0.68 [0.22, 1.18]. Both intervals exclude 0 and contain 1. We apply the interval criterion as well as the 25% point-estimate tolerance.
For example, the citation-fabrication claim (C11) reproduces two-sided: we measured 58.6% fabricated references, close to the paper’s 55%. In contrast, the claim that LLM judges change their verdict when answer order is swapped (C4; Wang et al., 2023) reproduces only one-sided: we measured a 62.5% verdict-flip rate (95% interval: 51.3–72.5%), compared with the paper’s 46.3%. This supports the claimed sensitivity to answer order even more strongly, but does not match its reported magnitude. Both reproductions used same-family substitutes for the original models.
Caveats for reproducibility
- Strawberry letter counting (C35): This claim has no numerical paper reference. We normalize to our GPT-4o May 2024 reproduction (4 errors in 10 trials), so e = error rate / 0.4. It is excluded from the numerical paper-reproduction comparison.
- Artificial Hivemind (C45): Our panel includes five models from the original study. For each model, we use 20 samples per query rather than the paper’s 50. We show the paper’s reported per-model results separately; its unreleased raw outputs cannot be rescored. Its fitted interval is [1, 1] because the curve is constant and fixed at the paper reference, with no uncertainty assigned to that reference. This does not mean we know the effect exactly.
- Reanalysis of released results: For contradictory timeline answers (C47), we rescored the authors’ saved GPT-4 answers; for preference for AI-written abstracts (C49), we analyzed their saved GPT-4-1106-preview selection counts. These two cases are included in the exact-model count, although we did not generate fresh model responses.
The paper’s effect is 1. Blue points reproduce within magnitude or uncertainty tolerance; orange points show stronger effects. Error bars show 95% intervals. Select a claim to open its card.
Fitting how each claim changes over time
Single models are noisy, and models from different developers can disagree. So rather than determining a claim’s status based on a single model, we fit a smooth curve over a set of models by release date. We choose a panel of 20 models that were released between July 18, 2024 and September 29, 2026 across eight different model developers, with a slightly higher number of recently released models. Our models span large and small, open- and closed-weight.
We evaluate panel models under each provider’s default API configuration. We leave reasoning effort and optional thinking modes at those defaults, without tuning effort separately for individual models. Those defaults differ across models. For example, GPT-5.2 reported no reasoning tokens in the overthinking evaluation (C36), while other models used reasoning. The comparison therefore concerns default configurations, without a common reasoning budget. In particular, the overthinking result measures token overhead in the tested configurations; it does not establish that the effect disappears when optional reasoning is enabled.
The curve starts at our reproduction on the paper’s model, the claim as it stood when the paper came out, and runs through the panel models released after it. Our primary criterion for an expired claim is that its fitted curve reaches e ≤ 0.2 and stays there through September 2026. An additional count of the newest models classifies two further claims as expired, as detailed below. For the other claims, the curve’s value at September 2026 gives the category. The date where the curve falls into the expiration zone gives an expired claim’s expiration date.
Fitting the curve
We require the curve to pass exactly through our reproduction on the paper’s model at that model’s release date. We fit it to panel models released on or after that date, and plot older models without using them in the fit. For C45, which we could not run on the paper’s model, the curve starts at the paper’s own value at the publication date.
A Theil–Sen line flags outliers more than three robust standard deviations away, capped at 20% of the eligible panel points before filtering by the reproduction model’s release date. Outliers can therefore make up more than 20% of the models that remain after the date filter. Theil–Sen is a line through the median of pairwise slopes, so a few unusual models do not move it. Outliers are still plotted.
For strawberry letter counting (C35), we retain all 20 models, including those that fail the control question. Control accuracy is diagnostic only, and no models are excluded as trend outliers. For blackmail (C44), we also retain all reliable models, including those flagged as trend outliers, so its displayed curve and expiration date reflect the high-rate models.
On the retained points we fit a constant, linear, exponential and logistic curve, each passing through the reproduction, and keep the one with the lowest AICc.
We bootstrap the models 500 times for uncertainty. For each bootstrap sample, we also draw a starting value from the reproduction’s 95% interval. The band therefore starts as wide as the reproduction’s error bar. We also test whether requiring the curve to pass through the reproduction worsens its fit to the panel. For three claims (C22, C36, C40), the fit improves significantly when we let the curve miss the reproduction. The reproduction may therefore lie off the trend followed by later models. We still use the anchored curves, with this caveat.
Categories and claim status certainty
Our primary criterion for an expired claim is that its fitted curve reaches e ≤ 0.2 and remains at or below that threshold through September 2026. This concerns the fitted curve itself, not its entire confidence band. Twenty of the 22 expired claims meet this criterion.
We also classify a claim as expired when at least four of the eight panel models released in the last six months (April to September 2026) have e ≤ 0.2. We count each model’s point estimate, including outliers, without requiring its confidence interval to fall below the threshold. It adds two claims—premise-order reasoning (C22) and Arabic nonanswers (C50)—whose fitted curves remain above 0.2, but for which five of the eight newest models are in the expiration zone. Both would be weakened by their fitted curves alone. The overview plots show fitted effects, so these two expired claims can have higher dots than weakened claims.
The other categories come from the fitted value at September 2026 and its 95% bootstrap interval. A claim persists when e is at least 0.8 and the bottom of its interval is above 0.2. It has strengthened when e is at least 1.5, or when the whole interval is above 1 and the trend rises significantly. A claim in between, or one at or above 0.8 whose interval stays below 1 and whose trend falls significantly, has weakened. A claim whose interval spans 0.2 to 1 would be uncertain; none of the 50 are.
We also fit the same anchored curve separately to open and closed models and to small and large ones. When one class persists while the other is expired, the claim keeps its category and its card notes the split. For each expired claim, we check how many recent models agree and whether the fitted interval stays in the expiration zone with and without outliers.
Recent-model agreement requires a strict majority of reliable models released in the last six months to have measured effects at e ≤ 0.2, including outliers. We use the point estimates here; we do not require each model’s interval to establish that the effect is expired. Robust trend evidence requires the fitted September 30 effect’s 95% upper bound to be at or below 0.2 both with and without outlier exclusion.
A claim has strong support if it passes both checks, moderate support if it passes one, and weak support if it passes neither. The cards show the counts and both fitted intervals under support for the expired verdict. Both checks use the same panel, so they are not independent tests and the label is not a calibrated probability. The label does not change the claim’s category or estimated expiration date.
Expiration date
Only claims in the expired category get an expiration date. The expiration date is the date where the fitted curve falls to e ≤ 0.2 and stays there. When the curve is already in the expiration zone before the first fitted model, we know only that the claim expired in that window. We take the window’s midpoint as the estimate and call windows of three months or less expired on arrival. Two expired claims, C22 and C50, have curves that end just above 0.2. We date their expirations from the newest models instead: the first date from which at least half of the models released in the previous six months stay in the expiration zone.
We use the same bootstrap to estimate uncertainty in the expiration date, taking the crossing date from each resampled curve. We report an interval only if at least half of those curves cross the threshold; otherwise we show the date without an interval. For expirations dated by a window, the window itself is the interval. Expirations dated from the newest models have no interval.
Discussion
While preliminary, these results teach us a few things about the current state of LLMs and their capabilities as well as empirical research of LLMs writ large.
Claims about LLMs have a life span
In this work, we show that many LLM claims, even famous ones, disappear as LLM capabilities increase over time. Many claims made in empirical LLM literature are assumed to hold for a long time, and they often take root as perceptions the community has about LLMs. As with fabricated citations (C11), these perceptions often work their way into policies without consideration of how subsequent generations of LLMs might impact this claim. Similarly, lags in perception of LLM behavior influence AI trust and how often people use AI in their work, as explained in this tweet from Andrej Karpathy. By revisiting claims, we can more adequately shape our expectations for the failure modes and behaviors of LLMs.
Across the claims we tested, 16% had expired within a year of publication and 39% within two years. Among the 22 claims with an estimated expiration date shown in our plots, the time from publication to expiration averaged about 16 months, with individual lifetimes ranging from about one month to roughly three years. This average excludes claims that have not yet expired, so it is not an expected life span for all LLM findings. Even still, it shows how quickly published observations can lose relevance as models improve. On the contrary, even if a claim was made a long time ago, that doesn’t mean the claim is automatically invalid today. Four of the earliest claims we tested here (Press et al., 2022 C1; Perez & Ribeiro, 2022 C2; Li et al., 2023 C3; Wang et al., 2023 C4) are still not expired today. These aggregate persistence estimates have wide confidence intervals because the study includes only 50 claims.
These results exhibit how empirical LLM claims should be presented in the context of current models rather than as general truths about LLMs. A finding is an observation about particular models at a particular time, not a fixed property of language models. Because of this, papers should report the model, version and date with each result. Citing this work should carry these limitations and acknowledge that these claims might not hold up on newer models. Further, papers should include their exact provenance for reproducibility, including prompts and analysis code, in order to repeat these claims on future LLMs.
Capability failures fade; preferences stay
Most claims that we tested about what models cannot do have faded. Of the reasoning claims, five are expired, four have weakened, and none of them either persisted or strengthened. Some notable failures in other areas disappeared, including fabricated citations (C11), facts lost in the middle of long contexts (C7), and abandonment of correct answers when the user pushes back (C16). One hypothesis for this might be that these failures have a right answer that developers can measure and train against, accelerating progress against these effects. Importantly, many of these failures, especially high-profile ones, might have been specifically patched in post-training in recent models.
Claims about what models prefer have lasted longer. Of the 8 claims that persist and the 3 that strengthened, three concern models as judges or reviewers (favoring their own answers (C28), scoring accepted and rejected papers alike (C31), and rating spun trial abstracts more highly (C37)), three concern agreeing with or flattering the user (C17, C42, C43), two concern sameness (near-identical answers to open prompts (C45) and non-uniform random numbers (C29)), two concern answering when the model should decline (C10, C41), and one is a left political lean (C21). These are tendencies rather than errors on a test with one right answer, so they may be harder to notice and to train away by model developers.
Social bias is a mixed case. Of the seven claims about social bias, culture and simulated populations, only the political lean (C21) persists. Three have weakened, including gender-stereotyped pronoun resolution (C9) and implicit association bias (C48). These cases highlight clear biases that LLMs can be trained against, but these biases should continue to be traced in subsequent model developments as progress continues to be made. Three of these bias claims are classified as expired: harsher judgments of speakers of African American English (C24), stereotyped personas of Black women (C5), and more nonanswers in Arabic than in English (C50). The African American English effect reverses direction in the fitted trend, with its interval entirely below zero.
Weakened is not expired
This work also reveals some surprising failure cases in recently released models and shows the benefit of reproducing claims against LLMs over time. Some reasoning failures have shrunk without disappearing. On two-hop questions (C1), Claude Sonnet 5.5 still gets about one in ten wrong (10%) when it answers both single-hop sub-questions correctly; the paper reported 43% for ChatGPT. The reversal curse (C13) and contradictory answers to paired timeline questions (C47) have also weakened but remain measurable. Through revisiting old claims about LLMs, we can potentially derive insights on persistent problems that can help inform benchmark design or evaluation strategies for new model releases.
Agentic AI and the reproducibility era
In this work, we leaned on agents to reproduce papers at a rate much faster than humans could do manually. This allowed us to test many more claims in a much shorter period of time than would have been possible before coding agents. This is an example of how agentic AI can help us make science more rigorous and reproduce works at scale to gain new insights. We’re excited about future studies that take a similar approach: use agents to revisit old works and provide systematic reproducibility claims that help us advance tomorrow’s science.
We want your feedback!
Have any questions or thoughts about this work or how it can be extended? Think we did something wrong or left out some crucial details? Have suggestions for other claims you’d want us to test? Please reach out to oqueen@stanford.edu with any comments, questions, or concerns. We’d especially love to hear from you if you’re the author of one of the papers we listed above 😄.
Citation
If you use this work, please cite:
@misc{queen2026shelflife,
title = {The shelf life of {LLM} findings},
author = {Queen, Owen and Zou, James},
year = {2026},
url = {https://zou-group.github.io/llm-claims-shelf-life/}
}