Comparative studies of predictive models often end by ranking candidate models, yet these rankings depend on evaluation protocols whose influence is rarely treated as a source of uncertainty. We formalize this problem as protocol-induced ranking uncertainty and introduce a framework that compares ranking displacement caused by switching protocols with displacement produced by conventional choices within a fixed protocol. We quantify these effects using the Protocol Sensitivity Score (PSS) and a full-refit intraprotocol reference. We validate the framework in a large-scale sequential prediction study of daily PM10. Static-split and rolling-origin evaluation are compared across 425 European background stations and 365 US EPA monitors. Switching protocols produces mean PSS values of 0.801 and 0.772 and changes the selected model at 35.3% and 31.5% of stations, respectively. In Europe, intraprotocol perturbations with identical scored targets produce PSS values of 0.072 and 0.230, with winner-swap rates of 0.8% and 4.9%. Between-protocol displacement is therefore substantially larger than the selected within-protocol references. Expanding the candidate set from three to nine models increases the between-protocol winner-swap rate to 60.2% in Europe. The pattern also persists under a frozen protocol applied to held-out background and non-background stations. These results show that model-selection conclusions can depend materially on legitimate evaluation choices. We recommend reporting ranking stability under a small set of defensible intraprotocol perturbations alongside claims of model superiority.
Figures & tables
Panel
Network
Universe
Eligible
N
Blocks
Role
EEA Heisig background
Heisig
2807
1216
425
15
confirmatory core
EPA AirData
EPA
–
365
365
38
cross-continental
EEA airbase (excluded)
airbase
2615
1172
–
–
outside confirmatory N
Single-site (Elche)
EEA local
1
1
1
–
not aggregated
Table 1: Panel summary for H1 and H4 claims.
Figure 1: Station selection funnel by network—universe, eligibility, European background stratum, and US census—with branches kept separate (no pooling).
Figure 2: Study design at a glance: ranking variance under two evaluation protocols. Attribution contrasts between-protocol discrepancy with intraprotocol noise.
Figure 3: Static-split versus rolling-origin protocols on a shared timeline: both use the full series; evaluation origins differ.
Figure 4: PSS distributions on the European and US panels, with equivalence margin δ and the discrete measurement grid.
Figure 5: Spatial maps of station-level PSS on the European and US panels.
Panel
Measure
Between protocols
Rolling convention
Static convention
EEA
PSS
0.801 [0.660; 0.908]
0.230 [0.212; 0.257]
0.072 [0.064; 0.083]
EEA
Winner swap
35.3% [22.1%; 47.6%]
4.9% [3.0%; 8.1%]
0.8% [0.4%; 1.3%]
EPA
PSS
0.772 [0.711; 0.823]
0.237 [0.197; 0.277]
0.065 [0.044; 0.085]
EPA
Winner swap
31.5% [20.6%; 38.9%]
6.3% [3.4%; 10.0%]
1.2% [0.4%; 2.1%]
Table 2: Ranking-variance decomposition (H2) on both panels.
Figure 6: Ranking-variance decomposition: between-protocol contrast versus intraprotocol nulls (PSS and winner-swap distributions).
Panel
Measure
Between protocols
Static placebo
Rolling placebo
EEA
PSS
0.540 [0.499; 0.572]
0.157 [0.148; 0.165]
0.251 [0.233; 0.276]
EEA
Winner swap
60.2% [56.0; 64.3]
27.2% [18.8; 35.0]
22.8% [17.5; 30.3]
EEA
MCS exclusion
1.4% [0.4%; 3.4%]
1.2% [0.5%; 2.5%]
4.7% [3.0%; 7.5%]
EPA
PSS
0.550 [0.505; 0.583]
0.169 [0.153; 0.181]
0.273 [0.251; 0.294]
EPA
Winner swap
67.4% [61.3; 73.3]
16.2% [12.3; 21.6]
27.4% [21.6; 32.7]
EPA
MCS exclusion
1.4% [0.4%; 2.7%]
0.4% [0.1%; 0.9%]
4.4% [2.1%; 7.9%]
Table 3: Nine-model arm: between-protocol contrast vs intraprotocol placebos.
Figure 7: Three-model versus nine-model decision spaces: between-protocol contrast and intraprotocol nulls under PSS and winner swap.
Figure 8: Winner-swap rate versus number of Borda-aggregated intraprotocol runs ( K ). Rows: EEA and EPA panels. Columns: Curve A (aggregate static, compare to rolling reference) and Curve B (aggregate rolling, compare to static reference). Solid line: median over 100 random subsets; band: interquartile range.
Panel
Curve
K
Median [%]
IQR [%]
EEA
Static agg.
1
35.5
[34.4; 38.8]
EEA
Static agg.
3
34.1
[33.4; 35.1]
EEA
Static agg.
5
33.9
[33.4; 34.1]
EEA
Static agg.
7
33.6
[33.4; 33.9]
EEA
Static agg.
10
33.9
[33.8; 34.1]
EEA
Static agg.
13
33.2
[33.2; 33.2]
Table 4: Winner-swap rate (%) under Borda aggregation: median [IQR] over 100 subsets.
Stratum
N
Blocks
Mean PSS [95% CI]
Winner swap [95% CI]
Background confirmatory
425
15
0.801 [0.660; 0.908]
35.3% [22.1%; 47.6%]
Background holdout
271
4
0.676 [0.606; 0.833]
20.3% [17.9%; 37.5%]
Traffic / industrial
520
19
0.701 [0.617; 0.847]
23.1% [16.5%; 32.8%]
Table 5: Frozen-protocol confirmation sets.
Panel
N
Blocks
Mean PSS
Winner swap
PSS > 0
TOST ( δ=0.10 )
BH-FDR
EEA
425
15
0.801 [0.660; 0.908]
35.3% [22.1; 47.6]
420/425
not equiv.
83
EPA
365
38
0.772 [0.711; 0.823]
31.5% [20.6; 38.9]
362/365
not equiv.
–
Table 6: Side-by-side confirmatory battery.
Alternative
How tested
Outcome
Single-station artefact
Panels of 425 European and 365 US monitors, independent networks, identical protocol, no pooling
PSS positive at 420/425 and 362/365 (Sections 5.1 , 5.9 ; Supplementary Section SM-08)
Evaluation-procedure noise
Full-refit intraprotocol references with strict target pairing
PSS 0.801 between protocols versus 0.072 and 0.230 within protocols; winner swaps 35.3% versus 0.8% and 4.9% (Section 5.2 )
Unequal test sets
Count of date–horizon pairs per station under each protocol
Counts are identical on both panels (Section 4.4 )
Static-split training lag
European re-run with training contiguous to evaluation
PSS 0.773 versus 0.801; mean absolute difference 0.073, below the grid step (Section 6.4 )
Background-stratum restriction
Frozen protocol on 520 traffic and industrial stations
Mean PSS 0.701, with an interval that overlaps the background interval (Section 5.6 )
Adaptation to examined data
Dated freeze before selecting 271 previously unexamined stations; one run
Mean PSS 0.676, inside the confirmatory interval (Section 5.6 )
Table 7: Attempted alternative explanations and outcomes.
Appendix figures & tables7 assets
Supplementary material from the paper’s appendix.
Appendix
Domain
Checklist item
Status
In SM/main
Models
Clear description of setting / algorithm / model
Yes
Methods
Models
Clear explanation of assumptions
Yes
Methods, limits
Models
Complexity analysis (time / space / sample)
Partial
Main + runtime note
Theory
Clear statement of claim
Yes
Intro / RQs
Theory
Complete proof
NA
Empirical paper
Data
Relevant statistics (sample sizes)
Yes
Data, tables
Appendix
Table 1: Machine Learning Reproducibility Checklist v2.0 ( Pineau et al., 2021 ) : compliance for this study. Full comments and file pointers: notes/phase5/S3_NeurIPS_checklist_draft.md .
Criterion
Threshold
Obtained
Decision
EEA sample floor
250
1216
pass
External sample floor
50
365
pass
Instrument check ( PSS≥1.0 )
1.000
1.143
pass
Equivalence margin δ(M=3)
0.100
0.100
locked
Equivalence margin δ(M=9)=4/[M(M−1)H]
0.008
0.008
locked
Index viability (adj. R2 )
0.150
0.105
supplementary
Appendix
Table 2: Pre-specified criteria and outcomes.
Figure 1: Macro execution sequence with hypothesis labels [Hn] , explicit branch terminals, and parallel European and US arms.
Station
Pre-specified criterion
PSS
Reversal
ES/ES1968A
hard reversal or PSS≥1.0
1.143
yes
Appendix
Table 3: Instrument check before the panel.
Figure 2: Diagnostic-index fit diagnostics (adj. R2=0.105 below the pre-specified viability gate of 0.15; reported in supplementary material by rule).
(a) Many air quality forecasting studies report gains from machine learning, but evaluations often use static chronological splits and omit persistence baselines, so the operational added value under routine updating is unclear. (b) Using 2,350 daily PM10 observations from 2017 to 2024 at an urban background monitoring station in southern Europe, we compare XGBoost and SARIMA against persistence under a static split and a rolling-origin protocol with monthly updates. We report horizon-specific skill and the predictability horizon, defined as the maximum horizon with positive persistence-relative skill. Static evaluation suggests XGBoost performs well from one to seven days ahead, but rolling-origin evaluation reverses rankings: XGBoost is not consistently better than persistence at short and intermediate horizons, whereas SARIMA remains positively skilled across the full range. (c) For researchers, static splits can overstate operational usefulness and change rankings. For practitioners, rolling-origin, persistence-referenced skill profiles show which methods stay reliable at each lead time.
Federico Garcia Crespi, Eduardo Yubero Funes, Marina Alfosea Simon
Departamento de Ingeniería de Computadores, Universidad Miguel Hernández, Elche, Spain · Departamento de Física Aplicada, Universidad Miguel Hernández, Elche, Spain
A forecasting benchmark reports which method won. We show that the answer is set by the evaluator's choices before any model is fitted. We benchmark 24 forecasting methods and one textbook reference, including six 2025-era time series foundation models, on a production marketplace panel of 1,887 business customers over 67 months. We hold the data, the horizon and the period fixed, and vary only the evaluation design. Three choices each reverse or dissolve a headline conclusion. Changing the unit of analysis from the market total to the individual customer moves our production baseline from second of nineteen, beaten by nothing, to twenty-third of twenty-five. Nineteen of its twenty-four challengers beat it there. Changing how much error is pooled decides whether a Diebold-Mariano test finds anything at all. Scoring prediction intervals rather than point forecasts reorders the field almost completely, with a rank correlation of 0.02 on intermittent demand. We then measure what the deployed system gets from this. Its selection rule captures 55% of the distance between doing nothing and choosing with hindsight. The reversal is not a quirk of our data. We ran the released protocol, unchanged, on the public M5 retail panel. The same baseline shape places first at the market total and last per series, beaten by everything, and a replayed selection rule closes 64.7% of the same floor-to-ceiling distance there. Adding five zero-shot foundation models to that roster changes who wins at the total, not the shape. The bands' blind spot travels too: conformal bands under-cover most on the spikiest items. Splitting our own panel into ever smaller groups turns the contrast into a curve: the baseline's rank worsens at every level of disaggregation. We release the evaluation protocol and report an error of our own that inverted a result before we caught it.
We study the problem of model selection among probabilistic forecasting models evaluated on datasets of multiple time series. The performance of a model on a single time series is quantified by the average value (score) of a proper scoring rule over a test set, but extending model selection to data sets of time series requires aggregating these scores. Common approaches either rely on scaling scores and averaging them (mean scaled score) or avoid scaling by using alternative statistics such as mean ranks or win rates. However, these approaches can yield conflicting conclusions. We show that such discrepancies arise from the skewness of the distribution of the scores, which is particularly pronounced when test sets are short. The skewness can cause non-mean criteria (e.g., mean rank, median, win rate) to select misspecified models. In contrast, the mean score is immune from this problem. We further show that, as the size of the test sets increases, all aggregation criteria converge to the same model selection decision, mitigating these discrepancies. Our experiments on intermittent demand time series, including data from the M5 competition, highlight the importance of sufficiently large test sets; the mean scaled score appears to be the more reliable approach, also because empirically we found its decision to remain consistent when different scaling factors are adopted.
Giorgio Corani, Stefano Damato, Dario Azzimonti +1
SUPSI, Istituto Dalle Molle di Studi sull’Intelligenza Artificiale (IDSIA), Lugano, Switzerland