We consider the problem of policy optimization with noisy rewards, where the policy is constrained to be in the neighborhood of a reference policy.We study the risk of the policy optimization process, defined to be the chance of obtaining a policy worse off than the reference policy. In an idealized multivariate Gaussian model for the noisy reward function, we show that the regularizer achieving optimal risk in a suitably local neighborhood of the reference policy is the quadratic norm weighted by the reward covariance matrix. This result is used to develop a new policy optimization algorithm based on regularization via reward variance estimates. Experiments across synthetic bandit models, large language models and reward models show that this algorithm yields more robust alignment outcomes than existing approaches.
Figures & tables
Figure 1: Reward scores assigned by 10 reward models on the same prompt-response pair. The reward models are identical in that they are trained independently on the same dataset, with the same hyperparameters and number of epochs. Despite this, we see a wide variation in the score assigned by each model.
Figure 2
\Vi[ri(x,y1)]
\Vi[ri(x,y1)−ri(x,y2)]
dataset
mean
median
mean
median
Chat
4.22
3.81
2.37
1.38
Chat-Hard
4.95
4.53
0.80
0.24
Safety
5.56
5.14
1.56
0.85
Reasoning
4.71
4.44
0.09
0.01
Table 1: Variance of the rewards assigned by 10 independently trained reward models to the same input. For each input we take the sample variance \Vi across the ten members, of the reward given to the accepted response y1 (left) and of the accepted-minus-rejected difference (right), which would vanish were the members separated only by a constant offset; each entry is the mean or median of that variance over the inputs of a dataset. Rewards lie on a 1 – 20 scale, so these are variances of scores on that scale. Figures 5 and 6 in Appendix B plot the full distributions.
number of arms K
method
50
100
500
1000
vanilla
0.163
0.190
0.180
0.185
covariance
0.055
0.067
0.051
0.058
UWO (0.1)
0.169
0.198
0.181
0.176
UWO (1.0)
0.291
0.330
0.263
0.197
KL
0.163
0.190
0.180
0.185
Table 2: Underperformance probability P[π⊤r∗⩽π0⊤r∗] for a uniform reference policy at κ=50 , at each geometry’s interior radius. With π0 uniform, KL coincides with the unweighted geometry and variance-weighted KL with the covariance geometry.
skew α
method
0
0.5
1
1.5
2
vanilla
0.194
0.194
0.194
0.194
0.194
covariance
0.058
0.058
0.058
0.058
0.058
KL
0.194
0.216
0.311
0.382
0.414
var.-wtd. KL
0.058
0.087
0.190
0.302
0.374
Table 3: Underperformance probability at K=100 against the skew of the reference, π0∝(i+1)−α , for which pmin falls from 10−2 at α=0 to 6.1⋅10−5 at α=2 .
radius ε/ε0
0.25
1
4
25
200
vanilla, measured
0.035
0.035
0.032
0.033
0.099
vanilla, predicted
0.035
0.035
0.035
0.035
0.035
covariance, measured
0.008
0.007
0.008
0.009
0.028
covariance, predicted
0.008
0.008
0.008
0.008
0.008
on boundary, vanilla
0.00
0.00
0.17
0.97
1.00
Table 4: Behaviour across the interior threshold ε0 of Definition 4.2 . “Measured” is the simulated risk, obtained by solving the constrained problem exactly for each sampled R ; “predicted” is the closed form Φ(−z) , which is derived assuming π⩾0 holds with strict inequality and is therefore constant in the radius. “On boundary” is the fraction of draws whose optimum has π(x,y)=0 for at least one pair. “Reversed” counts instances in which the covariance geometry is the riskier of the two by more than three standard errors of the difference, so that sampling noise is not recorded as a violation.
Direction Cosine
P[underperform]
Geometry, Score
α=1
α=5
α=20
α=1
α=5
α=20
Covariance, R
1.000
1.000
1.000
0.235
0.236
0.234
ℓ2 , S
1.000
1.000
1.000
0.235
0.236
0.234
KL, S/ρπ0
1.000
1.000
1.000
0.235
0.236
0.234
ℓ2 , R
0.763
0.764
0.764
0.292
0.293
0.291
KL, R
0.763
0.720
0.643
0.292
0.302
0.318
Table 5: Update direction and risk on candidate sets, by the skewness factor α of the reference policy. The first column group is the cosine between a geometry’s update direction and that of πΣ , the optimum of Theorem 4.3 ; the three pairings above the rule are the optimal pairing described in Section 5 and are seen to equal the prediction. The second group is the fraction of draws on which the policy is worse than the reference under the gold reward, in bold for the three optimal pairings and for RAPO .
trust-region radius
Objective
0.5
1
2
4
8
Pythia-1.4B
Vanilla
0.155
0.162
0.202
0.267
0.378
UWO (0.1)
0.157
0.163
0.203
0.263
0.372
RAPO
0.148
0.163
0.187
0.215
0.247
Qwen2.5-7B
Table 6: Probability that the fine-tuned policy underperforms the reference policy under the gold reward, across trust-region radii and objectives. Experimental details are provided in Appendix D.2 .
Appendix figures & tables6 assets
Supplementary material from the paper’s appendix.
Appendix
Figure 5: Distribution of sample variances in the rewards assigned to accepted responses, each variance computed across the outputs of 10 independently trained reward models. The median sample variance exceeds 3.81 in all datasets, with values reaching as high as 10 , confirming substantial model-level variability in reward estimates for the same prompt–response pair. Figure 6 repeats the measurement on reward differences.
Figure 6: Distribution of the sample variances of reward differences between accepted and rejected responses, computed across the 10 independently trained reward models. Were the members simple scalar translations of one another these differences would agree exactly and the distributions would collapse to a point mass at zero. The spread instead reflects genuine disagreement about preferences, driven by the statistical and stochastic nature of training.
(a) variance ratio κ , exact Σ
κ
1
3
10
50
200
vanilla
0.000
0.000
0.004
0.034
0.105
covariance
0.000
0.000
0.001
0.008
0.024
(b) members m estimating Σ , at κ=50
m
3
5
10
20
exact
covariance
0.052
0.023
0.013
0.010
0.008
Appendix
Table 7: (a) Risk against the heterogeneity of the reward variances, at an interior radius, where κ=σmax2/σmin2 is the ratio between the largest and smallest variance a pair can receive. (b) The same when Σ is estimated from m members rather than known; at m=3 the estimated method is worse than ignoring uncertainty altogether.
rank d of the parameterization
metric M
2
4
7
I (Euclidean)
0.177
0.123
0.092
J⊤Π0−1J (Fisher)
0.158
0.078
0.030
J⊤ΣJ (covariance)
0.150
0.057
0.008
unrestricted optimum
0.008
0.008
0.008
Appendix
Table 8: Risk for a policy whose updates are confined to the range of J , at K=8 , so d=7 is full rank, where the covariance pullback coincides with the unrestricted optimum of Theorem 4.3 .
radius ε
target τ
0.5
1
2
4
8
Pythia-1.4B
0.25
15
15
15
15
15
0.5
20
20
20
20
20
1
11
15
15
15
15
2
12
12
12
12
12
Appendix
Table 9: Number of samples ∣A(ε)∣ averaged at each radius, broken down by KL target. A sample is one ensemble head trained at one target, counted only when every objective has a checkpoint at or below that radius. Counts fall at the tightest radius because a run trained at a loose target may never come that close to the reference policy, and fall with the target for the same reason. The bold rows are the totals that Table 6 reports. A seventh target τ=6 was trained but contributes nothing, the three objectives having been run there on disjoint heads.
trust-region radius
m
Objective
0.5
1
2
4
8
20
Vanilla
0.277
0.363
0.472
0.553
0.643
UWO (0.1)
0.267
0.338
0.462
0.535
0.623
Covariance
0.070
0.055
0.058
0.052
0.047
10
Vanilla
0.427
0.510
0.572
0.665
0.723
UWO (0.1)
0.417
0.497
0.567
0.658
0.712
Appendix
Table 10: Reward model scalability. The construction of Table 6 repeated on Qwen2.5-7B at three ensemble sizes of m . The covariance arm is the safest at every radius and every ensemble size, and the uncertainty penalty stays within Monte-Carlo error of vanilla throughout. Bold marks the lowest risk in a column. Remaining parameters as in Table 6 .
Current critic-less RLHF methods aggregate multi-objective rewards via an arithmetic mean, leaving them vulnerable to constraint neglect: high-magnitude success in one objective can numerically offset critical failures in others (e.g., safety or formatting), masking low-performing "bottleneck" rewards vital for reliable multi-objective alignment. We propose Reward-Variance Policy Optimization (RVPO), a risk-sensitive framework that penalizes inter-reward variance during advantage aggregation, shifting the objective from "maximize sum" to "maximize consistency." We show via Taylor expansion that a LogSumExp (SoftMin) operator effectively acts as a smooth variance penalty. We evaluate RVPO on rubric-based medical and scientific reasoning with up to 17 concurrent LLM-judged reward signals (Qwen2.5-3B/7B/14B) and on tool-calling with rule-based constraints (Qwen2.5-1.5B/3B). By preventing the model from neglecting difficult constraints to exploit easier objectives, RVPO improves overall scores on HealthBench (0.261 vs. 0.215 for GDPO at 14B, p<0.001) and maintains competitive accuracy on GPQA-Diamond without the late-stage degradation observed in other multi-reward methods, demonstrating that variance regularization mitigates constraint neglect across model scales without sacrificing general capabilities.
Scaling laws for optimization against reward models in AI alignment have pinned down how performance depends on optimization effort---measured by a KL-divergence budget relative to a reference policy. Beyond a certain budget, over-optimization (or reward hacking) can arise: because we optimize against a proxy reward model (distinct from true rewards), performance can plateau or degrade. Naturally, the proxy reward's accuracy depends on how much preference data (often in the form of pairwise comparisons) was used to train it. However, existing research does not cleanly identify how performance jointly scales with the amount of training data and the divergence budget. Our main contribution is to provide an empirically accurate and theoretically grounded scaling law in such context. Performance roughly scales as Θ(min{log(M),K}), where M is the number of comparisons in training data and K is the policy's divergence budget. We develop an information-theoretic model to establish this upper bound and prove it is tightly achievable through a constructive procedure. Informed by this, we conduct extensive empirical evaluations using a real-world annotation setup, whereby a large 70B gold reward model generates feedback data and proxy reward models are trained from less capable models (0.6B to 4B). Our scaling law provides an excellent fit (R2 from 97% to 99%), outperforms alternative specifications, and remains robust across model sizes, noise, and optimization procedures (best-of-N or policy tilting). Our evidence suggests that reward optimization is analogous to a surprisingly simple selection task: choosing from a sequence of IID Gaussian random variables using noisy preference feedback.
Feedback noise is pervasive in preference data, arising from subjective human judgments, annotation mistakes, and imperfect LLM judges. Standard reward modeling trained on such feedback yields a biased estimate of the clean risk. Although classical denoising methods are directly applicable to noisy feedback learning, they generally assume a uniform noise ratio across samples. However, this assumption fails for feedback data, where noise is intrinsically sample-wise. To address this challenge, we propose CleanRM, which uses a few clean feedback to calibrate sample-wise noise ratios via optimal transport. Specifically, CleanRM aligns the joint distribution of preferences reverted from noisy feedback with that of clean feedback and then trains the reward model using a noise-corrected surrogate loss. Theoretically, we prove that the resulting objective is unbiased with respect to the clean risk. Extensive experiments demonstrate that CleanRM outperforms state-of-the-art denoising baselines and yields more effective downstream RLHF alignment.
Licheng Pan, Haocheng Yang, Yuzhou Chen +7
Zhejiang University · Xiaohongshu Inc · National University of Singapore +3