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Measurement-Induced Decision Loss: A feasible-set theory of microbiome intervention under observation loss

Javad Aminian-DehkordiiD, Mohammad R. K. MofradiD

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Abstract

Microbiome measurements are commonly judged by how faithfully they reconstruct an underlying biological profile, using taxonomic similarity, prediction accuracy, or compositional distance. Yet faithfulness and usefulness are not the same: a distorted measurement may still support the correct intervention, while a small error can be decisive when it falls near the boundary between two treatment choices. We therefore evaluate measurement quality by whether information loss changes the decisions and outcomes that remain attainable. We treat the intervention-relevant state of the gut community as a hidden quantity seen only through an imperfect, information losing measurement, mapped by a decision rule to a graded intervention. Each decision rule is evaluated by net host benefit and ecological margin, generating a feasible set of attainable outcome pairs. We define the measurement-induced decision loss (MIDL) as the maximum net host benefit lost under imperfect measurement relative to perfect observation. For scalar affine information loss, increasing degradation is a Blackwell garbling; under post-processing closure, more informative measurement weakly expands the feasible set and cannot reduce optimal host benefit. In the binary-state model, MIDL increases linearly while an observation-dependent decision rule remains optimal and plateaus once the optimal policy becomes signal-independent. We extend the framework to finite states, state-specific loss, multi-segment stool aggregation, and ecological-margin constraints. The framework distinguishes measurement faithfulness from decision usefulness and provides a principled basis for comparing stool and richer measurements by the interventions and trade-offs they support.

In-depth summary

Claude Opus 5.5 · xhigh effort · 7 Nov 2026 · from the full text of version 1 (7 Oct 2026) · CC BY 4.0

Measurement-induced decision loss (MIDL), host benefit forgone versus perfect observation, grows linearly with microbiome information loss in a binary model, then plateaus once the optimal policy becomes signal-independent.

Stool microbiome measurements are usually judged by how faithfully they reproduce an intestinal profile (correlation, classification or prediction accuracy), although a small error near an intervention boundary can flip the chosen treatment while a visibly distorted signal may not. The paper ties Blackwell's comparison of experiments to a two-objective feasible set (net host benefit and ecological margin), so measurements are ranked by the interventions and trade-offs they leave attainable.

Key results

  1. ShownFor a scalar affine channel (true category kept with weight 1 − β, otherwise replaced by a reference draw), larger β is a Blackwell garbling of smaller β. Closure is proven for the convexified monotone policy class, so feasible sets nest and MIDL is nonnegative and nondecreasing in β.

    An explicit row-stochastic kernel turns T_β1 into T_β2 for 0 ≤ β1 ≤ β2 ≤ 1 (using R^2 = R). A garbling theorem gives feasible-set inclusion under post-processing closure. A proof shows that a nondecreasing policy composed with the scalar kernel is a mixture of the original policy and constant policies. Delivered benefit over an uninformative channel plus MIDL sums to H_P(I) − H_P(R). · 3.1 Scalar affine observation channel; 3.2 Blackwell ordering and feasible-set…; 3.3 Scope of the Blackwell ordering

  2. ShownIn the binary-state model, the host-optimal monotone policy switches from signal-dependent to a constant rule at a closed-form threshold βc(α, η), where α is the high-state prior and η is the aggressive tier's normalized burden. MIDL grows linearly up to βc and is flat beyond it.

    The feasible set is the triangle conv{A, Bβ, C}: constant policies A and C stay fixed while the observation-dependent vertex Bβ moves affinely. MIDL is piecewise linear, concave, nonnegative and nondecreasing in β, with slope D(α, η)/2 before the switch and at most one interior kink. α = 1/2 gives βc = 2 min{η, 1 − η}; α = η gives βc = 1. Perfect observation yields host utility α(1 − η). · 4.1 Posterior policy regimes; 4.2 Feasible-set geometry and…; Measurement-induced decision-loss landscape; S1.2 Proof of feasible-set geometry for K=2

  3. ShownWith K ordered states, the feasible set under randomized monotone policies is a compact convex polytope spanned by finitely many deterministic-policy outcomes. Under scalar blur, the host-benefit frontier is convex piecewise linear and MIDL is concave piecewise linear in β.

    The proof counts nondecreasing policies as multisets of size K drawn from K values (combinations with repetition) and shows the feasible set is the convex hull of their outcomes. Each outcome is affine in β, so the frontier is an upper envelope of finitely many lines. Synthetic K = 5 (prior 0.12, 0.20, 0.31, 0.23, 0.14) and K = 3, 5, 6 systems show set contraction and MIDL kinks at policy switches. · 5 K-state feasible-set theory; S2.2 Finite-state illustrations

  4. ShownHeterogeneous information loss breaks simple orderings. Componentwise larger state-specific loss need not be a Blackwell garbling, and blurring the weighted-mean stool composition once differs from the heterogeneous multi-segment aggregate by a weighted blur-composition covariance.

    For K = 3 with uniform r, the kernel needed to garble one channel into its componentwise-blurrier partner has a negative entry, and so does the reverse kernel. The aggregation error equals a weighted covariance of segment βs and compositions zs, is zero iff that term vanishes (e.g., equal compositions or equal βs) and has a Cauchy-Schwarz norm bound. Illustrated with 4 segments, 4 guilds and βeff = 0.32. · 6 State-specific information loss; 7 Multi-segment stool aggregation; S1.1 State-specific information loss and…; S1.3 Proofs for the multi-segment aggregation…

  5. ShownAn expected ecological-margin floor preserves convexity, and both the unconstrained and floor-constrained host-benefit frontiers weakly improve with information. Yet the difference between them (the ecological-screening gap) can shrink and then widen as information loss grows.

    Binary example with α = 0.60, η = 0.30, d = 1, τ = 0.228: Gτ(0) = 0.1596, Gτ(4/9) ≈ 0.06086, Gτ(0.55) ≈ 0.06782. A constructed pair of nested sets gives gaps of 0 and 0.45. A two-guild generalized Lotka-Volterra (gLV) model, used as motivation, moves from stable coexistence to a stable boundary state via a transcritical bifurcation at ucrit ≈ 0.281553. · 8.1 Constraints on attainable outcomes; 8.2 Ecological reserve under community dynamics; S2.4.1 Two-guild dynamical model

Methods, data and reproducibility

Models the intervention-relevant gut state as a latent categorical variable observed via a row-stochastic channel (scalar or state-specific affine blur toward a reference distribution) and maps signals to graded interventions by monotone rules. It then derives analytically the feasible sets of expected ecological margin (UE) and net host benefit (UH), plus MIDL, illustrated with deterministic synthetic parameters.

  • Synthetic binary-state parameterizations (prior α, burden η, d = 1, r = (1/2, 1/2)) for feasible-set and MIDL illustrations (Table S1)
  • Synthetic ordinal finite-state systems: K = 5 with nonuniform prior (0.12, 0.20, 0.31, 0.23, 0.14), plus rank-based systems for MIDL comparison · n = K = 3, 5, 6 states
  • Synthetic multi-segment stool aggregation system (Table S2), not fitted to intestinal-segment data · n = 4 intestinal segments, 4 functional guilds
  • Two-guild generalized Lotka-Volterra model with dimensionless illustrative parameters (Table S3), not estimated from data · n = 2 guilds
Methods & tools
generalized Lotka-Volterra model
Reproducibility gaps
No code repository or archive is linked, although the supplement refers to code that computed the illustrations. Synthetic parameters are said to be in supplementary Tables S1 to S3, whose values are not reproduced in the provided text.
Limitations (6)
  • All results are conditional on the chosen state space, prior, measurement channel and utilities. Applying the framework to a real assay or intervention needs empirical calibration of state definitions, signal-generation probabilities, and benefit, burden and ecological utilities. · stated by the authors
  • UE is an abstract modeled reserve. The paper notes it does not directly measure resilience, resistance, recovery time or dynamical stability, and the gLV example motivates rather than calibrates it. · stated by the authors
  • The ecological floor constrains expected margin only, so a randomized policy may mix low- and high-margin outcomes. Statewise, robust or chance constraints would define different admissible sets. · stated by the authors
  • The scalar affine channel is a tractable benchmark. State-dependent, subject-specific or nonlinear channels need their information ordering established directly, and compositional transforms do not define stochastic channels (zeros and detection limits must be handled). · stated by the authors
  • The multi-segment identity is purely compositional: it does not define P(O | X) or MIDL, and linking it to the categorical decision model requires further calibration. · stated by the authors
  • No empirical microbiome data are used, and every illustration is a hand-chosen synthetic parameterization (e.g., the 0.38 floor factor). So there is no evidence on how large MIDL is for real stool versus intestinal sampling. · noted in this summary

Read this if you compare microbiome sampling strategies (stool versus regional gut sampling) and want a decision-theoretic criterion based on which interventions stay attainable rather than on reconstruction accuracy.

Citations
1

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