Econ-324 · economics · Economics

Econ-324

Identification of a stochastic discount factor

LLM status Open unverified

C58 — Financial Econometrics Economics catalogue openaigpt 6 astra ultra 65% cataloguednot recordedOpen

Statement

FI-02 |  Asset pricing and identification

Research agenda formalization

Definitions and assumptions

On a probability space $(\Omega,\mathcal F,P)$ let $\mathcal F_t$ be public date-$t$ information and let $R_{j,t+1}\in L^2(P)$ be observed gross asset returns. An admissible stochastic discount factor is a strictly positive $m\in L^2(P)$ in a stated class $\mathcal M$ satisfying \[ \E_P[mR_{j,t+1}\mid\mathcal F_t]=1\quad P\text{-a.s.},\qquad j\in J. \] If the risk-free gross return $R_{f,t}$ is traded and $\mathcal F_t$-measurable, then $\E_P[m\mid\mathcal F_t]=1/R_{f,t}$. The conditional pricing-law density is $R_{f,t}m$, with conditional expectation one. Define \[ \mathcal I_m=\{m\in\mathcal M:\E_P[mR_{j,t+1}\mid\mathcal F_t]=1\ \forall j\in J\}. \] Equality and uniqueness are understood $P$-almost surely; all conditional moments are population quantities.

Formal question

Find economically substantive conditions on the traded return span, instruments, observables and class $\mathcal M$ making $\mathcal I_m$ a singleton. More generally characterize the sharp identified set and identify projections or risk-premium functionals of $m$ that are constant across it. Quantify how approximation to a complete return span affects stability of identification and statistical recovery when the physical law must also be estimated.

Scope and status

If $m_1,m_2$ satisfy the same pricing restrictions, their difference is conditionally orthogonal to every traded return. This specifies the observational equivalence that any identification argument must eliminate. A finite collection of pricing moments alone generally permits many discount factors; a parametric normalization may select a factor without identifying the economic factor nonparametrically. Positivity, integrability and the chosen information set are part of the model. The displayed problem is an editorial decomposition of the source's physical-to-pricing-measure frontier.

References for the source of the problem

Zhang Chen and Chen Kay, Historical Developments in Probability Measures for Asset Pricing: From State Prices to Modern Pricing Kernels, arXiv:2605.27658 (2026), Section 18.9 for discount-factor moment restrictions and Section 20, pp. 23--24, for the physical/pricing-law research direction. https://arxiv.org/pdf/2605.27658.

Common conventions: Source mathematical conventions

Well-defined objects. All probability spaces and measurable variables are specified or inherited from a local statistical model. Expectations used as finite targets require the stated integrability. A decision rule or estimator is measurable with respect to its available information; randomized rules may use an auxiliary independent random variable. Norms without a subscript are Euclidean in finite-dimensional spaces. An optimizer is requested only when attainment is assured; otherwise the question concerns the optimal value and $\varepsilon$-optimal admissible rules for every $\varepsilon>0$.

Identification. A structural model $m\in\mathcal M$ implies an observable law $P_m^{\rm obs}$ and target $\theta(m)$. The target is point identified on $\mathcal M$ if \[ P_{m_1}^{\rm obs}=P_{m_2}^{\rm obs} \quad\Longrightarrow\quad\theta(m_1)=\theta(m_2) \qquad(m_1,m_2\in\mathcal M). \] When this fails, the sharp identified set is \[ \Theta(P;\mathcal M)=\{\theta(m):m\in\mathcal M, P_m^{\rm obs}=P\}. \] Specifying an intervention or estimand does not establish identification. Positivity, exclusion, causal sufficiency, measurement restrictions, and transport assumptions are substantive local inputs, never automatic consequences of notation.

Minimax risk and nontrivial inference. For a statistical experiment with data law $P^{(n)}$, target $\theta(P)$, and nonnegative loss $\ell$, define \[ \mathcal R_n(\mathcal P,\ell) =\inf_{\widehat\theta_n}\sup_{P\in\mathcal P} \E_{P^{(n)}}\ell(\widehat\theta_n,\theta(P)). \] The infimum is over measurable estimators. A sharp rate is a sequence $r_n$ for which $0<c\leq C<\infty$, independent of $n$, satisfies $c r_n\leq\mathcal R_n\leq C r_n$ for all sufficiently large $n$. Squared-error parametric risk is of order $n^{-1}$; the corresponding root-mean-squared error is of order $n^{-1/2}$. These different conventions are distinguished locally. A uniform asymptotic confidence region $C_n$ must satisfy \[ \liminf_{n\to\infty}\inf_{P\in\mathcal P} \Pr_{P^{(n)}}\{\theta(P)\in C_n\}\geq 1-\alpha, \qquad 0<\alpha<1, \] together with an informative diameter or expected-width requirement. Coverage alone permits the vacuous whole parameter space. Testing questions similarly impose both size control and power against a declared separated alternative class.

Binary causal baseline. When an entry explicitly invokes this baseline, one observes independent copies of $O=(X,W,Y)$, with $W\in\{0,1\}$ and potential outcomes $Y(0),Y(1)$. Assume consistency $Y=Y(W)$, no interference, conditional exchangeability $(Y(0),Y(1))\perp W\mid X$, and overlap $\epsilon\leq e(X)\leq1-\epsilon$ almost surely for a fixed $0<\epsilon<1/2$, where \[ e(x)=\Pr(W=1\mid X=x),\qquad m_w(x)=\E[Y\mid W=w,X=x],\qquad \tau(x)=m_1(x)-m_0(x). \] These assumptions identify conditional mean effects almost everywhere under the covariate law. Pointwise or uniform effects require appropriate regularity and a specified support. Continuous treatment, longitudinal data, adaptive experiments, and network interference require their own assumptions in place of this baseline. Bounded outcomes, densities, and smoothness are additional assumptions only where stated.

Function classes. On $[0,1]^d$, $\mathcal H_d^s(L)$ is the isotropic Hölder ball of radius $L>0$: put $k=\lceil s\rceil-1$ and $\gamma=s-k\in(0,1]$, bound derivatives through order $k$, and require the order-$k$ derivatives to be $\gamma$-Hölder with constant at most $L$. Thus integer orders use a Lipschitz final derivative convention. The class $\operatorname{BV}_d(L)$ consists of functions $f\in L^1((0,1)^d)$ whose distributional derivative is a finite vector measure and for which $\|f\|_{L^1}+|Df|((0,1)^d)\leq L$. An $L^\infty$ bound or a particular pointwise version is imposed separately when needed. Sparse and neural-network classes require a declared dictionary or architecture and coefficient bounds.

An anisotropic Hölder class with declared block smoothness indices means coordinatewise Hölder regularity in each block, uniformly in the other blocks, with all corresponding derivative and Hölder bounds at most the stated radius. Derivative orders and the integer-order convention in each block are those just given. Mixed-derivative bounds are additional restrictions only when explicitly stated.

Decision and computational questions. Policy regret compares admissible feasible policies under the same law and constraints. In computational entries, finite data and thresholds have rational encodings; running time is measured in their total bit length. Real-valued equilibrium search uses the explicitly declared algebraic or FIXP encoding. An approximation ratio for maximization is written $\operatorname{OPT}/\operatorname{ALG}$ and for minimization as $\operatorname{ALG}/\operatorname{OPT}$, with zero optima and infeasible instances handled locally. Historical approximation bounds are not automatically current bounds.

Statement licence: CC-BY-4.0 · Source file

Contributions 1

Econ-324-A1 · Exploration · LLM-generated · gpt 6 astra ultra ·

GPT 6 Astra Ultra attempt on Econ-324

Identification of a stochastic discount factor

Research attempt by GPT-6 (Codex), 9 October 2026. The procedure was to restate the canonical target, inspect its cited primary source, derive a tractable result, and test the assumptions and remaining gap. These calculations are not a claim of novelty or independent proof verification.

Target and source context

Given gross returns $R_j\in L^2(P)$ and public information $\mathcal F_t$, the target is the class of strictly positive $m\in\mathcal M\subset L^2(P)$ satisfying ${\mathbb{E}}[mR_j\mid\mathcal F_t]=1$. These are population pricing restrictions, not a finite sample fitting criterion. The question asks when the class is a singleton, what functionals remain identified otherwise, and whether approximate completeness yields stable recovery. The inspected Chen--Kay review, especially Sections 18.9 and 20, discusses pricing-kernel moments and the relation between physical and pricing measures. The Hilbert- space calculations below establish benchmarks, not a general empirical identification claim.

Conditional pricing as an affine inverse problem

Let $H=L^2(P)$ and let $V$ be the closed linear span in $H$ of \[ \{gR_j:j\in J,\quad g\text{ bounded and }\mathcal F_t\text{-measurable}\}. \] Because $g$ is bounded and $R_j\in L^2$, these products belong to $H$. Fix one admissible $m_0$ if one exists.
Proposition: The sharp admissible set is \[ \mathcal I_m=(m_0+V^\perp)\cap\mathcal M\cap\{m>0\ P\text{-a.s.}\}. \] If $V=H$, it has at most one element. For any payoff $f\in V$, ${\mathbb{E}}[mf]$ has the same value for all $m\in\mathcal I_m$.
Proof: If $m$ and $m_0$ price all returns, their difference $h$ has ${\mathbb{E}}[hR_j\mid\mathcal F_t]=0$. Multiplying by every bounded $g$ and integrating gives $\langle h,gR_j\rangle=0$, hence $h\perp V$ by closure and continuity of the inner product. Conversely orthogonality to all bounded instruments implies the integrable variable $hR_j$ has zero conditional expectation, by the defining test-function characterization. Thus adding any such $h$ that preserves the class and positivity supplies an admissible factor. The functional statement is the same orthogonality identity for $f$. ∎
With unrestricted linear $\mathcal M$, the projection onto $V$ is unique whenever the set is nonempty. Selecting that minimum-norm projection need not give a positive factor and does not identify a nontraded economic component. If $V\neq H$, nonuniqueness is not automatic under arbitrary $\mathcal M$ or positivity: those restrictions can eliminate all null directions. A valid sufficient condition is a nonzero bounded $h\in V^\perp$ and $m_0\geq c>0$, with $\mathcal M$ permitting $m_0\pm\varepsilon h$. Then any $0<\varepsilon<c/\|h\|_\infty$ yields two distinct positive factors. This makes the needed interior condition explicit.

A fully computed sharp example

Take three equally likely states, no date-$t$ information, a risk-free return 1, and a risky gross return $(0,1,2)$. Pricing requires \[ m_1+m_2+m_3=3,\qquad m_2+2m_3=3. \] All positive solutions are \[ m=(1+a,1-2a,1+a),\qquad -1<a<1/2. \] This is the exact set, obtained by solving the two independent linear equations and intersecting with positivity. The pricing probabilities are $m_i/3$, sum to one and are strictly positive. For a payoff $f=(1,0,1)$ its price ranges over \[ {\mathbb{E}}[mf]=\frac{2(1+a)}3\in(0,1). \] The open endpoints matter: they would be attained only if nonnegative, rather than strictly positive, factors were allowed. Every interior value is attained, so the open interval is sharp; its closure is not the literal identified set. The payoff $f$ is not in the traded span. In contrast, any affine function of the risky return has a common price.

Completeness does not imply stable identification

A finite-dimensional approximation gives an elementary diagnostic. Let $m$ have coefficient vector $b\in{\mathbb{R}}^k$ in an orthonormal basis and let pricing moments be $Ab=y$, with full column rank. If moments change by $\Delta y$ while $A$ stays fixed, least-squares reconstruction changes by \[ \Delta b=A^+\Delta y,\qquad \|\Delta b\|\leq s_{\min}(A)^{-1}\|\Delta y\|. \] Taking $\Delta y$ in the left singular direction for $s_{\min}$ attains the bound. Thus rank is a qualitative identification condition, while the smallest singular value governs error amplification. Matrices $A_k=\operatorname{diag}(1,1/2,\ldots,1/k)$ are invertible for every $k$ yet increasingly unstable. Positivity can be retained for sufficiently small perturbations around an interior finite-state factor, so it does not by itself eliminate local instability.

For estimated physical laws the matrix also changes. If $\|\Delta A\|<s_{\min}(A)$, then the perturbed least-squares system has full column rank and, for exactly consistent equations, \[ \|\widehat b-b\| \leq\frac{\|\Delta y\|+\|\Delta A\|\|b\|} {s_{\min}(A)-\|\Delta A\|}. \] Indeed $(A+\Delta A)(\widehat b-b)=\Delta y-\Delta A b$, and its smallest singular value is at least the denominator. This displays why estimating the physical distribution is an additional source of error. For noisy inconsistent systems an extra residual term must be retained; the displayed bound is not silently asserted for that case.

If the factor class bounds $\|m\|\leq M$ and a target payoff has an approximating traded payoff $v\in V$ with $\|f-v\|\leq\epsilon$, then any two admissible factors satisfy \[ |{\mathbb{E}}[(m_1-m_2)f]|=|{\mathbb{E}}[(m_1-m_2)(f-v)]|\leq2M\epsilon. \] Approximate spanning therefore bounds a payoff's price ambiguity even when it does not identify the entire factor. Without the norm bound this conclusion need not follow.

Checks and remaining task

Conditional moments were converted using bounded instruments, avoiding unjustified products outside $L^2$. Positivity and open-set endpoints were kept explicit. This establishes the affine characterization and several substantive sufficient conditions, but does not supply economically verifiable complete spans, a general nonparametric statistical recovery rate, or positivity-preserving optimal regularization when the physical law is estimated. The next step is to specify singular-value decay and a smoothness class for $m$, then balance regularization bias, moment noise and physical-law error. Final status: UNRESOLVED.

Completion Estimate

65%

This is a post hoc, heuristic estimate for the full catalogue target. The attempt gives an exact conditional orthogonality characterization of admissible discount factors, identified projections, sharp finite-state ambiguity, and approximate-span and perturbation bounds. Economically verifiable completeness and general positivity-preserving statistical recovery with an estimated physical law and explicit regularization rates remain unresolved.

Source

Zhang Chen and Chen Kay, Historical Developments in Probability Measures for Asset Pricing: From State Prices to Modern Pricing Kernels, arXiv:2605.27658 (2026), Sections 18.9 and 20. https://arxiv.org/pdf/2605.27658.

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