Abstract
This paper aims to make explicit the methodological conditions that should be satisfied for the Bayesian model to be used as a normative model of human probability judgment. After noticing the lack of a clear definition of Bayesianism in the psychological literature and the lack of justification for using it, a classic definition of subjective Bayesianism is recalled, based on the following three criteria: an epistemic criterion, a static coherence criterion and a dynamic coherence criterion. Then it is shown that the adoption of this framework has two kinds of implications. The first one regards the methodology of the experimental study of probability judgment. The Bayesian framework creates pragmatic constraints on the methodology that are linked to the interpretation of, and the belief in, the information presented, or referred to, by an experimenter in order for it to be the basis of a probability judgment by individual participants. It is shown that these constraints have not been satisfied in the past, and the question of whether they can be satisfied in principle is raised and answered negatively. The second kind of implications consists of two limitations in the scope of the Bayesian model. They regard (1) the background of revision (the Bayesian model considers only revising situations but not updating situations), and (2) the notorious case of the null priors. In both cases Lewis’ rule is an appropriate alternative to Bayes’ rule, but its use faces the same operational difficulties.
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Notes
One can think of four major exceptions: Cohen’s (1960) pioneering work on “psychological probability”; Hammond’s theory of social judgment (Hammond 1955); Anderson’s theory of the integration of information (Anderson 1991) and research on “fast and frugal heuristics” (Gigerenzer et al. 1999). More generally, and from a descriptive point of view, it has often been claimed that normative models in general, and the Bayesian model in particular, require unrealistic computational faculties, and are therefore poorly adapted to the realistic description of human judgment (Chase et al. 1998; Oaksford and Chater 1992). Bayes’ identity (see Appendix 1), in particular, demands the combination (multiplication, addition and subtraction) of at least three different numerical items.
For instance, the famous paper by Gigerenzer and Hoffrage (1995) which underscores the importance of the frequentist format in using Bayes’ identity is entitled, “how to improve Bayesian reasoning without instruction: frequency formats.”
Of course, the authoritativeness of many authors mentioned in the present paper is acknowledged. Our point concerns the use that they had of the term “Bayesianism” in their writings.
More precisely, what appeared in Bayes’ essay is the definition of conditional probability (see the first formula in Appendix 1). It is Laplace, in his “Mémoire sur la probabilité des causes par les événements,” who offered, in 1774, the first formulation of Bayes’ identity (the second formula in Appendix 1; see Laplace 1986).
However, Bayesian theory does not automatically reject frequentist information in order to work out (subjective) probability estimate. It may be the case that a coherent subjective judgment of an event probability equals the frequency of occurrence of this event (de Finetti 1964).
According to the frequentist interpretation, probability is defined as the limit of a frequency. It is unique and in no case does it depend on the individuals’ knowledge (the epistemic criterion is not respected). In this view, the phrase “the probability of event E is P” indicates that probability of event E is a property of the event itself which possesses an objective value that can be calculated or approximated by means of logical or physical operations.
The Bayesian model relies on a very constraining criterion of coherence due to the axiom of additivity of probabilities. As we have underlined, other possible ways to model degrees of belief exist, based on a weaker coherence criterion obtained by loosening the axiom of additivity. For each of these normative models, theorists have proposed specific sets of axioms that degrees of belief should satisfy. From a technical point of view, some of these models, and notably all of the probability interval models, can be considered as generalizations of the Bayesian model (and especially of its subjective variety, see Walley 1991) with less constraining criteria, rather than alternatives to it. Taking these models as norms of reference would relax the constraint of additivity, but would not solve the methodological difficulties already mentioned.
Results of the few studies that follow this methodology indicate that participants produce revised probabilities close to those calculated by the experimenter using Bayes’ identity and participants’ prior probabilities and likelihoods as input (for example: Baratgin 2002b; Evans et al. 1985; McCauley and Stitt 1978; Peterson et al. 1965).
In distinguishing between revising and updating (which are two different kinds of revision), we follow a well-established distinction in artificial intelligence.
There is a domain in which the notion of possible worlds seems applicable, and therefore the use of Lewis’ rule justifiable, namely counterfactual reasoning: theorists of this domain explicitly refer to the philosophical discussion of possible worlds (Roese and Olson 1995). More precisely, the analysis of counterfactuals leads one to consider, on one hand, the ease with which the antecedent condition can be altered (see Kahneman and Miller’s 1986 construct of mutability, of which one factor is clearly linked to plausibility or feasibility, and ultimately to the proximity to the actual world); and on the other hand, the closeness of a possible expected outcome to the actual outcome. It would seem that individuals have an intuitive notion of a “distance between possible worlds.” This notion is the basis of the process of revising by Lewis’ rule (see Appendix 3).
For example, one of the important postulates is strong conservation. It is common to the systems of axioms for probabilistic revising and updating. It states that if a message is already validated by the initial belief, the final belief is unchanged: if P(D)=1, then P D (H)=P(H).
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Acknowledgments
The authors thank Denis Hilton, David Over and Steven Sloman for their comments on various drafts of this paper.
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Appendices
Appendix 1
One can put into question the extensively used term of “Bayes’ rule.” The literature indeed offers several specifications of Bayes’ rule. Although these specifications are equivalent, it appears important to distinguish three major forms. Given two alternative hypotheses H and \(^{\neg}H\), one event D such that \(D \ne \emptyset\), let P(H) be the prior probability of H, P(H|D) the posterior probability, P(D|H) and \(P(D | ^{\neg}H)\) the likelihood and finally P(D) the probability of the data D.
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Form 1.
“Conditional probability”:
$$P(H | D) = \frac{{P(H \cap D)}}{{P(D)}},$$ -
Form 2.
“Bayes’ identity”:
$$P(H | D) = \frac{{P(H) P(D | H)}}{{P(D)}},$$ -
Form 3.
“Derived Bayes’ identity”:
$$O(H | D) = \frac{{P(H | D)}}{{P(^{\neg}H | D)}} = \frac{{P(H)P(D | H)}}{{P(^{\neg}H)P(D |^{\neg}H)}} = O(H) \frac{{P(D | H)}}{{P(D |^{\neg}H)}} = O(H)L(D | H).$$
The vast majority of studies have exclusively used the second form of Bayes’ rule (b). Few studies have used the third form (c), considering more specifically the phenomenon of conservatism (for example Phillips and Edwards 1966) or the base rate neglect (for example Kahneman and Tversky 1973). Pieces of research quoting the first form of Bayes’ rule (form a) are much less numerous (see nevertheless Gigerenzer and Hoffrage 1995; Lewis and Keren 1999; Mellers and McGraw 1999).
Appendix 2
In the 1960s, several studies in various fields (computer science, psychology and medicine) strove to define a rule that would hold in the case where the new evidence D is not certain (let it be D*). Dodson (1961) addressed this problem. An uncertain message D* can lead one to elaborate subjective judgment on the probability of D being true, thus yielding P(D|D *) and its complementary \(P(^{\neg}D|D^{*})\). His idea was to incorporate P(D|D *) and \(P(^{\neg}D|D^{*})\) in the conditioning of H based on the notion of expectation. Dodson suggested that posterior probability must be equal to the sum of the probabilities conditionally to D and \(^{\neg}D\) multiplied by the probabilities of being in the situation where D is true or where \(^{\neg}D\) is true. Dodson (1961) established the following rule:
One can notice that in the degenerated cases where P(D|D *)=1 and \(P(^{\neg}D|D^{*}) = 0\), the rule reduces to simple conditioning \(P(H | D^{*}) = P(H | D) \, {\rm and} \, P(H | D^{*}) = P(H |^{\neg}D)\) when P(D|D *)=0 and \(P(^{\neg}D|D^{*}) = 1\), respectively. In other words, Dodson’s rule can be viewed as the generalization of Bayes’ identity. Independently, Jeffrey (1965) proposed the same rule of revision. However, in the subjective interpretation of the Bayesian model as specified in the present paper, an individual can revise his/her probability directly when learning D*, and it can be shown that, conversely, Bayes’ identity is equivalent to the Dodson–Jeffrey rule (under the assumption that D* depends on D but not on H; see for example Gettys and Wilke 1969; Jaynes 1994; Schaefer and Borcherding 1973; Schum and du Charme 1971).
Appendix 3
Gärdenfors (1988) showed that Lewis’ (1976) rule (imaging) can be analyzed as a rule for probabilistic revision. In this case, the methodology of revision is different from the one provided by Bayes’ rule. We simply intend here to give an intuitive idea of it (for a detailed technical analysis, see Gärdenfors 1992; Pearl 2000; Walliser and Zwirn 2002). In order to explain this rule, it seems convenient to use Kripke’s (1962) possible worlds semantics. An agent considers a distribution of probability on possible worlds. Following a message invalidating a possible world, degrees of belief concerning this world are redistributed on the other possible worlds that the agent considers to be the closest to the invalidated world. Let us consider the following example (Dubois and Prade 1994; Walliser and Zwirn 2002). A basket may be described by four worlds depending on whether it contains an apple (a) or not \((\neg a)\) together with a banana (b) or not \((\neg b)\). Someone believes at t 0 that the basket contains at least one fruit: \(K = (a \wedge b) \vee (a \wedge \neg b) \vee (\neg a \wedge b)\). Let us assume that the person’s prior probabilities associated to each possible world are 1/2 for \((a \wedge b)\), 1/3 for \((\neg a \wedge b)\), 1/6 for \((a \wedge \neg b)\) and 0 for \((\neg a \wedge \neg b)\). A revising message brought up by a reliable direct witness informs the person that there is no banana: \(A = (a \wedge \neg b) \vee (\neg a \wedge \neg b)\). The revised belief K*A is now \((a \wedge \neg b)\), so that the posterior probability allocated to \((a \wedge \neg b)\) is 1. This is what Bayes’ identity gives:
But with Lewis’s rule (or imaging) one will end up with a different result. An updating message says at t 1 that there is no more banana. In this updating situation, the revised belief K*A is \((a \wedge \neg b) \vee (\neg a \wedge \neg b)\) because the reasoner starts afresh a distribution over all possible worlds. In order to do so, the prior probabilities (1/2 and 1/3) attached to \((a \wedge b) \, {\rm and} \, (\neg a \wedge b)\) are distributed over other close worlds. One can think that the world \((a \wedge b)\) is closer to \((a \wedge \neg b)\) than to \((\neg a \wedge \neg b)\) (choosing arbitrarily the intuitive physical action as a basis to define the distance) and therefore the degree of belief 1/2 attached to \((a \wedge b)\) is attributed to
Alternatively, one can think that the world \((\neg a \wedge b)\) is closer to \((\neg a \wedge \neg b)\) than to \((a \wedge \neg b)\) and therefore the degree of belief 1/3 attached to \((\neg a \wedge b)\) is attributed to \((\neg a \wedge \neg b)\):
This example illustrates the two situations of revision using, of course, a distance arbitrarily chosen in the updating case. In the latter case (Lewis’ rule), the initial belief can be thoroughly modified, since one could expect to have no fruit anymore in the basket following the message.
Appendix 4
Kolmogorv’s axioms contain the following two “convexity rules” (the impossible event is noted \(\emptyset\) and the set of possible results Ω):
-
1.
\(P(\emptyset) = 0 \; {\rm and} \; P(\Omega) = 1\);
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2.
H is said to be “significant” if and only if 0<P(H)<1;
and the additivity rule:
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3.
\({\rm If} \, H \cap G = \emptyset, \; {\rm then} \; P(H \cup G) = P(H) + P(G)\)
together with its corollary, the complementarity constraint \(P(H) + P(^{\neg}H) = 1\).
The conditional probabilities must satisfy the rule of compound probabilities:
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4.
\(P(H \cap G) = P(H)P(G | H)\);
and its corollary, namely Bayes’ identity (Appendix 1).
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Baratgin, J., Politzer, G. Is the mind Bayesian? The case for agnosticism. Mind & Society 5, 1–38 (2006). https://doi.org/10.1007/s11299-006-0007-1
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DOI: https://doi.org/10.1007/s11299-006-0007-1