1 Introduction
Expected utility theory (EUT) is the standard theoretical model of choice under risk used in economic analysis. EUT posits that the utility assigned to a lottery or prospect is linear in the probability of each possible outcome of the lottery. While EUT is an appealing formulation for economic modeling, a number of experiments have called it into question as a descriptive model of choice under risk (see Starmer (Reference Starmer2000) for a review of the literature). On the other hand, specifications allowing probabilities to be weighted by a function pi(p), where pi(p) has an inverted S-shape, provide a good empirical fit to the available experimental data (see for example Prelec, Reference Prelec1998, Wu and Gonzalez, Reference Wu and Gonzalez1996, Camerer and Ho,Reference Camerer and Ho1994, or Gonzalez and Wu, Reference Gonzalez and Wu1999). The inverted S-shape corresponds to an overweighting of low probabilities and an underweighting of high probabilities. In recognition of this empirical support, probability weighting is incorporated as a key assumption of several theories of choice under risk, including prospect theory (Kahneman and Tversky, Reference Kahneman and Tversky1979), rank dependent expected utility theory (Quiggin, Reference Quiggin1993), and cumulative prospect theory (Tversky and Kahneman, Reference Tversky and Kahneman1992).
A particularly striking phenomenon that can arise as a consequence of probability weighting is the common ratio violation.Footnote 1 Consider two lotteries and an individual with a utility function U(x). The first yields a payoff of xi not-equals 0 with probability p i and a zero payoff with probability 1-p i. The second lottery yields x j not-equals 0 with probability p j and zero otherwise. The linearity assumption of expected utility theory implies that an individual who chooses the first lottery over the second one must also choose a lottery that delivers xi with probability q*p i over a lottery that yields x j with probability q*p j. Clearly, if p i U(xi) is greater than or equal to , p j U(x j)), then q*p i U(xi) is greater than or equal to q*p j U(x j)). As originally conjectured by Allais (Reference Allais1953), common ratio violations which result in indifference curves in the probability triangle (explained later) that fan out or fan in, have been found to be widespread in the domain of positive payoffs for lotteries involving monetary outcomes (see for example Starmer and Sugden, Reference Starmer and Sugden1989).
The empirical support underlying probability weighting and common ratio violations comes primarily from experimental studies in which all outcomes involve non-negative monetary payments (see for example Loomes, 1991; Hey and Orme, 1994; or Harless and Camerer, 1994).Footnote 2 However, many economic decisions involve the possibility of losses. Examples include a decision to invest in a stock, to choose among alternative medical procedures, or to trust another person or institution in a business or personal transaction. A few studies have explored decisions in the domain of losses, and they have used one of two techniques to induce negative payoffs. In some studies, researchers use hypothetical payoffs; examples include Kahneman and Tversky (Reference Kahneman and Tversky1979) and Abdellaoui (Reference Abdellaoui2000). In other studies, participants are given a real cash endowment at the beginning of the experiment and real losses are deducted from this initial balance; examples include Holt and Laury (2004) and Mason et al.(Reference Mason, Shogren, Settle and List2005).
However, many real life decisions involve negative outcomes that are not monetary. Consider a cancer patient who is asked to make a choice between two uncomfortable medical treatments that involve tradeoffs between probabilities and utilities of different prospective states of health (e.g., radiation therapy versus extensive surgery). Another example is the decision of a defendant in a criminal case to accept or reject a plea bargain for a reduced sentence in prison. The defendant faces a choice between lotteries over the time of incarceration.
However, a methodological challenge exists when studying decisions over non-monetary adverse outcomes: how do we induce real outcomes of this typeFootnote 3 in the laboratory? Some authors have used aversive stimuli to investigate other principles of decision making. For example, Ariely et al.Reference Ariely, Loewenstein and Prelec2003) used annoying sounds as well as having subjects place their fingers inside a tightening vice to study the effects of anchoring on preferences. Coursey et al.(1987) required individuals to drink sucrose octa-acetate, an unpleasant tasting liquid, to study willingness-to-pay and willingness-to-accept decisions for a "bad", that is, a good with negative value. In this paper, we use painful electric shocks to induce negative payoffs. Pain is a good measure of disutility as almost everyone would rather avoid it. In addition, as a means of inducing disutility, the use of electric shocks satisfies Smith’s (Reference Smith1982) precepts pertaining to the appropriateness of a reward medium for an experiment: monotonicity and dominance. We can presume that a larger shock (in either magnitude or duration) is worse than a smaller one.Footnote 4 For a fixed duration, the disutility of a shock is monotonic in the current, and therefore it is monotonic in its voltage. Furthermore, for our simple decision task, which is described below, and given the voltage levels applied in our experiment, it is quite reasonable to presume that the differences between voltage levels from the alternative choices are large enough to dominate the costs of deciding between alternatives. Physical pain, unlike cash payments, also has other advantages in inducing individual incentives, in that the recipient consumes it instantly and cannot transfer it to other individuals.
In this paper, we consider whether the phenomenon of probability weighting, and in particular the inverted S-shaped pattern of probability distortion, is observed when people face lotteries that involve painful shocks, and whether common ratio violations, which have been observed for lotteries involving positive monetary payments, also appear in our setting. In addition, although probability weighting can predict a complex pattern of fanning in and fanning out inside the probability triangle, for the particular gambles that we consider, we expect to see more risk aversion when gambles get better (i.e., when there is a lower overall chance of a shock); which means that indifference curves would tend to fan-out. We find that both probability weighting and common ratio violations are prominent features of our data. The median probability weighting parameter we estimate is very similar to those observed in decisions over negative hypothetical monetary payoffs (Tversky and Kahneman, Reference Tversky and Kahneman1992; Abdellaoui, Reference Abdellaoui2000). The results suggest that a similar process of probability weighting characterizes lottery choice for both monetary and non-monetary outcomes when payoffs are negative.
2 Experimental design and procedures
A total of 37 subjects participated in the study. Seventeen were male and 20 were female. The average age of participants was 25 years, and 17 of the 37 subjects were students. Each individual participated in the experiment at a separate time, and thus during each session only one participant was present. Sessions were conducted at the Emory University Hospital in Atlanta, Georgia, USA. Each session lasted an average of two hours and each participant was awarded $40 at the end of his session. Each session consisted of a series of 180 trials, in which in each trial subjects had the possibility of receiving an electric shock. Shocks were delivered using a Grass SD-9 stimulatorFootnote 5 through shielded, gold electrodes placed 2-4 cm apart on the dorsum of the left foot. Each shock was a monophasic pulse of 10-20 ms duration. During their session, individuals were lying down in an MRI scanner.Footnote 6 While in the scanner, the participant observed a computer screen and used a handheld device to submit their decisions.
At the beginning of the session, the voltage range was titrated for each participant. The detection threshold was determined by delivering pulses starting at zero volts and increasing the voltage until the individual indicated that he could feel them. The voltage was increased further, while each participant was instructed, “When you feel that you absolutely cannot bear any stronger shock, let us know - this will be set as your maximum; we will not use this value for the experiment, but rather to establish a scale. You will never receive a shock of maximum value.” The purpose of this procedure was to control for the heterogeneity of the skin resistance between subjects and to administer a range of potentially painful and salient stimuli in an ethical manner. We measured the strength of the shock administered to an individual by the parameter s, where the associated voltage for an individual was V = s(Vmin-Vmin) + Vmin, where Vmin is the detection threshold (not painful, but just noticeable) and Vmax is the maximum value for the individual. For the remainder of the experiment, s took on values of 0.1, 0.3, 0.6, and 0.9.
After the voltage titration, the first phase of the experiment, which we call the passive phase, began. The software package, COGENT 2000 (FIL, University College London), was used for stimulus presentation and response acquisition. The passive phase consisted of 120 trials. The sequence of activity in each trial is illustrated in Figure 1. The upper part of the figure illustrates the displays that subjects observed on their computer screen. The lower part of the figure shows the timing of events within each trial. At the beginning of each trial, each participant was presented with a pie chart, called the cue, which conveyed both the magnitude of the potential impending shock and the probability with which it would be received. The magnitude of the shock was indicated by the size of an inner circle relative to an outer gray circle. This outer circle corresponded to the individual’s maximum tolerable voltage, Vmax. The area of the inner circle was V s, where s equaled 0.1, 0.3, 0.6, or 0.9, depending on the trial. The probability was indicated by the proportion of the inner circle colored in red on participants’ computer screens, which is shown in Figure 1 as the percentage of the inner circle shaded in the darker color. The five possible probabilities were 1/6, 1/3, 2/3, 5/6, and 1. The particular example shown on the left part of Figure 1 depicts a voltage level with the value of s = 0.6, and a 1/3 probability of the shock being applied. The four possible voltage levels and five possible probabilities yielded 20 voltage-probability combinations, each of which was presented 6 times in the 120 trials that constituted the passive phase of the experiment.
Display on subjects’ screens and timing of activity during the passive phase of the experiment
After the cue was presented for 8 seconds, the shock was then delivered with the appropriate probability.Footnote 7 The word, “outcome,” as shown in the second image located in the upper middle of Figure 1, was presented concurrently with the delivery of the shock on those trials in which a shock occurred. It also appeared at the same point in time on those trials in which a shock was not delivered, providing an indicator to the participant that the trial was over. It remained on display for one second,Footnote 8 after which a display consisting of a visual analog scale appeared on the participant’s screen. The display is shown in the upper-right part of Figure 1. The subject was then required to rate the experience of the trial in a range between “very unpleasant” and “very pleasant.” To indicate his rating, he marked a location on the scale, using a cursor operated by hand. The process then continued to the next trial.
The next phase of the session, which we call the Active Phase, consisted of 60 trials. In each trial, individuals were required to choose between two of the probability/shock combinations that were presented in the passive phase. The available choices differed from one trial to the next. Figure 2 shows an example of the displays that appeared on participants’ screens during a typical trial as well as the timing of a trial. At the beginning of each round, a display similar to the one shown in the upper left of the figure appeared. The figure shows two lotteries presented side by side, and subjects were required to choose one of the two using the keypad provided to them. The two options available in a given trial always had the property that one alternative specified both a higher voltage shock as well as lower probability than the other alternative. For instance, the example shown in Figure 2 represents a choice between 1/6 chance of a shock with s = 0.9 vs. a 1/3 chance of a shock with s = 0.6. The larger inner circle represents the larger shock (i.e., s = 0.9); the probability is represented by the proportion of the area of the inner circle that is colored in red.
Display on subjects’ screens and timing of activity during the active phase of the experimen
After the participant made his choice, there was an 8 second interval, in which the display was augmented by an arrow indicating the lottery chosen. After the 8 seconds had elapsed, the outcome was realized and the word “outcome” was included on the display for 1 second, as shown in the upper right part of Figure 2. Then, the current trial ended and the next of the 60 trials that made up the active phase began. The experimental session ended after the active phase was completed.
3 Results
The results show that the data are consistent with probability weighting, and that the sample parameter value of the particular probability weighting function we estimate is very close to the values reported in previous studies. We first tested the hypothesis that expected utility theory can explain our data. To do so, we estimated the value of a prospect or lottery, V(L)=∑iπ(pi)U(xi), where pi is the probability of outcome xi. using the specification for probability weighting of Tversky and Kahneman (Reference Tversky and Kahneman1992)Footnote 9 Under this specification, the value of a prospect that yields non-positive payoffs under all possible realizations is given by:
The expected utility hypothesis is consistent only with γ = 1. In contrast, previous estimates of the median value of γ for samples of experimental participants incurring hypothetical monetary losses are .69 obtained by Tversky and Kahneman (Reference Tversky and Kahneman1992) and .70 observed by Abdellaoui (Reference Abdellaoui2000). All values γ ∊ (0,1) imply an inverted S-shape probability weighting function, in which relatively low probabilities are over weighted, and relatively high probabilities are underweighted (probabilities of 0 and 1 receive accurate weight for all γ ∊ (0,1].) The parameter lambda is a scaling factor. The parameter alpha measures the convexity (or concavity) of the utility function. The variable xi is the voltage of the shocks administered. There is no guide from prior research about the appropriate level of lambda or alpha because there is no reason to believe that the scale or curvature of the utility function would be the same for electric shocks as for the real and hypothetical monetary payments previous authors have investigated, though there is evidence (Stevens, 1961) that the psychological reaction to the intensity of electric shocks applied to the fingers follows a power function with an exponent of approximately 3.5.
Because we did not elicit certainty equivalents in our experiments, we used a ranking procedure to derive a measure of the relative value of each of the 20 lotteries to each subject. There were 190 possible lottery pairs, but we only observed actual choices for 60 pairs for each individual (i.e., all those pairs for which there was a tradeoff between higher probability and higher pain determined by the value of s). For these sixty pairs, individuals’ choices yielded a revealed preference between the two lotteries. To construct “revealed” preferences for the other 130 pairs (those that were not presented to the subject), we applied a strict dominance criterion. We assumed that individual i would have always chosen a lottery with a lower probability and lower pain over a higher pain, higher probability option.Footnote 10 We determined the rank or “relative preference” of each of the 20 lotteries based on the percentage of times that it was “revealed preferred” to other lotteries. This procedure yields a complete and transitive preference ordering of the 20 lotteries. We then used the ranked lotteries, determined separately for each individual participant, as data to fit the specification in (1). The parameters, alpha, lambda, and γ, were estimated jointly using nonlinear least squares regression with normally distributed errors.Footnote 11
The mean estimated value of the probability weighting parameter γ for the 37 subjects was 0.659, with a standard deviation among the 37 individual estimates of 0.218. The median estimated value was 0.685.Footnote 12 Females tended to have higher estimates (median=0.769 vs. 0.570 for males), but the difference between the two genders was not significant. We then classified our subjects into groups based on whether (a) the EUT value of 1 or (b) the value of γ estimated in Tversky and Kahneman (Reference Tversky and Kahneman1992) of 0.69, fell within the 95% confidence interval of the estimated individual γ (individual estimated values and standard errors can be found in the Appendix). Forty-six percent (17 out of 37) of our subjects’ estimated probability weighting parameters were consistent with Tversky-Kahneman but not with EUT, whereas 14% (5 out of 37) were consistent with EUT but not with Tversky-Kahneman. The rest of the subjects were consistent with both values (24%) or with neither (16%).Footnote 13 Figure 3 shows the proportion of estimated values that fell into the four categories listed above.
Percentage of subjects for whom the γ values of 1 or 0.69 fell within the 95% confidence interval of their individual γ estimate
We now consider the incidence of common ratio violations in the data. Let s h be the more painful and s l be the less painful of two alternative potential shocks presented as a pair-wise choice, and let p h and p l be the higher and lower probabilities among the two alternatives, respectively. In our experiment, common ratio violations were observed when the lottery (s h, p l = 1/6) was chosen over (s l, p h = 2/6), but (s l, p h = 4/6) was chosen over (s h, p l = 2/6), or alternatively, vice versa. Within the context of the Marschak-Machina triangle and under the assumption that the indifference curves are linear Footnote 15, the first sequence of decisions corresponds to “fanning in” of indifference curves; the second sequence, on the other hand, is consistent with “fanning out” of indifference curves. Figure 4 depicts the Marschak-Machina (M-M) triangle with indifference lines. An individual who is indifferent between x and y, and indifferent between z and w will have parallel indifference lines passing through each of the two pairs of points. However, if the individual prefers x to y, then her indifference line will have a higher slope as shown by the darker dashed line passing through x in the figure. Under EUT, if x is preferred to y, then z is preferred to w (shown by the lighter dashed line passing through z). A choice of w would constitute a common ratio violation, and would imply that the indifference line passing through w has a smaller slope than the one passing through x, as depicted by the darker solid line in the figure. Note that the choice of x and w means that the indifference curves are "fanning out". Similarly, Figure 5 depicts "fanning in." In the active phase of the experiment, there were a total of six instances in which common ratio violations could occur. The observed type and number of violations per subject can be found in the Appendix.
Fanning out
Fanning in
The results show that the average number of common ratio violations by individual was 1.95 with a standard deviation of 1.39, which is clearly different from the prediction of EUT.Footnote 15 There is a tendency to commit more fanning out violations than fanning in violations. This is not surprising, as indifference curves that fan out are consistent with overweighting of small probabilities. About 68% of the subjects (25 out of 37) committed one or more fanning out violations, whereas about 46% (17 out of 37) committed one or more fanning in violations. The Fisher exact test shows that the null hypothesis that the proportion of subjects who commit at least one fanning in and fanning out violations are the same is rejected in favor of the alternative of more people committing fanning out violations (p = 0.049; one-tailed). Five subjects committed fanning in violations only; in contrast, seventeen subjects committed uniquely fanning out violations. Finally, there were small differences between the average number of violations committed by females (2.10; std = 1.37) as compared to males (1.76, std = 1.43).
We also considered whether there was consistency between our above classification of subjects (Figure 3) and the observed number of common ratio violations. None of the five subjects whose estimated γ value was consistent with only EUT committed more than two common ratio violations. In contrast, the number of violations by subjects with estimated γ significantly less than 1 ranged from zero to five. Overall, however, there are no statistically significant differences in the median number of violations between these two groups (p > 0.188, one-tailed).
Although the overall fanning effect was as predicted, there were large individual differences. Some participants showed no fanning; whereas others showed fanning in the opposite directions. Were these consistent differences, or just random variation? We found that, within an individual, the direction of violations was consistent, in a specific sense, with their overall choice behavior in the 60 trials of the active phase. To study this consistency, we computed a "mean fanning effect" for each subject from the six instances where individuals could switch preferences, and we asked whether this effect could be predicted from an index of fanning computed from the remaining 54 cases. Fanning out is indicated by a lower tendency to choose the low-probability-high-shock option when overall shock probabilities are smaller (i.e., closer to the top of the M-M triangle in Figure 4). Using the 54 decisions between which common ratio violations cannot be detected from decisions, we conducted a regression with the chosen lottery as the dependent variable. The independent variables were the difference in the logs of the shock intensity of the two options, the difference in the logs of the probabilities of a shock under the two options, and the sum of the two probabilities of receiving a shock under the two options. The regression coefficient for this last variable, which is a measure of the distance from the top of the M-M triangle, was our index of the fanning effect. The coefficient takes on a smaller value, the more the tendency toward fanning out. We found a positive correlation between the individual estimated coefficients of the fanning index, and whether they committed more fanning out than fanning in violations (r=.31, t(35)=1.95, p=.0293, one-tailed).Footnote 16 Thus, individuals differ in a consistent manner in the direction and magnitude of this effect.
4 Discussion
In this paper we provide evidence that non-linear probability weighting, which has been observed when prospective losses are framed in terms of money, also occur in lottery choices when real adverse outcomes are induced with a non-monetary medium. As in previous studies, our estimated values of the probability weighting parameters provide little support for EUT. We find that about 14% of our subjects’ estimated probability weighting parameters is consistent with EUT. In contrast, about 46% of the subjects overweight small probabilities and underweight large probabilities, exhibiting a typical inverted S-shape probability weighting function. Furthermore, the estimated sample median probability weighting parameter we obtain is closely in line with values reported in previous studies. This suggests that probability weighting acts in a similar manner for lottery choice when outcomes are measured in terms of physical pain as well as for hypothetical monetary transfers. This result is consistent with the conjecture that probability weighting is a general phenomenon, and independent of the source of disutility.
We also find that common ratio violations, which are inconsistent with EUT, are widespread. A greater proportion of subjects commit violations consistent with indifference curves that fan out than with fanning in. However, there are large individual differences in the direction and incidence of the violations. Despite these differences, we were able to determine that the direction of subjects’ violations is largely consistent with their overall choice behavior, and not random.
In our view, the results we obtain are encouraging evidence that traditional methodologies used in economics and psychology to study decisions in the domain of negative payoffs lead to the same principles of decision making as those applied in decisions over non-monetary media with real losses. Indeed, we reach almost identical conclusions to previous studies. Our results also suggest a conjecture that in the domain of positive payoffs, the probability weighting parameters estimated for monetary payments would carry over to non-monetary media. In the future, we believe that the methodology of applying physical pain to study decision making may be used to explore the robustness of other behavioral anomalies observed in the laboratory that occur when payoffs are negative.
Appendix
Open access
