Ethical Free Riding: When Honest People Find Dishonest Partners

Experimental setup and key variables

The key variable of interest was people’s decision to switch versus stay with their partners. We study this decision by implementing a novel experimental setting in which participants were assigned a partner and could increase their payoff by coordinated lying. In the experimental choice condition, participants could choose whether to stay with or switch their partner. To investigate how the freedom to choose a partner affects the contagiousness of dishonesty and the overall financial impact of coordinated lies, we compared the choice condition with two additional conditions: a forced-stay condition, in which participants had to stay with their partner throughout the experiment, and a forced-switch condition, in which participants were forced to repeatedly switch their partner.

We employed a modified version of the dyadic die-rolling task (Weisel & Shalvi, 2015) in which participants are assigned a partner and are asked to report the outcome of a die roll presented on a computer screen (Kocher et al., 2017). Participants earn extra money if they and their partner report the same outcome, with higher outcomes corresponding to higher pay. Employing experimental tasks such as reporting die-roll outcomes to assess dishonesty is a common practice both in the lab and the field (Fischbacher & Föllmi-Heusi, 2013; for a meta-analysis, see Abeler et al., 2016). The task has good external validity. Lying in these tasks is correlated with diverse unethical behaviors such as not paying for public transport (Dai, Galeotti, & Villeval, 2017), being absent from work without a reason (Hanna & Wang, 2013), and not returning undeserved pay (Potters & Stoop, 2016).

Participants

Participants were recruited from the subject pool of the Center for Research in Experimental Economics and Political Decision Making (CREED) at the University of Amsterdam. In total, 372 participants (186 females; age: M = 22.00 years, SD = 3.38 years) took part in 19 experimental sessions. All sessions lasted approximately 1 hr and were run by two experimenters who answered participants’ questions, if there were any. All data and materials are available on the Open Science Framework (https://osf.io/bdvxs/). Screenshots of the instructions also appear in the Supplemental Material available online. No participants were excluded from any of the analyses, and all independent variables and manipulations are reported in the Method section and the Supplemental Material. Average earnings per participant were €18.68.

The dyadic die-rolling task

Participants were seated in individual cubicles in front of a computer screen, where they read the task instructions. Each participant was paired with a partner and assigned the role of first or second mover. Participants’ roles as first and second movers remained fixed throughout the experiment. To avoid reputation concerns, we made sure that participants were not aware, during or after the task, with whom they were partnered. In the first stage of each round, the first mover observed a random die roll on a computer screen, presented as a video segment (Kocher et al., 2017), and was instructed to report the outcome. In the second stage, the second mover saw the outcome the first mover reported on the computer screen and then observed an independent, random die roll and was asked to report it (see Fig. 1a). Dyad members then received a summary of their own and their partner’s report and a payoff summary for that round. After each block of three rounds, participants saw a block summary. Overall, the task lasted for 30 rounds (10 blocks), but participants were not aware of the total number of rounds in the task. Each participant had to correctly answer three questions regarding the task’s rules to ensure task comprehension before starting the task (see the Supplemental Material). Per CREED lab rules, no experimental deception was used, and decisions had real monetary consequences.

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Fig. 1.

Task procedure, payoff scheme, and conditions. As shown in (a), the first mover, A, observes a die roll on a computer screen and reports the outcome to the second mover, B. B then observes an independent die roll on the computer screen and reports the outcome. Then A and B learn about both reports and the corresponding payoff. As shown in (b), if the number that B reports matches the number A reports (a double), each earns half (A/2) of the reported number in euros. Otherwise, they earn no extra pay. In the choice condition, participants indicated whether they wanted to switch partners (black letters in panel c) or stay with the same partner (white letters in panel c) after each block of three consecutive rounds. If at least one partner in a dyad wanted to switch, the dyad was split, and both members of that dyad were assigned a new partner for the next block. In the forced-stay condition, participants engaged in the task for 30 rounds with the same partner. In the forced-switch condition, participants were assigned a new partner after every block.

Payoff scheme

For every round, each participant received a fixed payment of €3 regardless of the outcomes reported. Beyond that amount, if the first and second mover reported the same outcome (i.e., a double), they received an extra payment associated with their reports. Specifically, each participant earned half of the reported outcome’s worth in euros (e.g., if both reported “two,” each earned an extra €1; if both reported “six,” each earned an extra €3). If the dyad did not report a double, they received no extra payment (see Fig. 1b). Thus, both participants had an incentive to misreport their die-roll outcomes and coordinate their reports. The first mover had an incentive to report the highest die-roll outcome possible, whereas the second mover had an incentive to match the first mover’s report. Note that compared with a dishonest first mover, a dishonest second mover has more impact on the dyad’s payoff because the second mover can guarantee a double in every trial, whereas the first mover can only increase the potential value of the double.

At the end of the task, one block of three consecutive rounds was randomly selected for pay. Thus, on top of the fixed payment of €9 (3 rounds × €3) per block, participants earned a variable amount depending on their own and their partner’s honesty, or lack thereof. The expected value if both dyad members report honestly was €0.29 ([€0.5 + €1 + €1.5 + €2 + €2.5 + €3] × 1/6 × 1/6) per round. On average, each member of a completely honest dyad would thus earn an extra payment of €0.88 (3 trials × €0.29) per block. Maximizing profit by reporting dishonestly, however, can increase participants’ extra payment tenfold. In a fully dishonest dyad, the first mover would report the highest die-roll outcome (a six), corresponding to a payoff of €3, and a dishonest second mover would guarantee a double by matching this number. A fully dishonest dyad could thus earn an extra payment of €3 per round, leading to a total payment of €9 (3 trials × €3) per block. Importantly, we chose the payoff scheme so that by reporting honestly, participants would earn the usual hourly payment at our lab.

Because the die-roll outcomes were presented on the computer screen, we were able to identify for each report whether a participant was honest or not. Participants were informed that every time a double was reported in which one or both partners misreported the number they observed, the dyad’s earnings from the double would be subtracted from a planned donation to a charity (see the Supplemental Material for details). Thus, the instructions made clear that it would be possible to determine whether participants misreported the die-roll outcome when data collection was completed.

Partner selection

In the experimental choice condition, participants were asked whether they wanted to stay with their partner or switch to a new partner after each block of three rounds. Participants could thus end their current partnership and look for a new partner. If at least one of the dyad members wanted to switch, and given that at least one more person from another dyad in the session wanted to switch, the dyad would split and both dyad members were reassigned a new partner (Fig. 1c). For details on the algorithm used to reassign participants, see the Supplemental Material. We further ran two control conditions in which we did not allow for partner choice. In the forced-stay condition, the first and second movers interacted with one another across all 30 rounds. In the forced-switch condition, the first and second movers were forced to switch to a new partner after each block of three rounds. Participants read all the instructions before starting the experiment and received clarifications if they asked for them.

Analysis approach

In both the choice and forced-switch conditions, participants could potentially interact with all other first and second movers in their session. The nested nature of the choice and forced-switch conditions meant each session of 20 participants was treated as one independent observation. In the forced-stay condition, each participant interacted with only 1 participant, making the dyad (rather than the session) one independent observation. Given the size of our subject pool, we opted to split our sample in a way that allowed us to obtain the most independent observations for each condition. Thus, in the choice (n = 160) and forced-switch (n = 160) conditions, we ran eight sessions of 20 participants (i.e., 10 dyads) per session, and in the forced-stay condition, we ran three sessions with a total of 52 participants (i.e., 26 dyads), leading to a total sample of 372 participants. In total, we had 8 strictly independent observations in the choice and forced-switch conditions and 26 independent observations in the forced-stay condition. In previous work assessing the effect of partner selection on various economic games (e.g., Abbink, 2004; Page, Putterman, & Unel, 2005), data were collected from 144 to 256 participants, and there were between 6 and 9 independent observations for the partner-selection conditions. Our sample size compares favorably with these studies. We thus feel confident that our sample size and number of independent observations were sufficient to detect effects. All in all, our design allowed us to analyze both choice-based switching patterns and the contagiousness of dishonesty between participants and dyads operating within a large group and across a relatively long time horizon (30 rounds).

We performed data analysis on strictly independent observations by aggregating across sessions (in the choice and forced-switch condition) or dyads (in the forced-stay condition) or by fitting mixed-effects regression models (also called multilevel regression). To account for the nested structure (in dyads and participants), we specified two random intercepts, one for each participant (with multiple observations across rounds) and one for each unique dyad in these models. When the dependent variable was binary, we fitted a logistic mixed-effects regression model. Further, when the dependent variable had natural boundaries (e.g., die-roll reports were restricted to be between one and six), we treated the data as left- and right-censored to avoid biased estimates resulting from heteroscedasticity. All mixed-effects models were fitted with R and JAGS using a Bayesian approach with noninformative priors. We hence do not report p values for these models but instead report the Bayesian 95% confidence interval (see the Supplemental Material for further details).

Finding a partner in crime

In the choice condition, we categorized each participant as an honest person (H) if he or she reported the outcomes that appeared on the computer screen in all three rounds in a given block, or as a liar (L) otherwise. This procedure led to four possible dyad types: LL (lying first mover, lying second mover; accounted for 50% of the dyads in our sample), LH (lying first mover, honest second mover; 4% of the sample), HL (honest first mover, lying second mover; 31% of the sample), and HH (honest first mover, honest second mover; 15% of the sample). Figure 2 depicts the proportion of participants who asked to switch partners on the basis of their role (first or second mover), separately for each dyad type. Because data were clustered in dyads and participants (across blocks) and the dependent variable was binary (0 = stay with partner, 1 = switch partner), we fitted a random-intercept logistic regression model to the data, as described above. Results revealed that dishonest people indeed sought a partner in crime, supporting Hypothesis 1. Dishonest first movers were much more likely to ask to switch partners when interacting with an honest versus a dishonest second mover, whereas dishonest second movers were much more likely to ask to switch partners when interacting with an honest versus a dishonest first mover (Fig. 2; random-intercept logistic regression; HL estimate vs. LL baseline: b = 3.52, 95% confidence interval, or CI = [1.98, 5.27]; LH estimate vs. LL baseline: b = 6.53, 95% CI = [4.55, 8.84]). Likewise, when both dyad members were dishonest, the dyad was very stable, and its members asked to switch only 3.5% of the time (1.4% for first movers, 5.6% for second movers).

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Fig. 2.

Proportion of first movers (black) and second movers (blue) who chose to switch partners, separately for each dyad type (LL = lying first mover, lying second mover; LH = lying first mover, honest second mover; HL = honest first mover, lying second mover; HH = honest first mover, honest second mover).

Furthermore, the more times a second mover matched a dishonest first mover’s report (i.e., reported a double), the less likely the dishonest first mover was to ask to switch (Fig. 3a; random-intercept logistic regression; number-of-doubles estimate: b = −8.61, 95% CI = [−12.84, −4.83]), and the more times a first mover reported the highest possible outcome, six, the less likely a dishonest second mover was to ask to switch (Fig. 3b; random-intercept logistic regression; number-of-sixes estimate: b = −1.30, 95% CI = [−1.62, −0.99]). Hence, in line with Hypothesis 1, results showed that dishonest participants preferred partners who helped them secure the highest profit possible.

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Fig. 3.

Proportion of dishonest first movers who chose to switch partners as a function of the number of doubles reported in the previous block (a) and proportion of dishonest second movers who chose to switch partners as a function of the number of sixes reported by the first mover in the previous block (b).

A preference for honest partners?

As predicted, people who were willing to violate rules to maximize profit systematically switched partners until they were paired with a like-minded dishonest partner. But what did honest people do? Consider an honest first mover who is paired with a dishonest second mover. The first mover reports the number appearing on the screen, including the less profitable ones and twos, whereas the dishonest second mover matches every time. The honest first mover clearly prevents the dyad from maximizing potential profit, but at the same time, financially benefits from the second mover’s dishonesty. In such a case, would the honest first mover switch in the hope of finding a like-minded honest partner? Or, alternatively, stay with the lying partner and enjoy both worlds—being honest while profiting from the other’s dishonesty?

Results revealed that honest first movers systematically engaged in ethical free riding, supporting Hypothesis 2b over Hypothesis 2a. Honest first movers were less likely to ask to switch when their partner (the second mover) was a liar versus an honest person (Fig. 2, Table 1; random-intercept logistic regression; HL estimate vs. HH baseline: b = −3.08, 95% CI = [−4.37, −1.83]).

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Table 1.

Results of the Logistic Random-Intercept Regression Modeling the Choice to Switch (0 = Stay, 1 = Switch) in the Choice Condition as a Function of Dyadic Relationship

Predictor	Estimate	SD	95% CI
Intercept (first mover in HH dyad)	0.07	0.583	[−1.043, 1.239]
LL dyad	−6.58	0.966	[−8.512, −4.772]
LH dyad	−0.05	0.895	[−1.849, 1.682]
HL dyad	−3.08	0.645	[−4.368, −1.835]
Second mover	−0.07	0.748	[−1.494, 1.448]
Second Mover × LL Dyad	2.51	1.036	[0.537, 4.609]
Second Mover × LH Dyad	0.19	1.079	[−1.926, 2.289]
Second Mover × HL Dyad	3.37	0.821	[1.722, 4.970]
Random-intercept error term (dyad)	2.09	0.319	[1.513, 2.747]
Random-intercept error term (participant)	2.27	0.338	[1.643, 2.945]

Note: We compared the interaction model with a null model and a model with only main effects to test whether the full model with interaction terms explained significantly more variance than a simpler model. Compared with the null model, a model with main effects significantly increased the likelihood of the data given the model, χ²(4) = 149.39, p < .001. Furthermore, a model with main and interaction terms significantly increased the likelihood of the data given the model, χ²(3) = 21.24, p < .001. CI = confidence interval; HH = honest first mover, honest second mover; HL = honest first mover, lying second mover; LH = lying first mover, honest second mover; LL, lying first mover, lying second mover.

One may argue that an honest person facing a dishonest partner may not switch because of the ambiguity associated with the partner’s actions. It is not trivial for first movers to identify whether their partner was lying or not because there was a chance that the partner actually observed the same outcomes as they did. Indeed, the likelihood of a second mover matching exactly one of the first mover’s three die rolls equals 35%. If ambiguity, rather than ethical free riding, is driving honest first movers’ decision, we should observe that the more doubles a second mover reports, the less likely the first mover is to stay with this person. The reason is that with every additional double reported, the ambiguity about the second mover’s dishonesty fades away. For example, the likelihood that a second mover would honestly match the first mover’s reports three out of three times is less than 0.5%.

Our data suggest that honest first movers were ethically free riding rather than refraining from switching a partner because of ambiguity concerns. As Figure 4a shows, the more times a second mover matched an honest first mover’s report (i.e., reported a double), the less likely the honest first mover was to choose to switch (Fig. 4a; random-intercept logistic regression; number-of-doubles estimate: b = −3.36, 95% CI = [−4.58, −2.27]). In particular, honest first movers chose to switch in 46% of the cases if their partner did not match their reported numbers (possibly seeking a more profitable relationship) but only in 11% of the cases if their partner matched all of their reports, indicating they preferred a dishonest over an honest partner. Therefore, honest people seemed comfortable with profiting from the unambiguous dishonesty of their partner while they themselves remained honest.

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Fig. 4.

Proportion of honest first movers who chose to switch partners as a function of the number of doubles reported in the block (a) and proportion of honest second movers who chose to switch partners as a function of the number of sixes reported by the first mover in the block (b).

The temptation for honest people to engage in ethical free riding, however, depends on the mover’s position. Compared with second movers (who can secure a double every time), first movers have no control over the reporting of a double and can determine only the doubles’ potential worth (i.e., moving from an expected value of 3.5 if honest to 6 if dishonest). As a result, for honest participants, having a dishonest second mover as a partner is more profitable than having a dishonest first mover as a partner. The temptation to ethically free ride for an honest first mover is hence higher than the temptation for an honest second mover. Specifically, the expected payment for an honest first mover increases from €0.87 (€1.75 × 1/6 × 3 rounds) per block to €5.25 (€1.75 × 1 × 3 rounds) per block when switching from an honest to a dishonest second mover. Thus, honest first movers face a temptation of a 503% premium for switching from an honest to a dishonest partner. The expected payment for an honest second mover, by contrast, increases from €0.87 per block when paired with an honest first mover to €1.50 (€3 × 1/6 × 3 rounds) per block when paired with a fully dishonest first mover that always reports sixes. Thus, honest second movers face a temptation of only a 72% premium for switching from an honest to a dishonest partner.

In line with the notably lower temptation for second movers to switch to a dishonest partner, we found no evidence for ethical free riding among honest second movers. Honest second movers were as likely to choose to switch when they were paired with a dishonest or an honest first mover (Fig. 2, Table 1; random-intercept logistic regression; second-mover LH vs. HH estimate: b = 0.19, 95% CI = [−1.93, 2.29]). Furthermore, honest second movers were indifferent to the number of sixes reported by the first mover when they decided whether to switch or not (Fig. 4b; random-intercept logistic regression; number-of-sixes estimate: b = −2.70, 95% CI = [−10.69, 4.22]). Note that whereas honest first and second movers in our experiment may not have consciously calculated the exact expected value when choosing between switching or staying with their partners, their switching decisions were consistent with the notion that a dishonest second mover has more influence on the dyads’ payoff than a dishonest first mover.

Taken together, supporting Hypothesis 1, dishonest people seek a dishonest partner who will allow them to secure high payoffs on the basis of mutual rule violations. Supporting Hypothesis 2b, honest people do not seek like-minded honest peers. Instead, honest first movers exploit the freedom to choose a partner and switch away from honest second movers. When paired with a dishonest second mover, many participants engaged in ethical free riding. Ethical free riding allows honest first movers to remain honest but secure high profits from the dishonest behavior of their partners.

The prevalence of ethical free riders

We assessed the prevalence of ethical free riding by classifying participants according to the most common choice strategy they exhibited throughout the experiment (in the choice condition). In particular, we classified each participant’s behavior on a block-by-block basis and then assigned unique labels for each individual depending on the behavior that was most prevalent for this person. Specifically, (a) ethical free riders were honest people (i.e., reported the outcomes observed in all three rounds) who chose to switch when paired with an honest partner and stay when paired with a liar in most of the blocks, (b) Kantian truth tellers were honest people who chose to switch when paired with a liar and stay when paired with an honest partner, (c) brazen liars were liars (i.e., misreported the die-roll outcome in at least one out of three rounds) who chose to switch when paired with an honest partner and stay when paired with a liar, (d) tolerant liars were liars who chose to stay when paired with an honest partner, and (e) confused liars were liars who chose to switch when paired with a liar.

In total, most participants (70.6%) were classified as liars, with the large majority being brazen (89.4% brazen liars vs. 10.6% tolerant liars). Among the percentage of honest people (29.4%), the majority were ethical free riders (63.9%) and a minority were Kantian truth tellers (36.1%). The rank order of this type frequency was stable across different classification procedures (see the Supplemental Material).

Participants were rather consistent in their types in the first and second half of the experiment. Cramér’s ϕ captures the association between categorical (or nominal) variables, with 0 indicating a complete lack of association (i.e., lack of consistency) and 1 indicating a perfect association (i.e., full consistency). Participants’ classification into one of the aforementioned five categories in the first half (i.e., the first four out of nine switching decisions) correlated with this person’s classification in the second half of switching decisions (i.e., the subsequent five switching decisions; ϕ = 0.68). This finding suggests that participants were rather consistent in their behavior, but some did modify their behavior (and thus type). We next assessed the extent to which partner’s honesty and dishonesty drives such behavior modifications.

Contagiousness of dishonesty

Thus far, we have treated honesty as a stable individual difference and assessed behavior per block. For some people, however, the preference for honesty may not be stable (Gibson, Tanner, & Wagner, 2013) but may be influenced by the partner’s behavior (Weisel & Shalvi, 2015). The choice condition may critically affect the degree to which people influence one another because in this setup, honest people face the possibility of having their dishonest partners leave them, resulting in a loss of potential earnings. We thus assessed the extent to which dishonesty is contagious in the choice condition and compared it with the forced-stay and forced-switch control conditions.

To an extent, we found that lying is contagious. Participants were more likely to lie when their partner lied compared with when their partner reported honestly in the previous report (i.e., previous round for first movers and previous stage for second movers; Wilcoxon signed-rank test, p < .01). In the forced-stay condition, participants’ likelihood of lying in a given round increased by 39% when their partner previously lied versus reported honestly (see Table S2 in the Supplemental Material; random-intercept logistic regression; partner’s Time t – 1 behavior estimate: b = 0.33, 95% CI = [0.02, 0.68]). The ability to choose partners did not reduce the contagiousness of dishonesty (see Table S2; random-intercept logistic regression; Choice × Partner’s Time t – 1 Behavior estimate: b = −0.01, 95% CI = [−0.42, 0.39]). Specifically, in the choice condition, participants’ likelihood of lying increased by 38% when their partner previously lied versus reported honestly. By contrast, compared with the forced-stay condition, forcing people to switch partners reduced the likelihood that a participant would lie following a partner’s lie (see Table S2; random-intercept logistic regression; Forced Switch × Partner’s Time t – 1 Behavior estimate: b = −0.41, 95% CI = [−0.81, −0.03]). In the forced-switch condition, participants’ likelihood of lying decreased by 8% after their partner had lied versus reported honestly, suggesting that forcing people to repeatedly switch partners can effectively curb the contagiousness of dishonesty.

These results show that, to a degree, dishonesty spread and some honest people were influenced by their dishonest partners and started lying as well. Across conditions, the contagiousness of dishonesty was stronger the longer the partners were together. In the forced-stay condition, participants interacted with their partner for 30 rounds, whereas in the forced-switch condition, they interacted with each partner for only 3 rounds. In the choice condition, some people chose to stay with their partners while other chose to switch, leading on average to longer relationships than in the forced-switch condition and shorter relationships than in the forced-stay condition. We found dishonesty to be the most contagious in the forced-stay and the least contagious in the forced-switch condition, suggesting that longer relationships increased the contagiousness of dishonesty.

Overall financial impact

The overall financial impact of corruption is composed of (a) the proportion of fully honest dyads and (b) the financial damage liars cause (i.e., their effectiveness). Interestingly, these two factors may (or may not) cancel each other out. A setting with a high prevalence of honest dyads (and thus less liars) in which lies are efficient (i.e., have a large financial impact) can produce an overall financial damage similar to a setting with a low prevalence of honest dyads (and thus more liars) in which lies are inefficient (i.e., have a small financial impact).

First, the overall magnitude of lying was similar to previously reported findings (Weisel & Shalvi, 2015; see the Supplemental Material). In the forced-stay condition, only 4.6% of dyads were fully honest (i.e., both the first and second mover were honest in a given block). The prevalence of honest dyads roughly doubled under the forced-switch condition (9.9%; see Table S3 in the Supplemental Material; censored regression; forced-switch estimate: b = 0.17, SE = 0.07, p = .01) and tripled under the choice condition (14.5%; see Table S3; censored regression; choice-condition estimate: b = 0.22, SE = 0.07, p < .01). Giving people the choice to switch partners led to a relatively high level of fully honest dyads.

Second, financial damage caused by liars is reflected in how effective lies are. Effective lies are those in which the first mover reports a high number and the second mover matches it. When both dyad members are coordinated on high numbers, lying secures high payoffs. When a dyad is poorly coordinated, some lies are not reciprocated, resulting in ineffective dishonesty. To assess the effectiveness of each dyad’s lies, we assessed the proportion of brazen lies—those reporting a double of sixes, leading to the maximum pay of €3 per dyad member. As can be seen in Figure 5, 31% of lies yielded the maximum financial damage in the choice condition. This finding was similar to that in the forced-stay condition, in which 38% of lies resulted in the highest possible monetary return, χ²(1, N = 178) = 0.48, p = .49. By contrast, only 9% of lies resulted in maximum pay in the forced-switch condition, which was lower than in the forced-stay and choice conditions, χ²(1, N = 311) = 22.1, p < .01, Bonferroni corrected for multiple comparisons. Analyzing the average effectiveness of lies across conditions led to the same conclusions (see the Supplemental Material).

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Fig. 5.

Distribution of average earnings per round (in euros) of dishonest participants, separately for each condition.

These findings suggest that high levels of coordinated dishonesty emerge not only from long-term relationships (forced stay) but also from dishonest people seeking to interact with one another (choice). The choice condition allowed people to find like-minded dishonest partners who would help them coordinate on lies and increase payoff. Forcing people to switch and thus restricting their ability to coordinate reduces the effectiveness of their lies.

Taken together, whereas the choice condition contained a relatively large proportion of fully honest dyads (and thus fewer liars), participants who lied were very efficient in causing financial damage. By contrast, the forced-switch condition contained a relatively lower proportion of fully honest dyads (and thus more liars); however, those who lied were less efficient, causing less financial damage. Seen in this light, the finding that the accumulated effects of corrupt collaboration (i.e., money earned by misreporting) did not vary greatly between the choice and forced-switch conditions is not surprising because the two factors canceled each other out. Overall, the average earnings from dishonesty (per dyad, per block) was somewhat lower in both the choice (M = 10.79, SD = 6.83; 10.67% reduction) and forced-switch (M = 10.23, SD = 6.65; 15.31% reduction) conditions, compared with the forced-stay condition (M = 12.08, SD = 5.94). These differences did not reach statistical significance (Mann-Whitney U test, p = .17).