Skip to main content


Swipe om te navigeren naar een ander artikel

01-05-2009 | Original Article | Uitgave 3/2009 Open Access

Psychological Research 3/2009

The microgenesis of action-effect binding

Psychological Research > Uitgave 3/2009
Ilona B. Dutzi, Bernhard Hommel


People plan and perform voluntary actions in order to reach particular, intended goals, that is, to modify particular states of affairs or create particular events. Obviously, they can do so only if they have reliable knowledge at their disposal regarding which kind of action is likely to create the intended event. According to ideomotor theories of voluntary action (James, 1890; Lotze, 1852) and, to some degree, Piaget’s ( 1946) sensorimotor approach to cognition, this knowledge is acquired “on the fly”: Carrying out movements is assumed to be accompanied by a more or less automatic process of self-perception that integrates, without much ado, the motor patterns underlying the movement with the codes of that movement’s perceptual consequences. In other words, actions become automatically associated with codes of their perceivable effects. This bilateral association provides the individual with a retrieval cue that allows creating that effect intentionally: One only needs to “think of” or “anticipate” (i.e., internally activate the codes of) particular action effects in order to prime and activate the action that has been experienced to produce that effect before.
Although this issue was neglected for quite some time, numerous recent studies provide increasing evidence that action effects are indeed picked up in an automatic fashion (for an overview, see Hommel & Elsner, 2009): People quickly acquire bilateral associations between actions and novel effects, such as keypress-contingent tones of a particular pitch or lights of a particular location, whether these effects are relevant to, or useful for the task at hand (Hoffmann, Sebald, & Stöcker, 2001; Hommel, 1993; Ziessler, 1998) or not (Beckers, De Houwer, & Eelen, 2002; Elsner & Hommel, 2001; Hommel, 1996). As studies using PET and fMRI have shown, once an action effect has been acquired its mere perception primes apparently associated motor structures (in the caudal supplementary motor area; Elsner et al., 2002; Melcher, Weidema, Eenshuistra, Hommel, & Gruber, 2008).
Even though the bulk of the evidence suggests that action-effect learning occurs spontaneously and without any intention to learn, Ziessler, Nattkemper, and Frensch ( 2004) have argued that effective action-effect acquisition depends on the active anticipation of the effects and is thus under attentional control. In their study, participants carried out pairs of manual responses signaled by visual letters (S 1 → R 1, S 2 → R 2). The second stimulus was systematically related to the preceding response so to allow for acquiring R 1–S 2 associations—which Ziessler et al. consider comparable to action-effect associations. As evidence for R 1–S 2 learning was obtained under undistracted conditions but not when participants were in addition to the sequential task to count tones presented in the R 1–S 2 interval, the authors conclude that R 1–S 2 acquisition cannot be automatic. But this conclusion is neither obvious nor necessary. First, ideomotor approaches claim that action-effect learning is automatic in the sense of not requiring an intention to learn, but they do not speak to the amount of cognitive resources involved. For instance, it is not unreasonable to assume that action-effect bindings need to be consolidated in order to affect subsequent behavior. As memory consolidation is known to be resource demanding and fragile (Jolicœur & Dell’Acqua, 1998), it may well be that it suffers from an overlapping task, such as tone counting. Second, even though it does not involve overt motor output, counting a tone may well be considered an intentional action. This means that Ziessler et al.’s tone-counting condition turned the original R 1–S 2 sequence into one where a third action intervened between R 1 and S 2, rendering it a R 1–R 2–S 2 sequence. If so, people might well have acquired R 2–S 2 associations, but that they failed to acquire R 1–S 2 associations is hardly surprising. Finally, the group that eventually showed the largest R 1–S 2 learning effects also showed by far the best performance on all measures from the very first trials on. For instance, their average reaction time for the first 12 performances of R 1 (the response that preceded and could thus not be affected by the tone) was already about 100 ms faster than the average of any of the other three groups. This strongly suggests major differences in motivation, which may also account for more efficient learning. In sum, we doubt that the available evidence provides strong support for a selective integration mechanism. On the contrary, numerous findings support the ideomotor expectation that carrying out a movement is indeed accompanied by the automatic (i.e., unintentional) integration of its perceptual consequences.
The present study focused on the microgenesis of this integration process, that is, the emergence of individual action-effect associations. According to the Theory of Event Coding (TEC) of Hommel, Müsseler, Aschersleben, and Prinz ( 2001) stimulus and action events are integrated in two phases. The first, activation phase consists of activating codes of a particular stimulus and/or action feature, be that internally driven, as in the case of action planning (accomplished by “anticipating” the intended action’s attributes), or externally driven, such as when a stimulus event is perceived. The second, integration phase serves to bind the activated features together, hence, to integrate them into a sort of event file (Hommel, 1998). These event bindings may be actively maintained, such as when an action plan is held in preparation (Stoet & Hommel, 1999), or decay over time. In any case, however, event bindings seem to survive 1 s or longer (Hommel, 1998; Hommel & Colzato, 2004).
Here we applied TEC integration logic to action-effect integration. TEC claims that if the activations of codes (be they stimulus- or action-related) overlap in time, they get integrated. Hence, if the codes of an action plan are still activated to some degree when the effects of that action are coded, action and effects should become part of the same representational structure. Given that the codes of action plans commonly show activation 250 ms or longer after the corresponding action is carried out (Stoet & Hommel, 1999; Hommel, 1994), there are reasons to believe that the overlap is sufficient at least for immediate effects triggered by the action’s onset. Indeed, studies of long-term action-effect acquisition have shown that actions and effects are spontaneously associated if the effects follow the action onset by up to 1 s but not longer (Elsner & Hommel, 2004)—at least if the action-effect interval is not “bridged” by intervening events (cf., Reed, 1999). Likewise, if participants estimate the extent their actions have caused a particular event, the accuracy of their judgments decreases considerably if actions and effects are separated by more than about 2 s (Shanks, Pearson & Dickinson, 1989). With respect to the short-term binding of stimuli and responses, it has been shown that stimuli are integrated with responses if they appear in a temporal neighborhood of about half a second but not if they are separated from the response by about 2.5 s (Hommel, 2005).
If actions and effects are spontaneously (i.e., non-intentionally) integrated into action-effect bindings and if these bindings have a lifetime beyond the presentation of the effect, the way they are bound together should affect subsequent performance. Assume, for instance, a left-hand keypress is heard to produce a low-pitched tone, in a task where high and low tones can appear and left and right keypresses are carried out. If the co-occurrence of left-hand keypress and low-pitched tone creates a binding between the codes LOW and LEFT, presenting a high or low tone shortly thereafter (i.e., while the binding is still intact) should systematically bias response selection. Figure  1 shows how. Given the high and low tones are the perceptual alternatives in the present context, the participant is likely to represent these two possibilities as sketched in Fig.  1a, where the codes for high and low tones are connected by an inhibitory link (see Bogacz, 2007). The same logic applies to the two alternative responses (the left and right keypress or L and R), which are also shown in this figure. If we assume that tones and responses vary independently and are thus uncorrelated, there are no long-term associations between tones and responses. However, according to our reasoning, a single co-occurrence of low tone and left response should induce a binding between their representations, as indicated in Fig.  1b.
What would happen if the tone repeats? As shown in Fig.  1c, activating the code of the low tone should prime the still bound response, the left keypress that is. This means that a stimulus repetition should induce a tendency to repeat the response as well. Now consider what a tone alternation would imply. As shown in Fig.  1d, presenting a high tone would activate the corresponding code, which is not bound to any response (if we ignore previous trials for a moment). However, given the inhibitory link between the two tone representations, activating the code of the high tone should lead to the inhibition of the low-tone code. Given that this code is still bound with the left response code, inhibition will spread to that code as well. This follows from the integrated competition hypothesis suggested by Duncan and colleagues (Duncan, 1996; Duncan, Humphreys & Ward, 1997). They pointed out that the distributed cortical representation of perceptual and action codes calls for integration mechanisms that create coherent object-action compounds. Members of such a compound benefit from competitive gains achieved by other members of the same compound, so that, say, integrating RED with ROUND when processing the image of a cherry has the consequence that increasing the activation of the RED code also supports the ROUND code in its competition with other shape-related codes. The flipside of integrated competition is that losses in the competition also spread among members, so that outcompeting the RED code when seeing a banana somewhat later will also weaken the ROUND code associated with it. In other words, integrated elements win together and lose together. Applied to our example, this means that binding LOW and LEFT weakens LEFT if LOW loses against HIGH. Given that left and right responses are the only alternatives, this again implies that perceiving a high tone would bias response selection toward the right response, which would benefit from the indirect inhibition of the left response code.
Available evidence from stimulus-response integration studies provides support for both implications. For one, repeating stimulus features have been shown to speed up response repetitions as compared to response alternations (Hommel, 1998; Hommel & Colzato, 2004), suggesting that stimulus repetition indeed induces a response-repetition tendency. For another, alternations of stimulus features have been observed to speed up response alternations, sometimes even more than stimulus repetitions speed up response repetitions (e.g., Hommel & Colzato, 2004). Along the same lines, with multidimensional stimuli, response repetitions are particularly (i.e., over-additively) fast if signaled by a stimulus that repeats all the features of the previous stimulus (Bertelson, 1963), whereas response alternations are particularly slow under these circumstances (Hommel, Memelink, Colzato, & Zmigrod, 2008). Hence, stimulus alternations indeed seem to induce a response-alternation tendency.
According to these considerations perceiving a tone that does or does not match a just-experienced response-produced tone should systematically bias the decision to perform a left or right keypress. Importantly, this should be the case independently of previous experiences, hence, even if the overall probabilities for a high and low tone to follow a left or right response are equal. We tested this prediction as sketched in Table  1. Participants carried out free-choice responses by pressing a left or right key (for a discussion and validation of this technique, see Elsner & Hommel, 2001; Hommel, 2007). Each trial consisted of two parts. In the first, induction part participants made a freely chosen response (R 1) to a non-discriminative visual trigger stimulus (S). This response produced one of two auditory effects ( E A), a low- or a high-pitched tone. Importantly, the mapping of response keys to pitch varied randomly from trial to trial, so to prevent any incremental response-effect learning across the experimental session. One-second later, in the test part of each trial, participants encountered one of the two effect stimuli ( EA), which now served as go signal (in 75% of the trials) to perform another freely chosen response (R 2). The measure of interest was the response choice in the test part (i.e., R 2). In particular, we analyzed the tendency to repeat the previous response (R 2 = R 1) as a function of the relationship between the effect tone E A and the go-signal tone EA. According to our hypothesis, participants should be more likely to repeat a response if the two tones match ( EA =  E A) than if the tones do not match ( EA ≠  E A), because the tone’s code should still be bound with the response that just had produced it.
Table 1
Conditions in Experiments 1 and 2
Each trial consisted of two parts. In the induction part, a row of asterisks (Stimulus) triggered a free-choice response (R 1), which was followed by a randomly chosen high or low pitched tone (auditory action effect E A). In congruent or incongruent go trials of the test part, a high or low pitched tone (which was congruent or incongruent with the preceding action effect) triggered another free-choice response (R 2)—the dependent measure (?) being the type of response (same as vs. different from R 1)

Experiment 1

Experiment 1 was conducted as a first test whether action-related codes are spontaneously integrated with codes of their effects, as suggested by TEC. If so, we would expect response-repetition rates (%RR) to be higher if the R 2-go signal ( EA) matches the preceding action effect ( E A) in pitch than if it does not.



Twenty students served as paid participants. As was the case for all participants of this study, they reported having normal or corrected-to-normal vision and audition and were not familiar with the purpose of the experiment.

Apparatus and stimuli

Visual stimuli (a row of 13 white-on-black asterisks) were presented on a computer monitor and auditory stimuli (sinusoidal tones of 400 and 800 Hz) through external loudspeakers to the monitor’s left and right. Responses were made by pressing the left or right of two external microswitches with the corresponding index finger. The experiment was controlled by a standard PC running under ERTS (Beringer, 1994).


Each trial consisted of an induction part, to induce a particular action-effect binding, and a test part, to diagnose the presence of such bindings. Table  1 shows the sequence of events. After an intertrial interval of 3,000 ms, the asterisk string (S) appeared for 300 ms, requesting a speeded left or right keypress (R 1). Participants were instructed to choose the key randomly and to avoid any strategy apart from using the keys about equally often. If a response was made a randomly selected effect tone ( E A) was presented for 100 ms, its onset being synchronized with the keypress. Due to the random selection procedure, keypresses and tone pitches were uncorrelated, that is, in a given trial each keypress had the same probability to trigger either a low or high tone. Participants were told that these tones were completely irrelevant for the task and that there would be no systematic relationship between keypress and pitch.
In the second, test part of each trial one of the two effect tones was used as go signal ( EA) to signal a second free-choice reaction (R 2) in 75% of the trials; in the remaining 25% no tone appeared and no second response was to be performed (no-go trials). No-go trials were used to work against some of the most obvious strategies in free-choice tasks, such as choosing responses according to a standard predetermined pattern. In go trials one of the two tones sounded for 100, 1,000 ms after the previous effect tone had been presented. In 50% of these go trials the tone was the same as the previous effect tone (congruent trial); in the other 50% the signal tone was the alternative tone (incongruent trial). Participants were instructed to respond to the tone as quickly and as spontaneously as possible by pressing a randomly chosen response key and to refrain from responding if no second tone would occur. It was emphasized that only the presence of a tone mattered for the execution of R 2 while its pitch would be neither relevant nor informative. Participants were also urged to use both keys and not to apply any strategy. The program waited up to 1,500 ms for a response. Responses with reaction times exceeding 1,500 ms were counted as missing, those faster than 100 ms as anticipation, and responses in no-go trials as false alarms. All these errors were fed back to the participants. Following ten randomly drawn practice trials three blocks of 64 randomly ordered trials each were administered. After the session participants were asked whether they had obeyed to the instruction and had guessed the purpose of the experiment.

Results and discussion

Our dependent measure of choice is very sensitive to individual strategies, which may conceal or even prevent the possible impact of go stimuli on response choices. Particularly damaging would be strategies that determine response choices long before the go stimulus is presented, so that the selection process we intended to bias is already completed. Accordingly, we not only took measures to work against some of the strategies by speeding response selection and including no-go trials, but we also excluded participants that were likely to apply a particular “pre-selection” strategy. For this reason, we only considered participants who produced less than 20% false alarms and at least 90% correct trials altogether, and who did not report having used a response rule. All participants passed these criteria and no-one reported having paid any attention to pitch or having guessed the purpose of the experiment. In fact, most of them believed that reaction time was the important dependent variable. We also excluded participants if their mean %RR was lower than 10% or higher than 90%, which we consider strong evidence of an alternation or repetition strategy, respectively. This applied to two participants. After excluding trials with response omission (0.3%) or anticipation (0.4%) individual %RRs were calculated as a function of congruency (see Table  1 for the coding scheme). 1
In the induction part of the trials the two keys were pressed equally often and their frequencies (48.5 vs. 51.5%) did not differ from chance. This observation, which we also made in the following experiments, confirms that participants experienced all possible response-effect couplings about equally often. The mean %RR in the test part was 39.1%, but the repetition rate was modulated by E A −  EA congruency: As shown in Table  2, congruent trials produced more response repetitions than incongruent trials, t(17) = 4.86, < 0.01. That is, as expected, stimulus repetitions were associated with more response repetitions, suggesting that the present response choice was affected by the relationship between the previous response and its auditory effect.
Table 2
Mean response repetition frequencies (in %) and response-repetition biases (congruent–incongruent) for Experiments 1–4 as a function of E E′ congruency (match between effect of R 1 and go signal for R 2), action-effect modality, and modality of the task-relevant go signal for R 2
Auditory action effect (pitch)
Visual action effect (color)
Experiment 1
Auditory go signal
43.5 (12.1)
34.6 (12.1)
Experiment 2
Auditory go signal
49.1 (12.3)
41.9 (15.0)
Experiment 3
Auditory go signal
47.6 (22.1)
40.5 (19.9)
Visual go signal
50.1 (21.6)
46.9 (18.4)
Experiment 4
Auditory go signal
46.4 (14.3)
41.4 (13.6)
42.9 (12.7)
44.9 (14.4)
−2.0 NS
Visual go signal
47.1 (19.9)
41.9 (17.6)
46.3 (19.1)
42.7 (18.3)
Standard deviations of means are given in parentheses
NS non-significant bias
** Significant bias, p < 0.01
It is interesting to note that the response-repetition frequencies for congruent and incongruent conditions were not distributed evenly around 50% but shifted toward response alternations (i.e., around 39.1%). There are at least two possible accounts for this observation, which we will also make in the following experiments. The first account considers that people are often biased toward response alternations, as can be seen in faster reaction times with response alternations that repetitions, presumably reflecting a general misconception about statistical probability (Bertelson, 1961; Soetens, Boer, & Hueting, 1985)—also known as gambler’s fallacy. Interestingly, response alternations were faster than repetitions (335 vs. 357 ms) in the present experiment as well, t(17) = 3.01, < 0.01. Hence, even though our study does not provide a “pure” measure of the alternation bias, the fact that it has been so often observed in other studies may be taken to suggest that our participants also showed such a bias. This again might suggest that our congruent and incongruent conditions were indeed symmetrically distributed around a mean that would ideally approach 50%, but the whole distribution was torn to the lower half because of the gambler’s fallacy.
The second account holds that our participants were not biased toward repetition or alternation in principle, and that the outcome for the congruent condition represents something like a neutral baseline. Indeed, it will turn out that the 43.5% we observed in the congruent condition of Experiment 1 is the lowest estimate of the present study, and that the other experiments will produce estimates very close to 50%. If so, the main impact of stimulus repetitions and alternations would consist in stimulus alternations biasing people toward response alternations. In other words, the effect sketched in Fig.  1d would be much stronger than the one in Fig.  1c. As mentioned earlier, this would fit with occasional observations that stimulus-response alternations produce faster and more accurate responses than complete stimulus-response repetitions, at least numerically (e.g., Colzato, Fagioli, Erasmus, & Hommel, 2005; Colzato, van Wouwe, & Hommel, 2007; Hommel & Colzato, 2004). Indeed, given that repetition-induced priming of previous bindings and alternation-induced integrated competition are different types of processes, there is no reason to believe that the reaction-time benefits they produce should be of exactly the same size.
As we neither have a pure measure of possible general alternation biases nor a noise-free measure of binding reactivation and integrated competition, it is premature to try deciding between these two interpretations. Importantly, however, they both rest on the same assumption, namely, that perceiving a self-produced stimulus event creates a temporary binding of the codes underlying the action and the codes representing the perceived event. As a consequence, perceiving the same event or its alternative systematically biases response selection. Taken altogether, Experiment 1 provides first evidence for our hypothesis that a single pairing of an action and an effect is sufficient to integrate their cognitive representations, and that this integration has a systematic effect on subsequent response selection.

Experiment 2

Even though the outcome of Experiment 1 is consistent with our expectation that action-effect binding affects subsequent response-selection processes, there is an alternative interpretation. Our participants had the task of producing random responses and response sequences, which is known to be very hard to do. One way to make this task easier and to still meet the task requirement of getting close to a 50:50 distribution of response repetitions and alternations would be to strategically repeat the response whenever the stimulus repeats. Note that this strategy only works well if the probability of stimulus repetition versus alternation in go trials is also 50:50. If this ratio would be drastically changed, such as if stimulus alternations would be much more frequent than stimulus repetitions, such a matching strategy would be bound to fail: either response alternations would now also become much more frequent than response repetitions or participants would notice that a matching strategy makes little sense and simply no longer apply it. This was the logic underlying Experiment 2, which replicated Experiment 1 with a 25:75 probability of stimulus repetitions and alternations. According to a strategic interpretation of the congruency effect, this manipulation should eliminate the effect, whereas an interpretation in terms of action-effect binding predicts the same outcome as in Experiment 1.


Twenty-one students served as paid participants. The method was exactly as in Experiment 1 with only one exception: the go trials of the test phase did not consist of 50% congruent and 50% incongruent conditions but of 25% congruent and 75% incongruent conditions; i.e., the trigger tone matched the previous action effect tone in only one quarter of the trials.

Results and discussion

Applying the same criteria as in Experiment 1 led to the exclusion of one participant. Again, trials with response omissions (<0.9%) and anticipations (<0.3%) were excluded. The overall response-repetition rate in the test part was 43.7%, which is higher than in Experiment 1 and statistically no longer different from chance. Clearly, this observation does not support the idea that participants might have strategically matched the response repetition rate to the stimulus repetition rate. The response repetition rate was again modulated by E A −  EA congruency, t(19) = 3.07, < 0.01, due to that congruent trials produced more response repetitions than incongruent trials did (see Table  2). An ANOVA on the combined data from Experiments 1 and 2 did not yield any hint to an interaction between experiment and congruency effect, p > 0.5, confirming that the congruency effect was equivalent in the two experiments. Taken together, these findings suggest that the congruency effect does not reflect a deliberate response selection strategy but rather represents an automatic by-product of action-effect binding.

Experiment 3

Our next experiment was conducted to see how automatic the impact of action-effect bindings really is and whether, or to what degree it is sensitive to attentional effects, that is, to the task relevance of the effect’s perceptual characteristics. In Experiments 1 and 2, tones were used as both action effects ( E A) and R 2-go signals ( EA). Accordingly, although neither the pitch nor the presence of the action effect was of any relevance, tones did play an important role and could not be ignored entirely. It may have been this, somewhat indirect type of task relevance that drew sufficient attention to the effects to integrate and bind them with the responses and/or to retrieve the just-bound response when the effect stimulus was encountered again. 2 If so, it should be possible to reduce or eliminate the impact of action-effect bindings on ongoing response selection by defining the R 2-go signal in another than the auditory modality, so that tones are no longer of any relevance. This is what we did in Experiment 3. In an auditory-go condition we replicated Experiment 1 by using again an auditory E′. But we also ran a visual-go condition, where the R 2-go signal was a visual stimulus ( EV). Although no longer of any relevance for the task, the tone was still presented as EA, thus accompanying the visual go signal in go trials and as the only stimulus in the test part of no-go trials. If task relevance affected the creation and/or retrieval of action-effect bindings we would expect the response-rate effect—that is, higher response-repetition rates if the R 2-go signal matches the preceding action effect—in the auditory-go condition but not (or less so) in the visual-go condition.


Another 26 female and 19 male students were randomly assigned to two groups of 23 and 22 participants, respectively. For the first, auditory-go group the method was exactly as in Experiment 1. For the second, visual-go group several modifications were introduced. The relevant go signal in the test part of each trial was not a tone but a red 3x3 cm square ( EV) 3 appearing for 300 ms at screen center. Just like the tone in the auditory-go group, the square was presented in 75% of the trials to signal R 2 (go trials) and participants were to withhold R 2 in the remaining no-go trials. The pitch of the tone matched the previous action-effect tone in 50% of the go trials and the alternative tone in the other 50%. It was pointed out to the participants that both presence and pitch of the tone would be completely irrelevant for the task.

Results and discussion

Applying the same criteria as in Experiment 1 led to the exclusion of three members of the auditory and of two of the visual group. Again, trials with response omissions (<0.6%) and anticipations (<0.1%) were excluded. The overall response-repetition rate in the test part was 46.3%, which is almost the same as in Experiment 2 and statistically not different from chance. Mean %RR were analyzed as a function of E A −  EA congruency (i.e., whether the two tones in each trial matched or not) and R 2-go-signal modality (i.e., whether R 2 was carried out in response to the second tone or a color square; see Table  2). The only reliable finding was a main effect of tone congruency, F(1,38) = 8.69, < 0.005, while the interaction with go-signal modality was far from significance, F(1,38) < 1. That is, irrespective of the tone’s task relevance, R 1 is repeated more often if the tone in the test phase matches the action-effect tone.
All in all, the outcome of Experiment 3 is somewhat mixed. Statistically speaking, task relevance had no impact on the congruency effect, suggesting that the auditory action effects were integrated and retrieved in either go-signal condition. However, numerically the induced bias in the visual condition was not even half as big as that obtained in the auditory condition. Moreover, auditory stimuli and their impact on perceptual processing have been demonstrated to be more salient, hence, to rely much less on attention than visual stimuli (Posner, Nissen, & Klein, 1976). One therefore may argue that Experiment 3 provides a rather conservative test of the impact of attention.

Experiment 4

To provide a more sensitive test we ran Experiment 4, where responses produced both auditory and visual effects. We also presented stimuli of both modalities in the test part of the go trials and varied their relevance. In one block, R 2-go signals were auditory, just like in Experiments 1–3, which rendered the visual stimuli in either part of the trial irrelevant. The saliency hypothesis suggests that auditory action effects should be integrated under such conditions while visual effect may not. If so, repeating tone pitch ( EA =  E A) should lead to higher response-repetition rates than alternating pitch, whereas repeating color ( EV =  E V) should yield the same rates as alternating color. In another block, R 2-go signals were visually defined, which rendered the auditory stimuli in either part of the trial irrelevant. According to the saliency hypothesis and in view of Experiment 3, we would expect that both auditory and visual action effects are integrated and retrieved, so that response-repetition rates should depend on whether pitch or color is repeated.


Another 27 female and 23 male students served as paid volunteers. The method was as in Experiment 3 (visual-go group) with the following exceptions. With regard to the induction part, performing R 1 now caused the simultaneous presentation of a low- or high-pitched tone (for 100 ms) and a red or green square at screen center (for 200 ms); hence, each R 1 had both an auditory and a visual effect.
In the test part of the trials, three independent variables were manipulated: the modality of the R 2-go signal (tone or square), the congruency between the pitch of the action-effect tone from the induction part ( E A) and the pitch of the tone presented in the test part ( EA), and the congruency between the color of the action-effect square from the induction part ( E V) and the color of the square presented in the test part ( EV). Like in the visual-go group of Experiment 3, there were two stimuli in the test part of go trials, a low- or high-pitched tone and a red or green square. However, in a given block only one of them was task-relevant by virtue of signaling a go trial, whereas the other was entirely irrelevant.
The experimental session consisted of two blocks, an auditory-go block, where no-go trials were defined by the absence of a tone in the test part of the trial, and a visual-go block, where no-go trials were defined by the absence of a square in the test part of the trial. Block order was balanced across participants. Each block was composed of 10 randomly drawn practice trials and 192 randomly ordered experimental trials. The 192 experimental trials comprised 144 go and 48 no-go trials, so that the go probability was again 75%. The 144 go trials were composed of 36 trials in which both the tone and the color presented in the test part matched the action effects of the preceding induction part (i.e., EA =  E A and EV =  E V), 36 trials in which only the auditory stimuli matched (i.e., EA =  E A and EV ≠  E V), 36 trials in which only the visual stimuli matched (i.e., EA ≠  E A and EV =  E V), and 36 trials in which neither the auditory nor the visual stimuli matched (i.e., EA ≠  E A and EV ≠  E V). To ensure that participants registered the visual action effects even in the auditory-go block, the instruction emphasized that they should always fixate the center of the computer screen.

Results and discussion

Applying the same criteria as in Experiment 1 led to the exclusion of 10 participants. Trials with response omissions (<0.2%) and anticipations (<0.1%) were excluded. Mean %RR were calculated for each participant as a function of auditory ( EA − E A) congruency, visual ( EV − E V) congruency, and modality of the relevant go signal (see Table  2). A corresponding 2 × 2 × 2 ANOVA produced two significant results: a main effect for auditory congruency, F(1,39) = 17.98, < 0.001, and an interaction of visual congruency and go-signal modality, F(1,39) = 9.26, < 0.005. As Table  2 shows, congruent pitch yielded a higher rate of response repetitions independently of go-signal modality whereas congruent color affected the repetition rate only if go trials were defined by the presence or absence of visual stimuli. Indeed, separate t-tests revealed a highly significant effect of color congruency in the visual-go block, t(39) = 3.27, < 0.005, but not in the auditory-go block, t(39) = 1.39, > 0.05. This pattern supports an account in terms of stimulus saliency: Action effects are integrated and retrieved if they are either relevant to the task or salient enough to attract attention in a bottom-up fashion.
Another important finding of Experiment 4 is that it for the first time demonstrates the integration of multiple action effects. Although previous studies on action-effect acquisition employed a variety of to-be-learned effect stimuli they were always restricted to one type of stimulus at a time. Yet, both auditory and visual action effects influenced performance in the visual-go condition of Experiment 4, which suggests that participants had integrated their actions with both pitch and color. 4

General discussion

Our study tested a TEC approach to the integration of actions and their effects. We hypothesized that the likely temporal overlap of activation of action- and effect-related codes induces the temporary binding of those codes. This binding may affect subsequent behavior by biasing it toward response repetition in case of a stimulus repetition, biasing it toward response alternation in case of stimulus alternation, or both. Consistent with this expectation, Experiment 1 showed that varying the pitch of a go signal systematically affects the tendency to repeat or alternate the response that was just experienced to produce a tone of that pitch. Together with the outcome of Experiment 2, which rules out a strategic interpretation of the response repetition bias, this suggests that codes of that action are still bound with codes of the tone it produced. As a consequence, re-activating the tone-related code spread activation to the corresponding action-related code, thus priming the previous action as indicated in Fig.  1c, while activating the alternative tone code led to the inhibition of the codes of both the previous tone and the previous response, resulting in a preference for response alternation (Fig.  1d). Interestingly, the distribution of response-repetition frequencies was shifted toward response alternation in all experiments. This might reflect a general impact of the gamblers fallacy and represent the same bias that has been shown in studies of sequential stimulus and response effects (Bertelson, 1961; Soetens et al., 1985). Alternatively, it might indicate that alternations of action-effect stimuli bias subsequent response selection more toward response alternations than effect repetitions bias selection toward response repetitions. In other words, the priming of response repetitions as sketched in Fig.  1c may be less efficient than the inhibition of response repetitions as sketched in Fig.  1d. The present study does not allow disentangling these two possibilities, which calls for a more detailed experimental analysis. However, both possibilities imply that actions and effects are spontaneously integrated into temporary bindings, which supports our main hypothesis.
As the action effect in Experiment 1 was not relevant or informative, effect integration seems to be spontaneous in the sense that it does not require the explicit intention to learn about those effects. This supports Elsner and Hommel’s ( 2001) assumption that effect integration is an automatic by-product of moving and acting. However, this does not mean that goals and intentions, and the attentional set they bring about, have no impact on effect integration and/or retrieval (Hommel et al., 2001). To the contrary, Experiments 3 and 4 provide evidence that the likelihood with which action-effect bindings affect performance depends on both bottom-up and top-down attentional factors. If an effect is salient enough to attract attention in a bottom-up fashion, as can be assumed for tones (Posner et al., 1976), action effects impact behavior even if they are neither directly nor indirectly related to the task at hand. This fits well with observations from learning studies, where auditory (e.g., Hoffmann et al., 2001; Hommel, 1996) and electrocutaneous (Beckers et al., 2002) action effects were spontaneously acquired and retrieved in otherwise purely visual-manual tasks. Less salient effects, however, such as visual effects in an otherwise auditory-manual task, seem to depend more on the fit of their attributes with the current attentional set. Even though we manipulated saliency by contrasting auditory and visual effects, we consider saliency to be a matter of degree and of the particular stimulus-context relations rather than an absolute characteristic of a particular sense modality; but more systematic studies are necessary to elucidate that issue.
Another question is which process exactly is affected by saliency. One possibility is that integration proper depends on some minimal activation of effect codes, which they may reach only if they are either top-down primed because of their task relevance or particularly salient (see Hommel, 2004). However, a major disadvantage of a selective integration mechanism would be that infants, children, and adults facing a novel task would no longer be able to pick up unpredicted but consistent action-effect relations on the fly—a characteristic of action-effect acquisition that one may consider essential for the development of voluntary action and action skills (Elsner & Hommel, 2001; James, 1890; Piaget, 1946). Another possibility is that action-effect binding is truly automatic and may not even be sensitive to the availability of attentional resources, which would leave binding retrieval as a possible target of our saliency manipulations. Indeed, we cannot exclude that saliency affected the retrieval of just-created action-effect bindings rather than the creation of bindings. That is, stimuli may be more effective to trigger the retrieval of previously created bindings if they are task-relevant or salient. Again, studies on stimulus-response integration suggest that the retrieval of bindings is more sensitive to attentional manipulations than the creation of bindings is (Hommel et al., 2008), which would fit better with a retrieval-based interpretation of saliency effects. Nevertheless, the final word on this matter presupposes a better understanding of how action-effect binding and retrieval processes work, and how they are controlled.
In view of the previous demonstrations of the acquisition of stable action-effect associations on the one side and of the present evidence for transient bindings between actions and effects on the other, it would be tempting to assume that the latter are functional predecessors of the former: The transient coupling of action and effect codes may reflect the presence of reverberatory loops in the sense of Hebb ( 1949), which again may serve to establish and consolidate more enduring cell assemblies. In other words, binding may represent the first step to long-term memory (cf., Raffone & Wolters, 2001, but see Colzato, Raffone, & Hommel, 2006). However, in the absence of clear-cut evidence that action-effect learning is impossible without binding (and in view of the major methodological challenges demonstrations of such evidence would need to overcome) this is no more than an interesting speculation.


We are grateful to Wilfried Kunde, who suggested the experimental rationale underlying Experiment 2 and drew our attention to the fact that manipulating action-effect saliency may affect both integration and retrieval of action effects. We are also indebted to two anonymous reviewers whose comments helped improving this article. This research was partially funded by the Max Planck Institute for Psychological Research in Munich, Germany.

Open Access

This article is distributed under the terms of the Creative Commons Attribution Noncommercial License which permits any noncommercial use, distribution, and reproduction in any medium, provided the original author(s) and source are credited.
Open AccessThis is an open access article distributed under the terms of the Creative Commons Attribution Noncommercial License ( https://​creativecommons.​org/​licenses/​by-nc/​2.​0), which permits any noncommercial use, distribution, and reproduction in any medium, provided the original author(s) and source are credited.
We did not consider reaction times (with one exception in another context below) because, as demonstrated and discussed by Elsner and Hommel ( 2001), it is impossible to predict and interpret their pattern in the present free-choice task. For instance, fast responses in the congruent condition may indicate that (a) the response was particularly spontaneous, and thus free from strategic considerations, suggesting that conditions were particularly good for tones to affect response selection; or that (b) the response was preplanned already and thus under full strategic control, suggesting that conditions were particularly bad for tones to affect response selection. Slow responses in the congruent condition may be interpreted to reflect (a) particularly strong contributions from strategic considerations (a lot of thinking before responding), which one would expect to minimize the impact of the tone; but they may just as well reflect (b) a delay due to extended competition between strategic top-down factors and tone-driven bottom up factors, which again would point to a particularly strong contribution from the tone. Multiple interpretations also exist for fast or slow responses in the incongruent condition, all suggesting that reaction times are a misleading measure in the present context.
Note that the design of our study (or of any other analysis of sequential effects) does not allow disentangling possible effects on the creation of action-effect bindings (i.e., integration) and on their retrieval. Obviously, bindings can only be retrieved if they have been created earlier, so that changes in the impact of action-effect bindings on performance may be due to changes in the binding process, changes in the retrieval process, or both. We will get back to this issue in “ General discussion”.
In keeping with the terminology introduced in Experiment 1 we refer to the visual go signal as EV. However, note that in the induction part of Experiment 3 there were only auditory action effects ( E A) but no visual action effects ( E V).
Alternatively, participants might have alternated between the integration of auditory and visual effects. However, this should have decreased the response bias for both types of effects, which does not fit the finding that the bias for auditory action effects in the visual-go condition was numerically stronger in Experiment 4 (where alternation might have taken place) than in Experiment 3 (where action effects were all auditory).

Onze productaanbevelingen

BSL Psychologie Totaal

Met BSL Psychologie Totaal blijft u als professional steeds op de hoogte van de nieuwste ontwikkelingen binnen uw vak. Met het online abonnement heeft u toegang tot een groot aantal boeken, protocollen, vaktijdschriften en e-learnings op het gebied van psychologie en psychiatrie. Zo kunt u op uw gemak en wanneer het u het beste uitkomt verdiepen in uw vakgebied.

Over dit artikel

Andere artikelen Uitgave 3/2009

Psychological Research 3/2009 Naar de uitgave