1 Introduction
In the natural environment the exposure frequency and exposure duration of homogeneous events are often correlated. For instance, when one has to wait at many traffic lights during a stroll through town, one has probably waited quite a long time in total. If one knows either the frequency or total duration of the waiting situations, one can estimate the other attribute fairly accurately.Footnote 1 In the laboratory, the exposure frequency and duration of stimuli can be varied orthogonally, and so accurate judgments of these attributes would be uncorrelated. But humans still produce correlated judgments: When they think an object has been presented often, they usually also judge it to have been presented for a long duration (e.g., Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference HintzmanHintzman, 1970; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Smith, Rule and PriceSmith et al., 2017; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015). Under certain conditions the reverse is also true: when an object has been presented for a long time, humans think it has been presented often (e.g., Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference BonannoBonanno, 1996; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011). These findings hint at a single underlying dimension on which judgments of frequency and duration are based.
But at the same time, it is known that judgments of frequency are extremely accurate, while judgments of duration are usually poor in comparison (e.g., Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference HintzmanHintzman, 1970; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015). If the same single dimension is used for both judgments, the difference in accuracy is difficult to explain. But does it really demand two separate dimensions?
Half a century ago, Reference HintzmanHintzman (1970) answered in the affirmative and concluded that judgments of frequency and duration must be based on two dimensions because they are affected differently by exposure frequency and duration subsequently this was also expressed in Reference HintzmanHintzman, 2011; Reference Hintzman, Summers and BlockHintzman et al., 1975). But in the last decade new findings have accumulated and a unidimensional model has resurfaced again (e.g., Reference Smith, Rule and PriceSmith et al., 2017; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011).Footnote 2 Specifically, Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010), as well as Reference WinklerWinkler (2009) and Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al. (2015), have favored a unidimensional model. They have found that under certain conditions, the biasingFootnote 3 effects of duration on judgments of frequency and of frequency on judgments of duration are relatively symmetrical.Footnote 4 In several experiments they manipulated how much attention participants paid to the stimuli during encoding. Under high-attention conditions (e.g., interesting material, special instructions), frequency influenced judgments of duration and duration also influenced judgments of frequency. In some conditions, these effects were comparable in size and this symmetrical pattern the authors took as evidence of a single underlying dimension.
Our goal in this paper is to resolve which of these opposing positions is valid: Are judgments of frequency and duration based on one or two dimensions? We reconstruct the arguments for and against both models formally, which shows that previous attempts to clarify this issue were methodologically unsatisfactory. We propose a different, more stringent method that is related to state trace analysis (Reference Dunn and KalishDunn & Kalish, 2018; Reference Dunn and KirsnerDunn & Kirsner, 1988). Finally, we gather available data and apply our proposed method to test which of the models is supported empirically.
2 Applying the Total Time Hypothesis to Judgments of Frequency and Duration
In a typical experiment on judgments of frequency and duration, participants observe many stimuli that are presented with varying frequencies and presentation durations. After the encoding phase, participants are asked to provide a numerical estimate of frequency and/or duration for each stimulus in retrospect.
This paradigm of studying the joint effects of exposure frequency and exposure duration on memory-related judgments was introduced by Reference HintzmanHintzman (1970). He borrowed the idea of the total time hypothesis (Reference Cooper and PantleCooper & Pantle, 1967) in memory research and applied it to judgments of frequency. The total time hypothesis states that the long-term memory strength for a stimulus depends on the total exposure time of the stimulus, independent of how time is distributed (Reference HintzmanHintzman, 1970, p. 437). This can be translated into a more formal statement:
where m is memory strength, f and d are exposure frequency and exposure durationFootnote 5, and gm is a function. The statement means that several repetitions of an item are like one long repetition, for example, m(10,1) = m(1,10). We cannot say much about the function gm because the memory strength is not measurable (at least not within the presented framework) and theorists have so far not been interested in it.
Judgments of frequency were conceptualized as memory-related judgments because they showed a spacing effect (Reference HintzmanHintzman, 1969; Reference UnderwoodUnderwood, 1969). Thus, the transfer of the total time hypothesis from memory to judgment of frequency seems obvious in retrospect. Hintzman postulated that frequency judgments are based on the memory strength, which can be translated into
where F is judgment of frequencyF is some unknown function. Again there is usually no explicit discussion of the shape of this function in the literature. Independent of the nature of the two functions (gF and gm), judgments of frequency should depend on the interaction between f and d, which Hintzman tested in his first experiment. His choice of analysis was an analysis of variance (ANOVA) with linear trends and a correlation analysis, which both constrain the relationships to be linear.Footnote 6 With this assumption we can equivalently state the expected relationship in regression form:
where bF f ˙ d is the slope for the interaction term and e is the error term.Footnote 7 Note that in a model with the main effects and interaction specified, the interaction should be the best predictor, and the main effects bFf and bFd are expected to be 0 and thus are excluded from the above formula.
To his surprise, Hintzman found the interaction term was negligible in size, and the effect of frequency (bFf) almost completely explained the variation in the data, while the effect of duration (bFd) was essentially 0. His verbal summary corresponds to
He had two explanations for this finding. The first was that the total time hypothesis did not hold: Duration had no effect on the memory strength and thus no effect on judgment of frequency:
and
But if duration did not influence the memory strength, the total time hypothesis had to be fundamentally questioned, at a time when it was popular (Reference Cooper and PantleCooper & Pantle, 1967). Furthermore, it is not intuitive that seeing something for a longer period of time should have no effect on memory strength at all (e.g., Reference Potter and LevyPotter & Levy, 1969). Thus, Hintzman’s alternative explanation was that the total time hypothesis was correct but not applicable to judgments of frequency. To be more specific, he assumed that judgments of frequency are not based on the memory strength. This idea required introducing the two-dimensional model: Exposure frequency and duration do not contribute to a single dimension of the memory trace, but to two independent dimensions (m 1, m 2):
When judgments of frequency are made, the duration information is filtered out, so exposure duration has no effect on these judgments:
To test which of the two explanations was supported, Hintzman derived predictions of what would happen if participants had to make judgments of duration. If the total time hypothesis was incorrect, but all other assumptions valid, judgments of duration should be based on the same memory strength as judgments of frequency. Thus, they should be affected by frequency, but not by duration:
where D is judgment of duration and gD is some unknown function. In this case the regression (or ANOVA with linear trends) should look like the one for judgments of frequency:
where bDf being the slope.Footnote 8 The crucial prediction here is that judgments of duration depend only on exposure frequency and not on exposure duration.Footnote 9
The alternative was that the total time hypothesis was correct but not applicable to judgments of frequency. In this case, information about frequency and duration should be stored independently and therefore frequency information could be ignored when making judgments of duration:
and so a regression would result in
The crucial prediction here is that judgments of duration depend only on exposure duration and not on exposure frequency. This is the exact opposite of the first explanation, where judgments of duration depend only on exposure frequency and not on exposure duration. Thus, Hintzman’s thought process leads to a decision experiment.
2.1 Interpreting the Results of Hintzman’s Crucial Experiment
To his surprise, Reference HintzmanHintzman (1970) found something in between the two opposing models: that bDd was not 0, but that neither was bDf. Although one might think this result allows no definitive conclusion, Hintzman confidently rejected the unidimensional hypothesis. He studied r2 for the effects of frequency/duration on judgment of frequency (.97/.003) and judgment of duration (.85/.123) and in the Discussion stated (p. 442): “Since the JOD data reveal a pattern that differs from that of JOF, the two cannot be based on identical information.”
While the effect sizes evidently differ, it remains unclear how exactly the pattern contradicts a unidimensional model. A first attempt to understand Hintzman’s reasoning might be to study the correlation between judgments of frequency and duration. If it is low, this would be a good reason to reject the unidimensional model. To derive the correlation between judgments of frequency and duration, the four reported effect sizes are sufficient. In the Appendix we give a formal argument for the following reasoning based on covariance algebra. The general idea can be demonstrated by applying Wright’s well-known tracing rules (1934; for an introduction see Reference KennyKenny, 1979) to the paths in Figure 1. Note that Hintzman used correlations for his argument, but we use standardized regression coefficients, which, in this case, are equivalent.
Path model for judgments of frequency and duration.
To find the correlation between judgments of frequency and duration one can start at either judgment and trace all paths to the other judgment. For instance, starting from judgment of frequency, there are two paths to judgment of durationFootnote 10: (1) through frequency and (2) through duration. Both paths need to be added to find the total effect:
When calculating the correlation between the two judgments with Hintzman’s data, one will find 
With such a high correlation it is difficult to argue against a unidimensional model and for a two-dimensional model.
Another methodological approach to understanding Hintzman’s reasoning might be dissociation. Indeed, exposure duration has an effect on judgment of duration (.123), but not on judgment of frequency (.003; compare with the interpretation in Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010, p. 349). Often this constellation is seen as evidence of two independent dimensions. In general, this is a logical fallacy (Reference Dunn and KirsnerDunn & Kirsner, 1988). In Hintzman’s specific case, adding the appropriate amount of noise to judgment of frequency would reduce the effect of duration to zero, without requiring the introduction of a second dimension. But this would only be possible if the effect of frequency would be larger on judgment of duration than on judgment of frequency, which it is not. In other words, the key point is that the effects of frequency and duration are differently ordered in size: 
but 
but 
. This pattern is logically impossible with a single dimension.Footnote 11 To illustrate this, imagine a situation where we specify the coefficients between frequency/duration and memory strength, as in Figure 2.
Hypothetical unidimensional model for judgments of frequency and duration.
The tracing rules allow us to express the coefficients between the independent and dependent variables via
Now recall Hintzman’s pattern of results:
which can also be written as
Assuming that βmf and βmd are positive,Footnote 12 the equal terms cancel out and one has a contradiction:
Thus, in a unidimensional model, the coefficients have to have the same order: If βFf > βDf, then βFd > βDd. This is violated in Hintzman’s data, and assuming the result is not a coincidence, but reliable, there must be two dimensions.
2.2 Relationship to State Trace Analysis
The above deduction seems to come out of nowhere but is in fact just a special case of state trace analysis (for an introduction see Reference Dunn and KalishDunn & Kalish, 2018). The goal of state trace analysis is to determine the number of latent variables (here dimensions) required to explain empirical phenomena. The general idea is to theoretically constrain the type of relationship between independent/dependent variables and latent variables. The constraint leads to conditions under which certain empirical observations logically demand a certain number of latent variables. A typical scenario is to assume monotonic functions between a latent variable and two dependent variables (Reference Dunn and KirsnerDunn & Kirsner, 1988).Footnote 13 In this scenario, one can infer that the relationship between the dependent variables must also be monotonic, which can be tested empirically. If the relationship between the dependent variables is nonmonotonic, then there must be two latent variables.Footnote 14
Testing the relationship between judgments of frequency and duration for monotonicity is not possible for Reference HintzmanHintzman’s (1970) study because the needed data is not available. State trace analysis requires means and ideally also standard deviations for all experimental conditions, but Hintzman reported mainly correlations and F values of ANOVAs. But these statistics can still be put to use: When the relationship between the variables is constrained to be linear, state trace analysis can be simplified, resulting in the test condition described above (section Interpreting the Results of Hintzman’s Crucial Experiment).
If one assumes that all variables in Figure 2 are already standardized, memory strength (m) can be expressed as
This is also referred to as the input mapping in state trace analysis, as it maps the independent variables to the latent variable. Mapping the latent variable to the judgments (output mapping) results in
On substitution we can also write
In matrix notation this is
And here is the pivotal part. Note that the matrix B has rank 1. The rows and columns are multiples of each other with a ratio of 
, respectively. Thus, either judgment can be expressed in terms of the other judgment. This simply means that a single dimension is sufficient to explain both judgments.
To find out whether the rows are independent or dependent, we can study the determinant of matrix B, since a deficient matrix has dependent rows and columns. B can also be expressed as
and the determinant is
If the determinant is zero, the judgments are dependent. If the determinant is nonzero, the judgments are independent. The critical condition described above, βFf > βDf and βFd < βDd, corresponds to a case where the determinant is positive because the terms of the determinant on the left (βFf, βDd) are both larger than the terms on the right (βFd, βDf). A positive determinant is just a more specific case of a nonzero determinant.
It might be more useful to study the determinant directly because it is the more general condition. But error variance makes it unlikely one will find a determinant that is exactly zero, so one would need a more elaborate statistical framework to conduct a valid test. In contrast, testing the order of correlations is simple and straightforward, while not being less powerful. Furthermore, the boundary conditions are reasonable: All effects are expected to be positive and the effect of frequency should be larger on judgments of frequency than on judgments of duration. Thus, we have found a simple case of falsification. If βFd < βDd, the unidimensional model is incorrect. The test itself does not favor this hypothesis: Technically, the opposite result βFd > βDd is not less likely.
In light of the above derivation, Reference HintzmanHintzman’s (1970) implicit logical position is strong, but two problems remain. First, Hintzman probably unknowingly used the effect size ralerting for his argument. This statistic is not the correlation between the independent and dependent variable on the individual level, but on the aggregated level (correlation of averages).Footnote 15 Since we are interested in individual behavior and not in group behavior, unaggregated data should be used for the analysis.
Second, his conclusion is based on a single study with a sample size of 116. For medium to large effects this might be sufficient to reach high precision, but the effect of duration is quite small and will vary substantially from experiment to experiment. Indeed, in Reference HintzmanHintzman’s (1970) third experiment, duration actually had a significant effect on judgment of frequency, but he argued that the effect was quite small and a potential artifact (p. 439). This is surprising because the effect had the same size as the effect of duration on judgment of duration (almost the same ANOVA F value with the same degrees of freedom), which Hintzman did not regard as spurious. In the fourth experiment, Hintzman was dealing only with free recall and in the discussion he clearly rejected the unidimensional hypothesis.
In later publications an effect of duration on judgment of frequency was usually found, although its size varied (e.g., Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Williams and DursoWilliams & Durso, 1986; Reference WinklerWinkler, 2009; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011). Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) took up the task to explain why this effect varied and along the way resurrected the unidimensional hypothesis.
2.3 The Symmetry of Biases
Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) reframed the unidimensional hypothesis as the common-path hypothesis.Footnote 16Footnote 17 Their main argument was that biases in such a unidimensional model are symmetrical (or at least very similar) in size: βFd = βDf. While this sounds intuitive, it is not required nor sufficient for a unidimensional model to be valid. Recall that the general test condition is still 
. From this alone it does not follow that βFd = βDf. But if one starts from this assumption one will arrive at the required additional constraint:
Or verbally, the ratio of the effects of the independent variables on the memory strength is the same as the ratio of the effects of memory on the judgments. There appears to be no theoretical or empirical ground to assume that this constraint would be satisfied.
2.4 Conditional Unidimensional Hypothesis
Symmetrical biases might not be a good indicator of unidimensionality, but there is still substantial value in Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) work. When trying to produce symmetrical biases, they were mainly concerned with increasing the effect of duration on judgments of frequency. The influence of frequency on judgment of duration was well known (Reference HintzmanHintzman, 1970; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference WinklerWinkler, 2009), but the influence of duration on judgment of frequency has only sometimes been found and has varied in size (e.g., Hintzman et al., 1975; Reference WinklerWinkler, 2009). Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) main contribution to the field has been to explain this result and to find the conditions under which duration affects judgment of frequency. This attempt can also be seen as pointing out a fallacious dissociation: In some studies, duration had no effect on judgment of frequency only because the manipulation was too weak.
Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) postulated that the amount of attention paid to the stimuli is the critical variable. If a participant is required to attend to a stimulus for the whole presentation duration, memory strength will increase continuously and influence a single dimension in memory.Footnote 18
In one experiment they instructed participants to press a key until the stimulus disappeared or to specifically pay attention to either frequency or duration. In another experiment, they used different types of material. Simple stimuli (e.g., words) might take only 2 s for complete processing (Reference HintzmanHintzman, 1970), but more complex stimuli (e.g., pictures) can draw attention for a much longer duration. In several experiments, Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al. (2015) studied the effect of arousal as a means of changing processing intensity. In all these studies, duration had an effect on both judgments if attention was high. Thus, biases in both directions were present, but they were not perfectly symmetrical in size. Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) concluded that neither the unidimensional nor the two-dimensional hypothesis was supported. They suggested a conditional unidimensional hypothesis: Only under conditions of high attention will duration and frequency influence a single memory dimension.
One problem with this conceptualization is that it still requires two dimensions under conditions of low attention (when the biases are asymmetrical). Thus, the high-attention condition in the conditional unidimensional model might instead be seen as a case where the empirical data do not speak against a unidimensional model. Still the evaluation of this hypothesis by Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) rested on the symmetry criterion, which is not cogent. At the same time, the authors have shown that the relevant effects can vary substantially depending on the material and the attention of participants, so the pattern Reference HintzmanHintzman (1970) obtained is literally just one of many.
Overall it remains unclear whether the vast amount of data from Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) research speaks for a (conditional) unidimensional or a two-dimensional model. Besides, there are other studies that provide enough information to re-evaluate whether judgments of frequency and duration are based on one or two dimensions. Our goal in the remainder of this paper is to gather these studies and test the critical condition, if βFf > βDf then βFd > βDd.
3 Methods
The critical test can be conducted for every experiment that manipulated frequency and duration and assessed judgments of frequency and duration. Since there are some differences between the relevant studies, it makes sense to perform the test for every single study instead of aggregating the studies first. This also makes it easy to test the conditional unidimensional model: If there is a subset of studies that are consistent with a unidimensional model, we can look for similarities between these studies.
3.1 Selection of Studies
We queried Google Scholar for the search terms frequency AND duration AND [“(judgment OR judgement) of frequency” OR “(judgment OR judgement) of duration”]. We expected to find all studies where both independent variables were manipulated and both of the judgments were assessed. In addition, we did a forward search for the two main studies in this field, the seminal study by Reference HintzmanHintzman (1970) and the more recent study including four experiments with many conditions by Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010). Overall, this resulted in 193 hits. After scanning the abstracts we had to exclude many studies that were unrelated to the topic at hand. A high number of false positives was expected a priori, since the terms frequency and duration can be found in many areas of science. After this first selection, 12 articles remained but we had to exclude some that did not match the independent or dependent variables in question.
Reference Warm and McCrayWarm & McCray (1969) did not manipulate duration and frequency directly. The authors presented different words only once for 1 s. The words differed in their relative occurrence in the English language (familiarity) and their length (short or long). These manipulations deviate too much from the default procedure and therefore this study was excluded.Footnote 19 Reference Huppert and PiercyHuppert and Piercy (1977) assessed not judgment of frequency or duration as the dependent variable but recognition. Reference Mo and MichalskiMo and Michalski (1972) used pair comparisons and subsecond durations, which deviates too much from other studies. Several researchers (Reference BonannoBonanno, 1996; Reference HintzmanHintzman, 2004; Reference Williams and DursoWilliams & Durso, 1986; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011) studied only judgments of frequency and not judgments of duration, so we could not conduct the critical test. In one study (Reference Smith, Rule and PriceSmith et al., 2017) the independent variables had only two levels, so the effect size is not a normal correlation and our approach is not applicable.
Four articles in peer-reviewed journals remained (Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference HintzmanHintzman, 1970; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015). In addition, we received several unpublished raw data sets from Reference WinklerWinkler (2008). One might argue that unpublished data do not meet the quality standards of current scientific practices and thus should be excluded. But in our opinion the better approach is to include these studies and treat their quality as a moderating variable. In our specific case all these studies come from one source (Reference WinklerWinkler, 2008), so a subgroup analysis would also resolve the problem. As we show, this is not necessary since the data are conclusive.
Another problem we needed to address is that some authors studied average duration while others studied total duration. In the former the duration of a single presentation is held constant, while in the latter the total duration of all presentations is held constant. This difference has been somewhat neglected in the literature, presumably because the research focus was mainly on the empirical and not on the theoretical side. In our analysis we integrated both types of duration manipulation and can use this information as a moderator variable. Again, this does not play a big role since the data are conclusive.
Table 1 summarizes the selected studies. Since Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al. (2015) is a subset of Reference WinklerWinkler (2009), we considered only the latter. Most of the articles report several experiments, which in turn consist of multiple experimental conditions. Overall, our analysis contains 152 effect sizes from 38 conditions out of 19 experiments.Footnote 20
Note. In the first two experiments Reference Hintzman, Summers and BlockHintzman et al. (1975) did not assess judgments of duration, so they were excluded. In two studies Reference WinklerWinkler (2008) did not assess the type of duration that was manipulated, which makes our approach inapplicable. These two studies were also excluded.
3.2 Attention
According to the attention hypothesis (Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010), the duration of a stimulus will affect its memory strength only if the stimulus requires prolonged processing. A complex or relevant stimulus attracts attention, and processing can continue for a long time. In this case, duration matters, and according to the conditional unidimensional model (Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010) a single dimension is used for judgments of frequency and duration. In the analysis we used stimulus type and other attention manipulations as a moderator.
The material presented to the participants differed between the experiments: words (e.g., first names or foreign language words), images for which the degree of arousal varied, or video scenes. Accordingly, we divided the visual material into three groups (words: 0, pictures: 1, videos: 2) to numerically represent the different degrees of attention the three types of stimuli presumably draw. Furthermore, in some experiments there were special manipulations to increase attention. For instance, Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) required participants to press a button during stimulus presentation to increase processing intensity. If there were manipulations of this kind, we coded them with 1, otherwise with 0. We then combined stimulus type and manipulation into an attention score, ranging from 0 to 2 (0+0: words with no special manipulation; 0 + 1: words with special manipulation or 1 + 0: pictures without special manipulation; 2 + 0: videos without special manipulation; or 1 + 1: pictures with special manipulation). Note that there was no experiment that used videos in combination with an additional manipulation, so a score of 3 was never reached.
3.3 Statistics
Most researchers employed analyses of variance (ANOVAs) with contrasts or linear trends as their analysis strategy. To test the critical condition we need the correlation coefficients, which can be calculated from this data. Specifically, in contrast analysis, r effectsize corresponds to the correlation between the contrast weights and the dependent variable. The contrast weights are the values of the independent variables, and thus r effectsize is the correlation we are looking for.
Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) reported enough information to calculate the error variance and conduct an ANOVA as well as a contrast analysis without possessing the raw data. The effect size can then be calculated with the following equation (Reference FurrFurr, 2004, p. 10):
where F between and dfwithin are from an ANOVA with a single factor (all between conditions).
Reference HintzmanHintzman (1970) and Reference Hintzman, Summers and BlockHintzman et al. (1975) correlated the mean values of judgments of frequency for each condition with the corresponding values of duration and frequency. Although the authors did not mention it, this correlation corresponds to r alerting and can be transformed to r effectsize with the following equation (Reference Rosenthal, Rosnow and RubinRosenthal et al., 1999, p. 46):
where r 2contrast can be calculated from the F value of the reported linear-trend ANOVAs.
Reference WinklerWinkler (2009) calculated statistics for dependent measurements (g), where subject-specific variance is controlled for. These data are not directly comparable to the other studies, but we were able to calculate (r effectsize from the provided raw data.
3.4 Analysis Strategy
The critical test consists of two inequalities and can be performed on each individual data set. Evidence against the unidimensional hypothesis can be acquired by simply counting the number of violations of these inequalities. An intuitive way to do this is by (a) transforming the inequalities such that the right-hand side is 0:
and (b) plotting the differences on the left-hand side of both inequalities against each other. The resulting plot will have four sectors and one can directly see how many violations of the critical test exist. If the unidimensional hypothesis is correct, we would expect no violations (or only a few violations attributable to chance).
4 Results
As can be seen in Figure 3, in every experiment (or experimental condition) the influence of frequency was larger on judgment of frequency than on judgment of duration (βFf − βDf > 0; only Quadrant 1 at the top right and Quadrant 4 at the bottom right hold data). For the unidimensional hypothesis to be valid, this pattern should also hold for duration (βFd − βDd > 0; values should be found only in Quadrant 1). In only 3 (of 38) cases was this fulfilled, a relative frequency of 7.9% (95% confidence interval [1.7%, 21.4%]). Thus, we found 35 cases that speak against a unidimensional model.
Visual analysis of the test condition. R code to reproduce figure: https://github.com/johannes-titz/commonpath.
Since there are only three deviating data points, moderator analyses are not required. Any differences between the studies, such as attention of participants, instructions, or type of duration judgment, would not alter the conclusion that the data are inconsistent with the unidimensional hypothesis. Although the evidence is clear, it might be worth looking at the three deviating cases in more detail (Table 2). Note that in only one condition of Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) experiments is the unidimensional hypothesis not rejected; in all other conditions (10), it is. The one condition produced effects of -.02/.02 for duration on judgment of duration/frequency, which are essentially null effects. Thus, our analysis contradicts Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) statement that there is mixed evidence regarding the unidimensional and two-dimensional hypotheses. Independent of the attention condition, the unidimensional hypothesis has to be rejected and thus the conditional unidimensional hypothesis is also unsupported.
Note. e: experiment, c: condition, f: frequency, d: duration, F: judgment of frequency, D: judgment of duration
Further, note that in the three deviating studies, two effects of duration on judgment of duration are negative, the only ones of the 152. If these effects were larger they might hint at problems in the experimental setup: Stimuli presented for a longer duration should not be judged as shorter. But since these effects are close to 0, they are likely just the result of noise.
5 Discussion
In this paper we have tried to answer whether judgments of frequency and duration are based on one or two dimensions. While this question is old, interest in it has reawakened in the last decade (Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference Smith, Rule and PriceSmith et al., 2017; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011), probably because it has never been answered conclusively. We first retraced the theoretical roots of this question, starting with Reference HintzmanHintzman’s (1970) seminal paper. We showed how he transferred the total time hypothesis from memory research to judgments of frequency and duration. Reference HintzmanHintzman’s (1970) verbal statements relating both judgments to memory were expressed formally to better understand the implications of the unidimensional and two-dimensional models. Although Reference HintzmanHintzman’s (1970) crucial experiment was not consistent with either of these models, he confidently rejected the unidimensional one. His main argument was that the empirical pattern for both judgments was “too different” for a unidimensional model to be valid. This somewhat vague statement seems to correspond to our more stringent criterion regarding the order of effect sizes. The stringency of this criterion lies in its relation to state trace analysis, a general method for testing the number of latent variables involved in a phenomenon.
While Hintzman’s conclusion was implicitly based on strong inferential logic, he ignored reliability issues. It was not clear how robust the effects were or whether a different pattern of results could occur in subsequent experiments. It took some time until Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) pointed out this and other problems with Reference HintzmanHintzman’s (1970) conclusion. They found that the effect of duration on both judgments varied substantially from study to study. As a consequence, Reference HintzmanHintzman’s (1970) definitive statement could be correct for some studies, but incorrect for others.
To explain why the effect of exposure duration varied so much, Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) introduced attention as a moderating variable. They hypothesized that if attention is low, the variation of duration goes unnoticed and one might erroneously think that duration has no effect at all. But if attention is high, duration has an effect on the memory strength and eventually also on both judgments. Thus, only under conditions of high attention is a unidimensional model valid. To test this conditional unidimensional model, Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) introduced the idea that symmetrical biases are evidence of unidimensionality. Under conditions of high attention, they indeed found relatively symmetrical biases and concluded that their data is mostly in line with the conditional unidimensional model. But we showed that this conclusion is invalid in the context of state trace analysis because symmetrical biases is not a sufficient criterion for unidimensionality.
Overall, it has remained unclear whether the data on judgments of frequency and duration speak for a unidimensional or a two-dimensional model. We gathered all available experiments in the literature and tested the critical inequalities. Almost all studies are inconsistent with the unidimensional model. Consequently there are also no moderating variables regarding the number of dimensions, at least not in the data we analyzed. Specifically, under conditions of high attention, there is also no evidence of a unidimensional model.
Reference HintzmanHintzman’s (1970, p. 442) initial intuition, while somewhat vague, was correct: “Since the JOD data reveal a pattern that differs from that of JOF, the two cannot be based on identical information.” In contrast, Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) conditional unidimensional model turned out to be irrelevant because there is no support for any variant of the unidimensional model. Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al.’s (2015, p. 17) conclusion that their “findings strongly argue for the existence of a common mechanism underlying the processing of frequency and duration” has to be doubted. Furthermore, discussions of the unidimensional model to explain isolated results of a few experiments require an update (Reference Smith, Rule and PriceSmith et al., 2017; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011).
5.1 Two Dimensions
If there are two dimensions that determine judgments of frequency and duration, then the question of what these dimensions are arises. There are two views on this that are both related to memory. The first one follows the idea that judgments of frequency and duration are based on different memory constructs from existing memory theories. The second one states that exposure frequency and duration are different, independent attributes of a remembered event.
The first view was already proposed in the initial publication on judgments of frequency and duration (Reference HintzmanHintzman, 1970, p. 441): “The notion that long-term memory involves two mechanisms, one related to F and the other to total time, bears enough similarity to the idea that recognition and recall involve two different processes.” Indeed, Hintzman has approached this type of question repeatedly in his research (see Hintzman, 2011, for a summary). For instance, he investigated whether judgments of frequency or judgments of recency might be completely based on the familiarityFootnote 21 dimension of memory (Reference HintzmanHintzman, 2001), which they were not.
Analogously, one could ask whether judgments of frequency or duration are based on familiarity, while the other is based on recollection. Since recollection and familiarity and judgments of frequency and duration are all affected by exposure frequency and duration, it appears natural to be interested in their interrelatedness. But Reference HintzmanHintzman (2011, p. 259) concluded that judgments of frequency, duration, and recency as well as recognition memory are not based on the same information because of substantial task dissociations. This conclusion is problematic because task dissociations can occur with a single dimension. Not dissociation, but state trace analysis is the proper method for studying how many constructs are required to explain judgments of frequency, duration, and recency, as well as recollection and familiarity. One way to find out is to conduct new experiments that are tailored to the method of state trace analysis. Such a research programFootnote 22 bears potential for some surprise because its superior methodology could invalidate most of the past studies. Specifically, one might find that judgments of frequency are based on one memory construct and judgments of duration on a different one.
Let us now look at the second view, that judgments of frequency and duration are different attributes of memory that are independent and unrelated to other memory constructs. When remembering an event, different features can be accessed, one of them being the exposure frequency and another the exposure duration. At first glance this idea is appealing since it does not overcomplicate the problem and simply assumes that different things are not the same, but different: “People have no trouble telling repetition, duration and recency apart” (Reference HintzmanHintzman, 2011, p. 259). But this statement is not quite correct. Judgments of duration are highly dependent on exposure frequency (e.g., Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference HintzmanHintzman, 1970; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015). The correlation between exposure frequency (the irrelevant variable) and judgments of duration is usually higher than between exposure duration (the relevant variable) and judgments of duration. This is a surprising finding if one assumes that humans have direct access to exposure duration as a distinct dimension. To be consistent with empirical findings, one needs to assume that separate pieces of information about exposure frequency and duration are combined to come up with judgments of frequency and duration. How exactly this happens is a theoretical problem worth approaching, but that it must somehow happen takes away the simplicity initially gained by introducing two independent attributes.
So far, we have mainly focused on theories of memory. When taking a judgment perspective, the theory of magnitude (ATOM; Reference Bueti and WalshBueti & Walsh, 2009; Reference WalshWalsh, 2003) is likely the most prominent theory related to judgments of frequency and duration (as already suggested in Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015). According to ATOM’s basic assumption, all quantities—speed, size, duration, location, or number—are processed in the same brain region.Footnote 23 Judgments related to time, space, and quantity hypothetically all overlap to some degree. This explains why judgments of duration are affected by exposure frequency and judgments of frequency by exposure duration. Although ATOM offers an interesting view, it suffers from not specifying concrete processes. It remains unclear what exactly happens in the specific brain regions. One might naively suggest that some neurons are responsible for processing frequency, some for processing duration, and some for both. In this case, on the macro level, there are three dimensions, but the behavioral predictions do not change much from the memory-oriented views. Biases should be present and the judgments are expected to be correlated to some degree, but state trace analysis will result in at least two dimensions. Thus, the main task in the future is to accurately specify the different views on the two-dimensionality in judgments of frequency and duration to make more elaborate predictions.
5.2 The Assumption of Linear Relationships
Our assumption of linear relationships is mostly a consequence of previous work. Contributors in the field usually did not question it (Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al., 2010; Reference HintzmanHintzman, 1970; Reference Hintzman, Summers and BlockHintzman et al., 1975; Reference Williams and DursoWilliams & Durso, 1986; Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al., 2015; Reference Zhao and Turk-BrowneZhao & Turk-Browne, 2011). All of their analyses, such as ANOVAs with linear trends, contrast analysis with linear contrasts, correlations, regression with untransformed variables, assume linear relationships between independent and dependent variables. Thus, the whole reasoning of these authors is implicitly based on the linearity assumption. To understand their arguments, we had to take their position. Without doing this, we could not have understood why Reference HintzmanHintzman (1970) was convinced that his correlation pattern is crucial to rule out a unidimensional model. We might also have missed that symmetry in biases is not a sufficient condition for a unidimensional model and that Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al.’s (2010) data required a re-analysis.
In addition to this pragmatic reason, there is some evidence for the linearity assumption: Reference HintzmanHintzman (1970) compared linear with logarithmic models and found very small and inconsistent differences in R 2. The figures in Reference BonannoBonanno (1996) as well as in Reference WinklerWinkler (2009) show linear relationships for almost all conditions. The data in Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) look fairly linear too. Overall, it appears that, for the particular values of the independent variables chosen in these studies, the relationships in question can be assumed to be linear. If other, more extreme and more finely spaced values are chosen, this assumption might eventually be violated.
If this is the case, a normal state trace analysis could be performed as an alternative. Usually, only the assumption of monotonic relationships is made in state trace analysis, which appears reasonable in judgments of frequency and duration. Most theoreticians would assume that the memory strength is a monotonically increasing function of frequency and duration (i.e., when increasing exposure frequency or duration, the memory strength will not decrease). This assumption is also reasonable for the relationship between the memory strength and the judgments. Note that to conduct state trace analysis, correlations between independent and dependent variables (as used here) are not sufficient, so new experiments need to be run.
5.3 Problems of Comparability
There might be concerns that the data we used to test the critical condition are too diverse. Specifically, the independent and dependent variables regarding duration were not the same in all experiments. Reference HintzmanHintzman (1970) was mainly interested in average duration, while Reference Betsch, Glauer, Renkewitz, Winkler and SedlmeierBetsch et al. (2010) were interested in total duration.Footnote 24 Reference WinklerWinkler (2009) and Reference Winkler, Glauer, Betsch and SedlmeierWinkler et al. (2015) studied both. While this concern is definitely problematic when aggregating the data (e.g., in a meta-analysis), it is not a problem in our analysis. Since almost all experiments violate the unidimensional hypothesis, it does not matter whether single or total duration was manipulated and assessed. For both variables, there is no evidence of a unidimensional model. This logic applies to all potential moderators such as range and mean of independent variables, instructions, or attention manipulations.
5.4 Conclusion
On the basis of a methodologically stringent criterion and data from many experiments, we can conclude that judgments of frequency and duration are probably based on two independent dimensions. There seems to be only one convincing way to still argue for a unidimensional model: a violation of the linearity assumption. In this case, novel experiments should be conducted and analyzed with the method of state trace analysis. This is also a good approach to differentiate between different two-dimensional models: State trace analysis can reveal whether judgments of frequency and duration are based on other existing memory constructs. Finally, more theoretical work is required to understand why humans confuse frequency and duration, although the judgments of these attributes are based on two independent dimensions.
Appendix
Covariance Algebra for One Dimension
If there is a single dimension on which both judgment of frequency and judgment of duration are based, judgment of frequency and judgment of duration should be correlated. If there are two orthogonal dimensions they should be uncorrelated.
To demonstrate this formally, we need to study the standardized regression coefficients, which will lead us directly to the correlation between the two judgments. In general, standardized regression coefficients play an important role because most arguments in the literature were directly or indirectly based on correlations or equivalent effect sizes (e.g., R 2, η2) and not on unstandardized effects (e.g., unstandardized regression coefficients).
The correlation between judgment of frequency and judgment of duration reduces to the covariance if the variables are standardized:
Let us assume that both judgments are affected by frequency and duration and thus are linear combinations of these variables:Footnote 25
where f z and d z are now the standardized variables of frequency and duration and the β’s are the standardized regression coefficients. Note that in the case of uncorrelated independent variables, the standardized coefficients are equal to simple correlations and thus we conventionally use β for them.
By applying covariance rules (e.g., Reference KennyKenny, 1979), in a few steps we get to
In a controlled experiment the covariance between f z and d z is 0 and because the variables are standardized, the variance of both variables is 1, which reduces the formula to
The presented logic can also be followed purely functionally (cf. Reference Dunn and KirsnerDunn & Kirsner, 1988). If judgment of duration and judgment of frequency are based on the same memory strength, then
and
Applying the inverse function to express m in terms of F results in
and now substituting m results in
Or in words, judgment of duration will be a function of judgment of frequency. Under the assumption of a linear relationship, a positive correlation will result between the two variables. The analysis of Reference Dunn and KirsnerDunn & Kirsner (1988) shows that this functional dependence does not logically exclude a two-process model. For instance, if duration and frequency are functionally dependent or two memory dimensions are functionally dependent, we cannot exclude a two-process model that just looks like a one-process model. But, duration and frequency are uncorrelated in an experiment and the simplest model with the fewest degrees of freedom will be a unidimensional model.
Open access
