A new approach to the study of a relatively neglected property of mental architecture—whether and when the already-processed elements are separated from the to-be-processed elements—is proposed. The process of numerical proportion discrimination between two sets of elements defined either by color or by orientation can be described as sampling with or without replacement (characterized by binomial or hypergeometric probability distributions respectively) depending on the possibility to tag an element once or repeatedly. All empirical psychometric functions were approximated by a theoretical model showing that the ability to keep track of the already tagged elements is not an inflexible part of the mental architecture but rather an individually variable strategy which also depends on conspicuity of perceptual attributes. Strong evidence is provided that in a considerable number of trials, observers tagged the same element repeatedly which can only be done serially at two separate time moments.
Citation: Raidvee A, Põlder A, Allik J (2012) A New Approach for Assessment of Mental Architecture: Repeated Tagging. PLoS ONE 7(1): e29667. https://doi.org/10.1371/journal.pone.0029667
Editor: Suliann Ben Hamed, CNRS - Université Claude Bernard Lyon 1, France
Received: June 16, 2011; Accepted: December 2, 2011; Published: January 9, 2012
Copyright: © 2012 Raidvee et al. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: This study has been supported by the Estonian Science Foundation Grant 8231 and the Estonian Ministry of Science and Education Grant SF0180029s08. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Competing interests: The authors have declared that no competing interests exist.
The way mental processes are organized—their architecture—has been one of the main concerns for both psychologists and neuroscientists [cf. 1]. The question of whether people perform perceptual and mental operations in parallel or in series, has been pivotal in many of these pursuits , . Overwhelmingly, the debate about serial vs parallel processing has been concentrated on reaction time data. In a seminal experiment, Sternberg  demonstrated that when observers judge whether a test symbol is contained in a short memorized sequence of symbols, their mean reaction-time increases linearly with the length of the sequence. The linearity and slope of the function were interpreted as strong evidence in favor of an internal serial-comparison process whose average rate is between 25 and 30 symbols per second. However, as it was soon shown by a thorough theoretical analysis, the distinction between serial and parallel processing is constrained by model mimicking: parallel models can lead to exactly the same predictions as serial ones despite the completely different psychological assumptions they are based on , .
One lesson that can be derived from the serial vs parallel controversy is that it cannot be resolved in isolation from other relevant attributes of the cognitive architecture. For example, it became evident that the questions about stopping rule – the conditions under which the system ceases processing and generates a response – or the questions about capacity limitations, are inevitably linked to the question about serial vs parallel architecture . Considering this lesson, it is surprising that even though a number of studies exist on serial vs parallel processing in the context of enumeration accuracy of independent sets, e.g. , , the serial vs parallel debate has almost entirely escaped the numerosity discrimination accuracy problem. At least one study has shown similar counting and subitizing processes to those measured in standard enumeration tasks to be involved in the number discrimination task with a single stimulus set . Yet, not much information is available about the nature of processes involved in numerosity discrimination in case the stimulus display contains multiple distinct sets.
In the following, we use the term counting as referring to any process aimed at finding the total number of elements in a set. The term is neutral with respect to the temporal properties of the processes involved: counting can be parallel, serial, or mixed.
It has long been known that it takes at least 5–6 years before children are able to learn all principles that are needed for counting, including assignment of numerals for objects . But even after learning to count it is not guaranteed that perceptual mechanisms follow the principles used in verbal and propositional thinking. It is possible that even the most fundamental principle of numeration – the one-to-one correspondence between items and counting tags in the process of transformation of every item from the to-be-counted category to the already-counted category – cannot always be obeyed [cf. 9]. Perceptually it may be difficult to assign only one counting tag to every object with the purpose of preventing the same object from being counted twice. When the searched objects lack a clear structure it may be difficult to keep track of which object is already counted and which is still on the waiting list.
To the best of our knowledge, there is no generally accepted method for establishing whether or not the tagging process follows exactly the one-to-one principle. Unlike many previous studies which have used analysis of reaction times to differentiate between serial vs parallel processing styles, we attempt to reveal this property of mental architecture on the basis of probability distribution of responses. Our approach stems from an ideal observer analysis which purpose is to establish an absolute scale of performance for an ideal perceptual device that is limited only by stochastic characteristics of the stimulus itself . Let's suppose that the observer's task is to discriminate the numbers of two distinct sets of randomly distributed elements. These two sets can be distinguished by their spatial position, occupy two separate areas, for example , or they can be intermixed but distinguished by a certain visual attribute, such as color or orientation . This is a relatively simple task, as even pigeons, with a brain weighing less than 3 g, can be trained to discriminate numerical proportion in the mixtures of two types of elements with considerable accuracy , . As expected, an ideal perceptual device can notice even one element difference irrespective of the total number of elements. Real observers, human or nonhuman, usually perform less accurately, presumably because their decisions seem to be based on only a fraction of available items. It is conceivable that instead of all presented elements the real observers are able to take into account only a fraction of the elements, especially when these elements have a random spatial distribution and are presented for a very short time. Formally, this situation resembles the inverse probability problem in which a sample of randomly selected elements serves as a basis for inference about the true proportion of elements hidden from the observer. Jacob Bernoulli in his posthumous Ars conjectandi (1713/1899) devised an ingenious urn problem as an idealized mental exercise in which some objects or concepts of real interest (such as people, event outcomes, visual objects, etc.) are represented as colored balls or pebbles which are drawn, one after another, randomly from the urn and their color is noted. Every probability textbook teaches that balls or pebbles once extracted can or cannot be returned to the urn, which leads to two distinct probability distributions for the number of balls of a given color: the binomial and hypergeometric distributions, respectively. These two different replacement schemes, however, have an important application to the problem of mental architecture. Provided that Bernoulli's urn model describes sufficiently accurately what happens in the perception of numerical differences, the scheme of sampling with replacement (leading to the binomial distribution) implies that there is no tagging of which elements are already counted and which are not: the same element can, in principle, be inspected more than once. Consequently, if empirically determined psychometric functions for numerical discriminations between two sets of items are better described by binomial than hypergeometric distribution, it would provide evidence that some of these elements are inspected twice or more times which, understandably, can only be done serially at two or more different time moments. On the other hand, the scheme of sampling without replacement (leading to the hypergeometric distribution) implies that there is accurate one-to-one tagging of which elements are already counted and which are not, leading to an element being inspected only once, maximally. The attribution of one-to-one counting tags (corresponding to the sampling scheme without replacement) is by itself neutral to the problem of parallel or serial counting.
If an observer strictly adhered to the hypergeometric model (see equations (3) and (4) in the Methods section) with the parameter K (the number of elements taken into account in the decision process) being equal to the total number of elements in the stimulus display, N, then he or she would always determine correctly which of the two types of the elements is more numerous. The fact that the real observers in our experiments make errors indicates, within the proposed approach, that either they only take into account proper subsets of the elements (adhering to the hypergeometric model with K<N) or they count some of the elements more than once, adhering, at least partially, to the binomial model. Our analysis below indicates that both these possibilities take place: to account for the data best we need to assume that the observers in some trials use the hypergeometric model and in other the binomial model, with K varying from trial to trial. In relation to the seriality vs parallelity of counting, the conformity of the data with the hypergeometric model (i.e., sampling without replacement, one-to-one tagging of selected elements) leaves the question of seriality vs parallelity open. But once the data are shown to require the binomial model for at least a fraction of all trials, one has to accept that some elements can sometimes be counted more than once, and this can only be done serially, at two or more separate time moments.
The overall aim of the experiments was to introduce a new approach for the assessment of mental architecture, namely the property of whether, in the process of proportion discrimination of multiple stimulus sets, certain elements were being counted repeatedly. In our view, the aim was achieved by showing that this is indeed the case at least in some of the trials.
The study has been approved by the local Research Ethics Committee.
Four 20-year-old female observers with normal or corrected to normal vision were asked to decide which of the two distinctive sets of objects were more numerous by pressing one of two buttons. In two separate series these two sets of objects were distinguished either by color or by orientation. A schematic view of the two types of stimulus configurations is shown in Figure 1. In the first series a randomly distributed collection of red and green circles was presented. The red and green circles had a luminance of about 23.5 cd/m2. To diminish the impact of total red vs green area on the responses, size of the circles was randomly varied in the range of 11 to 22 minutes of arc. In the second series of the experiments a collection of short black line segments of luminance 0.3 cd/m2 and tilt of 20° either to the left or to the right from the vertical direction was presented. The width and length of a line subtended 2′ and 19′ respectively (and height of its vertical projection 16′). Both types of stimuli were presented within an elliptical gray background with luminance of 54 cd/m2 and with lengths of horizontal and vertical axes 8.86° and 8.70° respectively. This elliptical background was in the center of a rectangular area of luminance 64 cd/m2 filling the rest of the screen. In order to avoid overlaps between elements, each element was positioned within an invisible inhibitory area which prevented other elements to be closer than 22′. Each stimulus element had a high contrast to guarantee its 100% identification would it have been presented in isolation. The total number of objects N presented on the display was kept constant through each experimental session and was equal either to N = 9 or 13 elements. These two relatively small values were chosen because the difference between the response probabilities from the binomial vs hypergeometric models is greater in case the total number of elements is small. During experimental sessions, the relative proportion of the type A and type B elements was varied. For example, for the total number of N = 9 the relative proportions of A (red or tilted to the left) and B (green or tilted to the right) element categories were the following: 1∶8, 2∶7, 3∶6, 4∶5, 5∶4, 6∶3, 7∶2, and 8∶1. The stimuli were presented at a viewing distance of 170 cm for 200 milliseconds, with 3 seconds for responding.
Schematic view of stimulus configurations used in the numerosity discrimination experiment using color (left panel) or orientation (right panel) as a distinctive attribute.
All stimuli were generated on the screen of a Mitsubishi Diamond Pro 2070SB 22″ color monitor (frame rate was 140 Hz with the resolution 1024×769 pixels) with the help of a ViSaGe (Cambridge Research Systems Ltd.) stimulus generator. Every stimulus condition was replicated 100 times. Choice probability of the red circles was plotted as a function of the proportion of red elements NR in the total number of elements on the display N = NR+NG. Similarly in the orientation experiment, probability of the choice of the leftward tilted elements was measured as a function of the proportion of leftward tilted elements N(\) in the total number of elements on the display N = N(\)+N(/).
Mathematical expression of the psychometric models
- k is any positive natural number;
- p is the proportion of a certain type of elements to the total number of elements (either NA/(NA+NB) or NB/(NA+NB), depending on the experimental definition;
- K is the number of elements taken into account in the decision process.
- k is any positive natural number;
- NA is the number of type A elements in the stimulus;
- NB is the number of type B elements in the stimulus;
- N is the total number of elements in the stimulus (N = NA+NB);
- K is the number of elements taken into account in the decision process.
As stated above, one only needs to consider either odd or even values of K because the probabilities given by a pair of equations (either those for the binomial model or for the hypergeometric model) are equal, given equal values for k.
The obtained psychometric functions are shown in Figure 2. The probability of the choice of “red” (color experiment) or “leftward tilt” (orientation experiment) are plotted as a function of the proportion of the respective type of elements in the total number of displayed elements. As expected, the choice probability monotonically increases with the increase in the proportion of the indicated elements.
The choice probability as a function of the proportion of the chosen response category for four observers, two discrimination tasks (color and orientation), and two numbers of elements (N = 9 and 13). Each point is a probability estimate computed from 100 trials. The dotted line represents the best fitting theoretical mixture model shown in Tables 1.A and 2.A.
It is assumed that the observer's decisions between response categories A and B are based on the inspection of K elements that are randomly selected from all available elements N. If the number of the A-type elements KA in the selection exceeds the number of B-type elements (KA>KB), then the response category “A” is chosen; in the opposite case the response category “B” is chosen. If the numbers of A and B elements happen to be equal (KA = KB) for an even number of selected elements K, then the choice between “A” and “B” response categories is random with probability 0.5. Following this simple decision rule it is easy to compute all theoretical cumulative probability functions for binomial and hypergeometric distributions. Figure 3 demonstrates these theoretical binomial and hypergeometric models for odd numbers of selected elements K (the sample size). One only needs to consider odd numbers of elements since K = 2k−1 (odd) and K = 2k (even) yield identical predictions. The equivalence of K = 2k−1 and K = 2k is easy to demonstrate numerically for any arbitrary k value or demonstrate their formal equivalence by using, for example, Wolfram's Mathematica. However, an analytic proof seems to go beyond ordinary algebra. The mathematical formulations of response probabilities from both types of models – binomial and hypergeometric – are given in the Methods section.
All possible theoretical models corresponding to binomial (binK) or hypergeometric (hypK) distributions with the length of trials K.
Only in a few cases were the empirical psychometric functions close enough to one of these model predictions. This outcome is expected since it would be unrealistic to assume that the observer can use a fixed number of elements K in each trial through the whole sequence of trials. It is more realistic to assume that the number of selected elements K is a variable and changes from one trial to another. Also, there is no clear reason to hold any one specific combination of theoretical models strictly superior to the others as, within error limits, many mixture models are able to provide a comparable fit. Therefore, the emphasis of the current analysis is to estimate the relative performance of the hypergeometric models to that of a combination of both hypergeometric and binomial models. We are greatly indebted to Ehtibar Dzhafarov for suggesting the described approach. At the heart of the underlying logic lies the assumption that in case any binomial component(s) is/are able to improve the overall fit of the mixture model (with the maximum number of possible mixture components held equal to the number of respectively possible hypergeometric models) then that would be an indication in support of serial processing in at least some of the trials.
An approximation algorithm based on least squares optimization was written which looked for the weighted combination of all theoretical models which minimizes the sum of squared errors between theoretical predictions and points of empirical functions. Prior to plotting the best mixture of theoretical models vs the empirical psychometric functions, the latter were shifted to the left or right to make their mean (μ) equal to 0.5. If the mean of all responses deviates from the expected 0.5 then it characterizes a response bias towards one of the two response alternatives. As expected, the empirical means were close to 0.5, ranging from 0.44 to 0.53.
The best predictions of the mixtures of theoretical models are shown in Figure 2 as continuous psychometric functions. The parameters of these best fitting mixture models are shown in Tables 1.A and 2.A. The number in the column corresponding to the theoretical model (binK or hypK) indicates the percentage of trials in which each of these models is expected to be used. For example, in the first row in Table 1.A the mixture model is described as 31•hyp5+26•hyp7+15•hyp9+28•bin3, which means that for the observer S1 the best fit was obtained when the hypergeometric model with the sample size of either K = 5, K = 7 or K = 9 was supposed to be used in 31%, 26% and 15% of all the individual trials, respectively, and the binomial model with the sample size of K = 3 was used in the remaining 28% of the trials. Even a visual inspection can reveal that the fit to all 16 empirical psychometric functions shown in Figure 2 was excellent. This was confirmed by more formal tests showing that the predicted psychometric functions were able to explain on average 98.86% of the total response variance. Thus, only about 1.14% of total variance on average remained unexplained and could be attributed to measurement error.
The maximum number of components in the best fitting mixture models is four in case N = 9 (Table 1.A) and six in case N = 13 (Table 2.A) in order to keep the number of regressors equal to that of the competing mixture composed of hypergeometric models only. The best predictions obtained by hypergeometric models alone are given in Tables 1.B and 2.B. In most cases does the fit of the mixture containing binomial model(s) surpass that of the respective mixture containing only hypergeometric models. In Tables 1.A and 2.A, in cases where the binomial component improved the fit, the number presenting the proportion of unexplained variance is underlined. Since in 12 out of 16 cases addition of the binomial component improved the fit one can conclude that there were a significant number of trials in which the observers were not able to track exactly the elements that were already counted and those that were not.
In general, it is known that numerical discrimination based on color is more efficient than one based on geometric attributes, such as orientation [cf. 12]. This seems to be in agreement with our results: across all conditions and observers on average 5 elements were taken into account in orientation discrimination task and 7.5 elements when color was the distinguishing attribute.
In both types of tasks the hypergeometric distribution provided a better fit than the binomial one: in 65.3% of all trials when applied to discrimination on the basis of orientation, and in 88% of trials when applied to discrimination based on color. It was not entirely surprising to discover some small individual differences since it was previously shown that some participants adhered to a serial processing profile in most conditions while other participants could exhibit parallel-like strategy in some conditions at least .
In order to enumerate objects accurately it is necessary to follow certain rules. One of these basic rules is the maintenance of the one-to-one relationship between objects and tags assigned to these objects: every object needs to be tagged only once. It is generally unknown whether and how well different perceptual processes are able to separate the to-be-counted items from the already-counted ones. In this study we have proposed a new approach to this problem. Although the question of whether and when people can perform perceptual and mental operations in parallel or in series has been dominating debates about mental architectures, it was also made clear that this central question can be answered only when other related questions such as stopping rules, selective influence , , and capacity limitations have been answered as well , . The one-to-one principle of tagging obviously belongs to the same category of the related problems. In this study we presented strong evidence that it is reasonable to assume that in a considerable number of trials observers behave as if they are not able to keep track of the elements they have already counted. It is very likely that when forming their decision, they have taken the same element into account repeatedly. Since the same element can be visited twice or more times only on different time moments, this is a strong indication that at least some operations are executed serially.
The obtained evidence does not allow to assert that the adherence to the one-to-one tagging principle is an inflexible part of the mental architecture. Previous studies have shown that depending on the observer and stimulus conditions the parallel processing strategy can be used in some and the serial processing strategy in other situations . Our results seem to suggest that in perceptual tasks that can be solved more automatically and spontaneously, like discriminations based on color, the observers have a tendency to keep track of elements that have already been counted. By contrast, in tasks like discrimination based on orientation that require more deliberation and scrutinizing of each element, the observers tend to confuse which elements have already been counted and which have not. Although the accurate tagging of the counted elements does not necessarily mean that the processing is executed in parallel, lack of the one-to-one tagging implies that at least some elements are processed serially, one after another. However, these are not inflexible rules. For instance, one of the four observers performed better in the orientation based discrimination task than in the color discrimination task. This seems to suggest that avoidance of repeated tagging of elements is not a rigid part of mental architecture but rather a flexible strategy that can be changed and, if necessary, learned. This conclusion is supported by the fact that no single theoretical model was able to provide a satisfactory explanation for most of the empirical psychometric functions. The best fit was found when predictions of different theoretical models were combined. This implies that the observers do not adhere to only one strategy even during one experimental session. We can only guess the number of different strategies used during one session but at least three appear to be the norm in most cases.
The observed individual differences are particularly interesting in the light of a recent report showing that the ability to discriminate numbers of elements in two sets was correlated with a psychometrically measured intelligence . It is an intriguing possibility that the ability to keep track of elements which have already been counted (together with the sample size one is able to base his/her decisions upon), forms a precondition for numerical intelligence which, in turn, among other faculties, gives rise to general intellectual abilities.
We are greatful to Ehtibar Dzhafarov for major improvements to our work and Mario Fific and two anonymous reviewers for commenting on an earlier draft of the manuscript. We thank Kristin Kurjama for help in collecting data. We also thank all our subjects.
Conceived and designed the experiments: AR JA. Performed the experiments: AP. Analyzed the data: AR JA AP. Contributed reagents/materials/analysis tools: AR. Wrote the paper: JA AR AP.
- 1. Townsend JT, Fific M, Neufeld RWJ (2007) Assessment of mental architecture in clinical/cognitive research. In: Treat TA, Bootzin RR, Baker TB, editors. Psychological clinical science: Papers in Honor of Richard M. McFall. Mahwah, NJ: Lawrence Erlbaum Associates. pp. 223–258.JT TownsendM. FificRWJ Neufeld2007Assessment of mental architecture in clinical/cognitive research.TA TreatRR BootzinTB BakerPsychological clinical science: Papers in Honor of Richard M. McFallMahwah, NJLawrence Erlbaum Associates223258
- 2. Townsend JT (1990) Serial vs parallel processing: Sometimes they look like Ttweedledum and Tweedledee but they can (and should) be distinguished. Psychological Science 1: 46–54.JT Townsend1990Serial vs parallel processing: Sometimes they look like Ttweedledum and Tweedledee but they can (and should) be distinguished.Psychological Science14654
- 3. Townsend JT, Wenger MJ (2004) The serial-parallel dilemma: A case study in a linkage of theory and method. Psychonomic Bulletin & Review 11: 391–418.JT TownsendMJ Wenger2004The serial-parallel dilemma: A case study in a linkage of theory and method.Psychonomic Bulletin & Review11391418
- 4. Sternberg S (1966) High-speed scanning in human memory. Science 153: 652–654.S. Sternberg1966High-speed scanning in human memory.Science153652654
- 5. Dzhafarov EN, Schweickert R (1995) Decompositions of response-times: An almost general-theory. Journal of Mathematical Psychology 39: 285–314.EN DzhafarovR. Schweickert1995Decompositions of response-times: An almost general-theory.Journal of Mathematical Psychology39285314
- 6. Dehaene S, Cohen L (1994) Dissociable mechanisms of subitizing and counting: neuropsychological evidence from simultanagnosic patients. Journal of experimental Psychology: Human Perception and Performance 20: 958–975.S. DehaeneL. Cohen1994Dissociable mechanisms of subitizing and counting: neuropsychological evidence from simultanagnosic patients.Journal of experimental Psychology: Human Perception and Performance20958975
- 7. Feigenson L (2008) Parallel non-verbal enumeration is constrained by a set-based limit. Cognition 107: 1–18.L. Feigenson2008Parallel non-verbal enumeration is constrained by a set-based limit.Cognition107118
- 8. Trick LM, Enns JT, Brodeur DA (1996) Life Span Changes in Visual Enumeration: The Number Discrimination Task? Developmental Psychology 32: 925–932.LM TrickJT EnnsDA Brodeur1996Life Span Changes in Visual Enumeration: The Number Discrimination Task?Developmental Psychology32925932
- 9. Gelman R, Gallistel CR (1978) The child's understanding of number. Cambridge, MA: Harvard University Press. R. GelmanCR Gallistel1978The child's understanding of numberCambridge, MAHarvard University Press
- 10. Rose A (1948) The sensitivity performance of the human eye on an absolute scale. Journal of the Optical Society of America 38: 196–208.A. Rose1948The sensitivity performance of the human eye on an absolute scale.Journal of the Optical Society of America38196208
- 11. Allik J, Tuulmets T (1991) Occupancy model of perceived numerosity. Perception & Psychophysics 49: 303–314.J. AllikT. Tuulmets1991Occupancy model of perceived numerosity.Perception & Psychophysics49303314
- 12. Tokita M, Ishiguchi A (2009) Effects of feature types on proportion discrimination. Japanese Psychological Research 51: 57–68.M. TokitaA. Ishiguchi2009Effects of feature types on proportion discrimination.Japanese Psychological Research515768
- 13. Honig WK, Matheson WR (1995) Discrimination of relative numerosity and stimulus mixture by pigeons with comparable tasks. Journal of Experimental Psychology-Animal Behavior Processes 21: 348–362.WK HonigWR Matheson1995Discrimination of relative numerosity and stimulus mixture by pigeons with comparable tasks.Journal of Experimental Psychology-Animal Behavior Processes21348362
- 14. Emmerton J, Renner JC (2006) Scalar effects in the visual discrimination of numerosity by pigeons. Learning & Behavior 34: 176–192.J. EmmertonJC Renner2006Scalar effects in the visual discrimination of numerosity by pigeons.Learning & Behavior34176192
- 15. Townsend JT, Fific M (2004) Parallel versus serial processing and individual differences in high-speed search in human memory. Perception & Psychophysics 66: 953–962.JT TownsendM. Fific2004Parallel versus serial processing and individual differences in high-speed search in human memory.Perception & Psychophysics66953962
- 16. Townsend JT (1984) Uncovering mental processes with factorial experiments. Journal of Mathematical Psychology 28: 363–400.JT Townsend1984Uncovering mental processes with factorial experiments.Journal of Mathematical Psychology28363400
- 17. Dzhafarov EN (2003) Selective influence through conditional independence. Psychometrika 68: 7–26.EN Dzhafarov2003Selective influence through conditional independence.Psychometrika68726
- 18. Dzhafarov EN (1997) Process representations and decompositions of response times. In: Marley AAJ, editor. Choice, Decision, and Measurement: Essays in Honor of R. Duncan Luce. Nahwah, NJ: Lawrence Erlbaum Associates. pp. 255–277.EN Dzhafarov1997Process representations and decompositions of response times.AAJ MarleyChoice, Decision, and Measurement: Essays in Honor of R. Duncan LuceNahwah, NJLawrence Erlbaum Associates255277
- 19. Halberda J, Mazzocco MMM, Feigenson L (2008) Individual differences in non-verbal number acuity correlate with maths achievement. Nature 455: 665-U662.J. HalberdaMMM MazzoccoL. Feigenson2008Individual differences in non-verbal number acuity correlate with maths achievement.Nature455665-U662