Everyone has their own unique version of the visual world and there has been growing interest in understanding the way that personality shapes one’s perception. Here, we investigated meaningful visual experiences in relation to the personality dimension of schizotypy. In a novel approach to this issue, a non-clinical sample of subjects (total n = 197) were presented with calibrated images of scenes, cartoons and faces of varying visibility embedded in noise; the spatial properties of the images were constructed to mimic the natural statistics of the environment. In two experiments, subjects were required to indicate what they saw in a large number of unique images, both with and without actual meaningful structure. The first experiment employed an open-ended response paradigm and used a variety of different images in noise; the second experiment only presented a series of faces embedded in noise, and required a forced-choice response from the subjects. The results in all conditions indicated that a high positive schizotypy score was associated with an increased tendency to perceive complex meaning in images comprised purely of random visual noise. Individuals high in positive schizotypy seemed to be employing a looser criterion (response bias) to determine what constituted a ‘meaningful’ image, while also being significantly less sensitive at the task than those low in positive schizotypy. Our results suggest that differences in perceptual performance for individuals high in positive schizotypy are not related to increased suggestibility or susceptibility to instruction, as had previously been suggested. Instead, the observed reductions in sensitivity along with increased response bias toward seeing something that is not there, indirectly implicated subtle neurophysiological differences associated with the personality dimension of schizotypy, that are theoretically pertinent to the continuum of schizophrenia and hallucination-proneness.
Citation: Partos TR, Cropper SJ, Rawlings D (2016) You Don’t See What I See: Individual Differences in the Perception of Meaning from Visual Stimuli. PLoS ONE 11(3): e0150615. https://doi.org/10.1371/journal.pone.0150615
Editor: Michael H. Herzog, Ecole Polytechnique Federale de Lausanne, SWITZERLAND
Received: January 10, 2015; Accepted: February 17, 2016; Published: March 8, 2016
Copyright: © 2016 Partos 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.
Data Availability: All relevant data are within the paper and its Supporting Information files.
Funding: The authors received no specific funding for this work.
Competing interests: The authors have declared that no competing interests exist.
Like all human abilities and traits, there are individual differences in visual perception. Anecdotally, these can lead to seeing different things in a cloud-filled sky and appreciating particular forms of abstract art . Experimentally, these variations range from slight, and perhaps random, fluctuations in performance across individuals [2–5], to considerable dissimilarities that can be reliably traced to broader group differences in, for example, gender , personality , culture , motivation , and the spectrum of psychosis [10, 11]. In the work described here we use the commonplace observation of meaningful images in the clouds to construct stimuli that allow us to measure individual differences in the inclination to see something in a degraded, noisy stimulus when nothing is actually there.
Individual differences in perception
The visual system is predisposed to extract meaning, often from stimuli containing substantial amounts of uncertainty; indeed one could argue that is its primary role. The meaning that is imposed can depend on our internal templates of prototypical stimuli [12, 13] our expectations and learned probabilities about the visual environment [9, 14–20], contextual cues or prior visual input [21, 22] and on random neural fluctuations in functionally relevant areas of cortex [23–26]. Each of these processes are also subject to influence by other factors such as the personality (or factors which influence personality) of the individual.
For instance, when subjects were presented with a sequence of line-drawings, starting with an extremely degraded image that gradually became less degraded as the sequence progressed, and asked to respond once they could identify the image, those who responded earlier in the sequence, although less accurately, were those with stronger beliefs in paranormal phenomena . Stronger belief in the paranormal is also associated with a greater bias toward seeing an illusory face during a signal-detection task that used real-world photographs, some of which contained “artifact faces” , the tendency to attribute intention and animacy to sequences of random motion , and to ascribe meaning to random sequences of everyday events . Paranormal ‘believers’ also show a greater likelihood to see a face in a jumbled non-face, and a word in a non-word compared to ‘skeptics’ . Overall, the results imply an influence of the internal state of the system (in this case a particular belief system) on the outcome of the process of construction of meaning, with a role for both of expectations [9, 14–20] and prototypical templates [12, 13].
Schizotypy and perception
From a more generalised perspective, psychometric scales of personality have long been thought to influence aspects of perception which, in turn, influences behaviour . Belief in extra-sensory perception and paranormal phenomena, and high scores on measures of psychoticism and magical thinking can be contextualised in terms of the personality dimension of schizotypy [31, 33]. The concept of schizotypy has often been employed within a dimensional approach to psychosis, whereby psychopathological symptoms are thought to form a quantitative continuum with normal, healthy traits [34–36]. The presence of schizotypal traits, even at relatively high levels, does not imply impaired functioning , but may be indicative of risk for psychosis-spectrum disorders [38, 39]. The normal personality traits comprising schizotypy typically cluster mainly into three subtypes: positive-psychotic, positive-disorganized, and negative, with a fourth subtype becoming increasingly, although not universally, recognized impulsive/ antisocial [40, 41]. Of particular interest for the present research is what has been termed the positive-psychotic subtype, which encompasses distorted or intense subjective sensory experiences and minor manifestations of delusional beliefs. This dimension also correlates well to various measures of creativity, contributing to the concept of the ‘healthy schizotype’ with which we concur [42–44], and we stress that in no way does any given schizotypy score imply a clinical diagnosis.
Experimentally, when observers were presented with a random array of white dots on a black background and (misleadingly) instructed that the dots sometimes show something meaningful, individuals who score higher on questionnaire measures of psychoticism, neuroticism, and hallucination-proneness are more likely to report perceiving meaningful images of a complex nature in the dots . Such complex false alarms on this Random Dots Task (RDT) have also been associated with belief in extra-sensory perception , magical thinking and positive schizotypy . Individuals high in positive schizotypy also see more words in a dynamic string of non-word strings than low-scoring individuals , mirroring the result from similar work with paranormal believers . This effect is strengthened when the frequency of real words is increased , and is mediated by expectation, even when that expectation is not met . These data are consistent with perceptual biases that predispose those high in positive-psychotic traits to have measurable false perceptions.
Hallucination as a visual false-alarm
From a stimulus-based perspective, the strengths of visual illusions are mediated by various aspects of individual difference and clinical diagnosis [49–51], and there is evidence that both illusions and false-perceptions (or hallucinations) arise, at least in part, from the same mechanisms as ‘veridical’ perception. For instance, changes in local cortical blood flow are similar when an individual is looking at either illusory or ‘real’ contours , studies of the McCullough Effect  suggest the illusory colours inherent in the illusion are mediated through the same mechanism as the percept of the coloured adapting stimulus , and there is mounting evidence for common mechanisms mediating hallucinations and shared perception [55, 56].
The results outlined above suggest that illusions and hallucinations can be conceptualised as “visual false alarms”; an approach that fits within a probabilistic framework of vision and brain function [15, 17, 57], and is consistent with the tone of the argument characteristic of the literature. The overall aim of this work is to use the visual false alarm in this context to examine how personality interacts with perception.
The current study
From a task-driven perspective, while much previous work used artificial stimuli and subjective judgements open to suggestibility [58, 59], the two experiments presented here outline the development and use of a more ecologically valid and controlled visual stimulus in a signal-detection task paradigm, allowing us to more confidently attribute performance to perceptual differences between individuals (see also [28, 31, 48]).
From a stimulus-driven perspective, we suggest that it is common to see apparently meaningful images in clouds because of their particular spatial structure, where the power in a given spatial frequency-band has an approximately reciprocal relationship to frequency (1/ f, where f is the spatial frequency), and the fractal characteristic of self-similarity across scale . These structural visual properties stimulate the system relatively evenly across its range of sensitivity at early visual stages , and can be considered to create an overall increase in ‘noise’, or uncorrelated signal. Since it could be argued that the system’s primary role is to make sense of an input—whatever it may be—such overall stimulation can increase the likelihood of false correlations over space (and time); the perceptual consequence of this may be to see more than is present in the input.
Consideration of the statistical properties of natural scenes has been fruitful for understanding the way the visual system works [62–65]. The observation that natural scenes possess an approximately 1/f amplitude spectra and that the visual system may be particularly well adapted to this is used here to develop more ‘natural’ stimuli, to give greater ecological validity to the task [61, 66, 67]. To distinguish the task we refer to it as the Perception of Meaning task (or POM where the use of an acronym does not compromise readability).
Consistent with the literature reviewed above, we suggest that positive-psychotic personality traits (as measured by the Unusual Experiences sub-scale of the Schizotypy metric) mediate the occurrence of visual false alarms, and that using ecologically valid stimuli in an appropriately controlled psychophysical paradigm will enable this to be measured more effectively in a normal population. We expect that those individuals which score highly on Unusual Experiences will experience more visual false alarms and that our paradigm will allow us to discriminate between sensitivity and bias in the subjects, as well as removing any influence of suggestibility on the data.
Two experiments will be reported here, both examine the interaction between personality and perception. The first will pilot the Perception Of Meaning task and critically compare it to its closest predecessor, Jakes and Hemsley’s (1986) Random Dots Task outlined in the introduction. The second experiment will examine performance on a modified and improved signal-detection style version of the POM, and concurrently investigate the role of participants’ expectations of the stimuli on perception [12, 13, 16]. Common aspects of the methodology with be described in this section, with the complementary specifics at the head of each Experiment.
Experiment 1 comprised 102 undergraduate psychology students (68% females) who took part in exchange for course credit. Ages ranged from 16 to 44 years (M = 20.0 years, SD = 4.6). Experiment 2 comprised 95 undergraduate psychology students (72% females) ranging in age from 17 to 41 years (M = 19.8 years, SD = 4.3). None of the participants in Experiment 2 had taken part in Experiment 1. Both studies were approved by the Human Ethics Advisory Group at the University of Melbourne and each participant provided written consent for participation and publication of their (anonymous) data.
Participants in Experiment 1 completed the Oxford-Liverpool Inventory of Feelings and Experiences (O-LIFE) , which is a 108-item yes/ no measure of schizotypy with four subscales (Unusual Experiences ‘UnEx’ for positive-psychotic, Cognitive Disorganization ‘CogDis’ for positive-disorganized; Introvertive Anhedonia ‘IntAnh’ for negative; and Impulsive Nonconformity ‘ImpNon’ for the impulsive/ antisocial subtype of schizotypy). The Vividness of Visual Imagery Questionnaire (VVIQ) , and Gudjonsson’s Scale of Interrogative Suggestibility (GSIS)  were also administered as control measures. The VVIQ is a 16-item questionnaire that asks respondents to mentally conjure and rate the vividness of features in four visual scenes (the face of a friend, the rising sun, a familiar shop-front, and a country scene). During this portion of the procedure, subjects were free to close their eyes, or keep them open; most subjects closed their eyes (see note in Experiment 1, discussion). The GSIS is an interview-style measure where respondents are read a short vignette and are then asked 20 questions relating to the story, 15 of which are leading questions regarding information that was never provided. Regardless of their accuracy, respondents are firmly told they have made a number of errors and asked the same questions again, with instructions to try and be more accurate. Responses are scored on the basis of accurate Recall (20 items) and two aspects of suggestibility: Yield (15 items)–the number of leading questions initially responded to in the leading direction, and Shift (15 items)–the number of leading questions the respondent changed their answer to upon being asked the second time. A total GSIS suggestibility score can be calculated by summing the Yield and Shift scores.
In Experiment 2, participants completed only the UnEx, CogDis, and ImpNon subscales of the O-LIFE. IntAnh was omitted due to time constraints and because it was of least theoretical interest.
Psychophysical tasks and equipment
All image manipulation, coding, and presentation of experiments was carried out using the Matlab computer language  and the Psychophysics Toolbox . All images were 8-bit monochrome greyscale, containing up to 256 shades of grey, ranging from black to white. The images were composed of a square matrix of pixels (1024 × 1024 (16 deg square) for Experiment 1, and 512 × 512 (8 deg square) for Experiment 2). The effective pixel size (spatial resolution) was the same for each experiment and a property of the generation hardware, but the overall image size was restricted by the database used in each case (Experiment 1 , Experiment 2 ). Stimuli were presented on a 23-inch (1920 × 1200 pixel resolution at 60 Hz, with a mean luminance of 40 cd/m2) Apple Cinema Display monitor, powered by a G4 Apple PowerBook. The voltage to luminance relationship of the display was approximately linear over the range used through the Apple standard gamma correction; this correction was considered adequate given the nature of the stimuli and task of the observer. Later work presenting the images on a fully calibrated CRT display has yielded similar data [43, 75, 76]. Presentation took place in a darkened room with participants seated at a distance of 964 mm from the screen supported with a chin-rest, such that one degree of visual angle corresponded to 64 screen pixels. Experimental sessions were conducted one-to-one and lasted approximately 90 minutes.
Monochrome pictures were combined with artificially generated two-dimensional noise to create visually degraded images. Experiment 1 combined the image and noise through the standard practice of addition of a given proportion of noise to an ‘image’ value within each pixel [23, 77]. Experiment 2, however, in an important variation from Experiment 1, spatially degraded the image on an alternate pixel by pixel basis. This novel spatial degradation process meant that pre-specified proportions of image pixels were randomly designated as either signal or noise. Thus, what was degraded was the degree to which the individual signal pixels correlate across space to generate a meaningful representation (Experiment 2), rather than the degree to which a single pixel in space is able to represent the signal (Experiment 1). The extent to which the visual system can discriminate between individual pixels and the precise signal to noise pixel structure will influence the effective difference between these two processes. This second method of image degradation has similarities to the phase-alignment method used recently by Hansen and colleagues 
To create each stimulus pair, a normalised 8-bit monochrome (meaningful) signal image was randomly positioned within a pixel grid of random 2D noise of similar dimensions and mean luminance and with an amplitude spectra of 1/f (where f is the spatial frequency) to create pink-noise (as opposed to a a flat amplitude spectrum across spatial frequency, termed white-noise). A companion noise-only image was also created with the same mean and range of pixel values and the same RMS contrast. These were then combined to create a composite image where the noise was added to the signal pixel values and then normalised (Experiment 1), or a percentage of pixels were from the signal image and the remainder from the noise image (Experiment 2), again with the same RMS contrast to remove contrast as cue to the presence of an image. A further noise-only image was also paired with each signal image as its non-signal counterpart. The image pairs were then band-pass filtered (using a Fast Fourier Transform and Gaussian filter in Matlab) in the spatial frequency domain to contain different octave bands of spatial frequencies, centred at (0.5), 1, 2, 4, 8, or (16) c/deg at the specified viewing distance (frequencies in parentheses used in Experiment 1 only). This process is summarised in Fig 1a and 1b and experiment-specific details given below.
Flow diagram representing the creation of the stimuli for the POM task used in Experiment 1 (1a) and Experiment 2 (1b). FC = central frequency.
Approach to the data and analysis
In this work we are interested in how different aspects of personality affect performance on the psychophysical tasks. As outlined in the introduction we have the most theoretical interest in the positive dimension (UnEx and CogDis in the O-LIFE), although we did examine all dimensions at the outset, and where possible we examined and included all dimensions of the O-LIFE, despite being aware of differing views as to the relevance of all four [40, 41]. We also analyse and present the data in a way consistent with our theoretical approach to the study; that personality is related to psychophysical performance in our particular task.
Furthermore, we analyse the data both from a continuous and dichotomous perspective to facilitate comparison with previous work [16, 45]. In order to designate respondents as low or high on a given schizotypal dimension a median-split was computed on the scores in order to compare our results to previous work. We are mindful of the potential issues of conducting a median split on continuous data e.g. [79–82], and perform regression analyses to ensure we do not rely on a single method of data treatment, while maintaining some consistency with previous work. We examined the data in all regression analyses for multi-collinearity and in no instance was the variance inflation factor (VIF) greater than 2 or the tolerance less than 0.6, indicating that multi-collinearity was not an issue. We have chosen to report both the continuous and dichotomous results in most cases. Missing data was accounted for on an analysis-by-analysis basis, which accounts for minor variations in subject number (n) in some analyses. Finally, we provide the Bayesian statistical analysis of the critical data as Supporting Information (S1 Appendix).
The two visual stimulus sets used in Experiment 1 were an adaptation of the Random Dots Task or RDT , and the newly developed Perception Of Meaning (POM) task. Similar instructions were given for completing both tasks, with participants told that they would be seeing a number of images, some of which contained something meaningful, and to describe out loud what they saw if and when they saw something meaningful or recognisable. Each image appeared on screen for 6 seconds before automatically changing to the next, for a total presentation time of approximately 18 minutes (180 stimuli in total). The order of images was randomised so each subject saw them in a different sequence. The experimenter sat about 2 metres behind the participant and recorded their responses verbatim, while remaining as unobtrusive as possible. The order of completion of the questionnaires (O-LIFE, VVIQ, and GSIS) and visual tasks (RDT and POM) was counterbalanced using a Latin square design, and order had no significant effects on the outcomes of interest.
Image generation specifics.
Eight photographs of natural scenes (e.g. forests, clouds) taken from the van Hateren image database  and seven cartoon style line drawings (mostly of anthropomorphised animals) taken from an online database  formed the basis for the signal stimuli. Paired with the noise stimuli and band-pass filtered to 6 different spatial frequency brackets, the final stimulus set therefore comprised 90 signal and 90 noise stimuli (see Fig 1a), which were randomly intermixed prior to presentation such that no two participants viewed them in the same order. They were presented in a single block of 180 images. Stimuli for the RDT were created by generating 60 random arrays of 400 dots filling a space the same size as the images of the POM. From the viewing distance used, each image subtended 16° × 16° of visual angle on the retina, and was presented for 6 seconds in a rectangular temporal envelope.
Signal detection theory specifics.
Detailed responses to the RDT (e.g. scenes, faces, or figures) were classified complex false alarms, whereas basic responses (e.g. simple geometric shapes, letters, or numerals) were classified simple false alarms, according to Jakes and Hemsley’s (1986) criteria. These criteria were also used to classify false alarm responses to the POM. In addition, misinterpreted responses to the POM signal stimuli that were incorrect and greatly removed from their actual content (e.g. “a dragon fighting a dinosaur” in response to an image of leaves on the ground) were also classified as false alarms using these criteria.
There were no images embedded in the RDT, so no hits or misses per se could be recorded although, arguably, a null response could be classified as a hit or a miss in this case. The hit rate for the POM in Experiment 1 was calculated as the total number of hits divided by the total number of signal stimuli, whereas the false alarm rate was the total number of false alarms divided by the total number of stimuli (hits + noise) to allow for the inclusion of these misinterpretations of the signal stimuli. This methodology differs from traditional signal detection methods where false alarm rates are calculated as the total number of false alarms divided by the total number of noise stimuli only. As such, the conventional rules of signal detection theory where the hit rate is equal to 1 minus the miss rate, and the false alarm rate is equal to 1 minus the correct rejection rate do not strictly apply to this data, although the relationships are a fairly close approximation.
Results and Interim Discussion
Scores on the questionnaire measures are summarised in Table 1, and are all comparable to reported norms for these psychometrics [69, 70, 84, 85]. Scores on the IntAnh subscale of the O-LIFE were positively skewed and so square root transformations were computed to correct for this, and the transformed scores were used in all parametric analyses.
The mean complex false alarm rates in response to the RDT (M = 11.4%, SD = 13.7) and the POM (M = 9.0%, SD = 8.5) were comparable, t(101) = .034, p > .05, and highly correlated r = .624, p < .01. The mean hit rate for the POM was 53.3% (SD = 11.0). Square root transformations were required to correct for positive skew for the complex and simple false alarm rates on both the RDT and the POM. A qualitative analysis of complex false alarm responses to the POM showed that 36% contained human faces or facial features, 25% animals or mythical creatures, 20% humanoid figures, 15% natural objects or scenes, and 4% other. It should be noted that all images in the RDT tasks were noise only, so there were no ‘hits’ or ‘misses’ per se, just images in which the subjects saw something or did not.
The correlations between the personality measures and performance on the two visual tasks are presented in Table 2, which indicates that positive-psychotic schizotypy (as measured by UnEx scores) was the only measure to be consistently associated with performance. This was reflected in the Bayesian correlation (see S1 Appendix) with a moderately high Bayes factor of 20.9, supporting the correlation between the UnEx score and the complex false alarms in the Perception of Meaning task.
The effect of personality on visual false alarms
Four blockwise hierarchical linear regression analyses, predicting the complex and simple false alarm rates on the RDT and the POM, were conducted. UnEx scores were entered in the first step, and the remaining schizotypy measures, suggestibility scores, and visual imagery scores were entered blockwise in the second step. This established whether these measures contributed to predicting false alarm rates once the effects of positive-psychotic schizotypy had been accounted for. Table 3 (left shaded columns) shows that UnEx scores accounted for 5% of the variance in complex responses and 4% of the variance in simple responses on the RDT. For complex responses, the remaining personality variables made a significant contribution in the second step, accounting for a further 19% of the variance. In the final model higher UnEx and GSIS shift scores increased, whereas higher CogDis scores decreased the rate of complex responses. None of the other personality measures made a significant contribution to predicting simple response rates on the RDT once the effects of UnEx had been accounted for. UnEx scores also made a significant contribution to predicting false alarm rates on the POM, accounting for 10% of the variance in complex false alarm rates and 5% of the variance in simple false alarm rates (see Table 3, rightmost columns). The addition of the remaining personality variables did not result in a statistically significant increase to the variance already accounted for by UnEx, either for complex or simple false alarm rates on the POM. It should be noted, however, that CogDis scores did make a significant contribution to predicting complex false alarm rates in the second step of the regression, with POM false alarm rates decreasing as CogDis scores increased. This is an unexpected result, but may possibly be related to social anxiety and neuroticism, which is reflected in an increasing CogDis score ; if this increase in anxiety causes the subjects to moderate they complex FA responses, for fear of seeming odd. We thank one of our reviewers (O.F.) for this tentative but interesting suggestion.
Overall, our measure of positive-psychotic schizotypy, the UnEx score, had the strongest association with participants’ tendency to perceive complex meaning in the random stimuli of both the RDT and the new POM. Visual imagery ability, as measured by the VVIQ, was not associated with performance, so it is less likely that false alarms resulted from an effortful attempt to ‘make out’ meaningful images in the noise, and plausible that they arose spontaneously in a manner analogous to visual hallucinations, especially given that their occurrence was linked to an aspect of personality suggested to lie on a continuum with the positive symptoms of psychosis. However, we note that one potential limitation of Experiment 1 was that we did not control whether participants completed the imagery task with open or closed eyes. It is possible that those completing it with closed eyes may have obtained higher VVIQ scores, which may have contaminated the effects of any association between imagery and schizotypy scores, or scores on the POM.
On the RDT, however, suggestibility also played a role, with those participants who were more likely to alter their responses due to experimenter instruction (indexed by the GSIS Shift scores) also more likely to report false alarms. Suggestibility did not impact performance on the POM. This coupled with the absence of any misleading experimenter instructions, as well as the more sophisticated and naturalistic characteristics of the noise stimuli, indicate the POM to be a promising tool for measuring hallucination proneness in laboratory settings with good discriminant and construct validity.
For consistency with previous work, and clarity of presentation, a 2 × 4 ANOVA was conducted using the median split of UnEx scores across the 4 indicators of hallucination proneness (the simple and complex false alarm rates on the RDT and the POM). The high UnEx group made significantly more false alarms than the low scorers. Details are presented in the Supporting Information (S1 Appendix) but the result is summarised in Fig 2. Ultimately this is the same result as the regression above, and based on the same hierarchical linear model, but presented in a more digestible format.
Response rates for simple and complex responses (false alarms) on the Random Dots Task (RDT) and the Perception Of Meaning task (POM), shown separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 102, error bars represent ±95% confidence intervals).
The effect of spatial frequency-band on visual false alarms
The final analysis was concerned with investigating the effect of positive-psychotic schizotypy on the complex false alarm rates on the POM across the different spatial frequency bands. A 2 (median split of UnEx) × 6 (spatial frequency brackets) ANOVA was conducted to address this question and the results are presented in Fig 3. A violation of the assumption of sphericity was indicated by Mauchly’s test, χ2(14) = 91.9, so Greenhouse-Geisser adjustments (ε = .688) were made to the degrees of freedom. A significant main effect of spatial frequency was observed, F(5, 500) = 70.3, p < .001, ηp2 = .413, reflecting the fact that complex false alarms were more prevalent at the lower spatial frequencies. The interaction between UnEx and spatial frequency was also significant, F(5, 500) = 4.3, p < 005, ηp2 = .041. Post-hoc comparisons revealed the differences between the low and high UnEx groups to be significant at 0.5 c/deg and 1 c/deg (p < .001) and also at 2 c/deg and 16 c/deg (p < .05). The presence of the U-shaped curve was corroborated by a statistically significant quadratic trend in complex false alarm rates with increasing spatial frequency, F(1, 100) = 37.2, p < .001, ηp2 = .271.
Response rates for complex false alarms on the Perception Of Meaning task (POM) across the 6 spatial frequency bands, shown separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 102, error bars represent ±95% confidence intervals).
Lower frequency bands elicited more false alarms than higher ones, an effect that was exaggerated for individuals high on UnEx. There is some evidence that low spatial frequencies are processed more rapidly than higher ones , although this will likely depend upon the precise task at hand. In addition, according to some theories (e.g. ), hallucinators take less time to form perceptual judgements, a similar effect having been observed in non-clinical populations where belief in the paranormal was associated with responding earlier (when less information was available) and making incorrect identifications of image-series decreasing sequentially in their level of degradation . We speculate that this earlier response might therefore be exaggerated with low spatial frequency information.
Overall, the results of Experiment 1 showed that the noise-based (POM) stimuli amplified the effect originally seen for the dot (RDT) stimuli ; whereby a high UnEx O-LIFE score was correlated to the likelihood of seeing a meaningful image when there was nothing present. This validates our contention that a more ecologically valid stimulus increases individual differences in the imposition of meaning. The second experiment extends this result to examine the same effect in a signal detection framework. We also vary the spatial frequency content of the image (as in Experiment 1) and the observer’s expectation that there will be a meaningful image present .
All participants completed the UnEx, CogDis, and ImpNon subscales of the O-LIFE prior to the POM, so they could be pseudo-randomly allocated into one of three experimental conditions, ensuring an even distribution of UnEx scores within each group. In order to manipulate subjects’ expectations, prior to commencing the POM, participants were told to expect 25% (Group 1), 50% (Group 2: the control condition), or 75% (Group 3) of the stimuli in the POM to contain a face; in reality, 50% of stimuli contained a face for all three groups. Responses were made on the computer keyboard, where participants were instructed to press the ‘L’ key if they detected a face and the ‘A’ key if they did not (these keys were reversed for half the participants). The importance of accuracy and speed were both emphasised, and reaction times were recorded. It should be noted that responses were made on a laptop with an integrated keyboard so the losses in reaction time accuracy associated with a peripheral USB keyboard were avoided. The reaction times were also in accord with those of another study, measured using separate and calibrated button boxes (RTBox and a Cedrus box) [43, 76].
The practice block of the POM was administered first, during which accurate audible feedback was provided. Each stimulus trial commenced with a blank screen prompting participants to press the spacebar, a fixation cross on a black screen of mean luminance then appeared for 1000 ms. An audible beep signalled the onset of the stimulus, which was presented for exactly 1000 ms (rectangular temporal envelope), followed by another blank screen. The stimulus remained on screen for exactly 1000 ms, regardless of when the participant made their response; this is represented in Fig 4. The stimuli were presented for a shorter duration than Experiment 1, and were also only 8 deg square. Participants were able to respond at any time during the 3000 ms interval following the onset of the stimulus. Responses made after this time were not recorded. Only the practice block gave feedback as to the observers response, and the subjects were not informed how many faces to expect until after the practice block. In the test trials there was no feedback and signal stimuli were present 50% of the time in all conditions, despite the three expectation groups.
Image generation specifics.
The POM task used in Experiment 2 was modified to allow for signal detection analysis so performance could be separated into factors relating to sensitivity (Dˈ) and response criterion (β) [88, 89]. This required that participants respond in a uniform manner to all signal stimuli, rather than describing what they saw, so the content of the signal stimuli had to be homogeneous. Faces were chosen for this purpose, partly because they were the most predominant spontaneous response to the open-ended POM used in Experiment 1. Twenty frontal photographs of human faces (10 male and 10 female) with neutral expressions, ranging in age from 19 to 37 years, taken from the database of the Productive Ageing Laboratory  formed the basis of the signal stimulus set. Each face was manually cropped to contain only the facial features without the hair or neck, and then pseudo-randomly positioned within a square background of 1/f noise, such that it was not necessarily in a central or uniform location. A typical face subtended 3.2° × 4° of visual angle within an 8° × 8° background. As described above, in a departure from the standard procedure adopted in Experiment 1, signal stimuli were degraded by pixel replacement rather than addition, with the percentage of signal pixels replaced by noise being 70, 75, or 77%. This range of stimulus image degradation was chosen to cover an approximate range close to threshold (image just visible for prolonged exposure through pilot observation). This varied for each specific image and each observer, but given the group design was a necessary step to allow presentation of a greater number of noise/image combinations which, in turn, we felt would facilitate the false-alarm response. Given the number of hits measured we were reassured this restricted range was adequate.
Images were degraded through the pixel replacement procedure prior to band-pass filtering, and only 4 spatial-frequency bands were used (centred at 1, 2, 4, or 8 c/deg) for Experiment 2. The final stimulus set thus comprised 240 signal and 240 noise stimuli, each one unique (see Fig 1b). To minimise participant fatigue, these were presented in 4 blocks, each comprising 120 stimuli with an even distribution of noise and spatial frequency bands. A practice block of a unique set of 96 stimuli (based on 8 new faces) was also created.
Results and Interim Discussion
Brief demographics and schizotypy scores for the three experimental expectation groups are summarised in Table 4. No significant group differences were observed on any of these measures. Considering all three groups together, the mean false alarm rate for the signal detection version of the POM used in Experiment 2 was 23.1% (SD = 15.4%), whereas the hit rate was 62.6% (SD = 9.7%), both somewhat higher than the rates for the open-ended version of the POM used in Experiment 1. The mean sensitivity (Dˈ) score was 1.2 (SD = 0.5) and ranged between 0.4 and 2.2, indicating that all participants were able to distinguish the faces from the noise stimuli with some degree of accuracy. The mean response criterion (β) score was 2.0 (SD = 1.8) and ranged between 0.6 and 10.8. A score of β = 1 represents no response bias for an ideal observer. In our sample, 29.5% of participants obtained a β score below 1, indicating a bias toward responding as having seen a face, with the remainder scoring above 1, indicative of a bias toward responding as not having seen a face. False alarm rates and response criterion scores were both positively skewed, so square-root and inverse transformations (FASQ = √(FA); βINV = 1 –[1 / (β + 1)]), were respectively applied prior to any parametric analyses.
The mean reaction time (RT) was 778 ms (SD = 141 ms) for hits and M = 911 ms (SD = 244 ms) for false alarms. We computed a difference score for each individual by subtracting their RT for hits from their RT for false alarms, such that a positive value would indicate faster RTs for hits than false alarms. The mean difference score was 133 ms (SD = 166 ms), a value significantly greater than 0, t(94) = 7.8, p < .0001, indicating that a speed-accuracy trade-off was unlikely to be occurring during the POM, as correct responses (hits) were faster than incorrect ones. RT difference scores did not differ by UnEx scores, t(94) = 0.11, p > .05. We also conducted t-tests to compare the mean reaction times for hits and false alarms, and at the four different spatial frequencies for participants below and above the median on UnEx. While the high UnEx group did tend to respond faster, none of the differences were statistically significant (all p > .05). These data are plotted in Fig 5.
Results are shown separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 94, error bars represent 1 SEM). Panel a plots the average reactions times to respond to all trails for the two subject groups at each spatial frequency band. Panel b plots the time to respond with a False Alarm (FA) and a Hit, and the average difference between the two for each subject (Difference) collapsed across spatial frequency.
The effect of personality on POM performance
To assess the effects of schizotypy and expectations on POM performance, four blockwise hierarchical linear regression analyses were conducted. Results are shown in Table 5. Only UnEx scores were entered in the first block, to observe the unadjusted effects of positive-psychotic schizotypy. Higher UnEx scores were associated with significantly more false alarms, lower sensitivity, and lower response criterion, but no difference in hit rates. These effects, collapsed across the 3 expectation conditions, are shown graphically in Fig 6, where POM performance is shown separately for those scoring below and above the median on UnEx.
Data shown separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 94, error bars represent ±95% confidence intervals). The reference line at 0.5 in panel a represents chance performance in the yes-no task, whereas the reference line at β = 1.0 in panel c represents the point of no response bias for an unbiased responder. A β value less than 1 indicates a bias toward saying a face was present in a noise-only stimulus.
In the second block of the regression, entering the remaining two schizotypy measures (CogDis and ImpNon in this experiment) into the regression equation did not make any significant contribution to the predictive power of the unadjusted model when only UnEx was included (p for all ΔR2 > .05). Notably however, the addition of CogDis and ImpNon reduced the unique influence of UnEx on sensitivity (D’) scores to be statistically insignificant. This effect was largely due to the shared variance between CogDis and UnEx, with both variables in isolation being significantly associated with a reduction in sensitivity on the POM (B = -0.02, SE B = 0.008, β = -.30, R2 = .09, p < .005, for the unadjusted regression model for CogDis predicting Dˈ (as opposed to UnEx as shown in Table 5)), but neither making a significant contribution when considered together. Indeed, the correlation between UnEx and CogDis for the sample in Experiment 2 was r = .478, p < .001, indicating around 23% shared variance. However, the tolerance (UnEx = .659, CogDis = .714) and Variance Inflation Factor (UnEx = 1.518, CogDis = 1.400) diagnostics indicated that multicollinearity was not an issue and correlations of this magnitude between the UnEx and CogDis scales are consistent with published norms .
In the third and final block, dummy variables for the 25% and 75% expectation conditions were entered into the regression equation, with the 50% condition used as the reference category. Expectations strongly predicted all four performance measures on the POM, over and above participants’ schizotypy scores (p for all ΔR2 < .0005), with the higher expectation condition having relatively greater influence (see Table 5). Compared to the 50% control condition, expecting fewer signal stimuli on the POM significantly increased sensitivity and response criterion scores, but did not significantly impact hit or false alarm rates. In contrast, expecting more signal stimuli than were presented significantly increased hit and false alarm rates, but lowered sensitivity and response criterion scores. Importantly, the association between positive-psychotic schizotypy (UnEx) and performance on the POM remained significant even after the effect of expectations had been accounted for. In the final model, a one standard deviation increase in UnEx scores resulted in a .28 standard deviation increase in false alarm rates, a .24 standard deviation decrease in sensitivity scores, and a .27 standard deviation decrease in response criterion scores.
We also explored the interaction effects between schizotypy and the three expectation conditions (2x3 mixed ANOVA), using dichotomous versions of each schizotypy variable based on median splits. We did this particularly to enable a comparison between our findings and the study of Cella et al., (2007). Unlike Cella et al. (2007), however, we did not find any significant interaction effects for any of the schizotypy variables. In fact, whereas Cella et al., (2007) found that the high UnEx group was especially likely to make more false alarms in the low expectation condition, our results indicated a non-significant trend in the opposite direction, with the high UnEx group more likely to make false alarms in the high expectation condition. Despite the non-significant interactions, data from the analysis are plotted in Fig 7 (collapsed across spatial frequency brackets). What the data do confirm are the reduced sensitivity and bias toward seeing a face (a lower β value) in the higher positive-psychotic (UnEx) group compared to the lower group.
Data plotted separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 94, error bars represent ±95% confidence intervals). The reference lines in panels a and b represent chance performance (yes-no task), whereas the reference line at β = 1 in panel d represents the point of no response bias for an unbiased responder. A β value less than 1 indicates a bias toward saying a face was present in a noise-only stimulus.
The effect of spatial frequency-band on POM performance
Finally, the role of spatial frequency on POM performance for individuals scoring below and above the median on positive-psychotic schizotypy (collapsed across the three expectation conditions) was examined. On the basis of Experiment 1, it was anticipated that schizotypy differences would be greatest at the lower spatial frequencies. Accordingly, the interaction between UnEx and spatial frequency was of primary interest, though the main effect of spatial frequency on POM hit rates, false alarm rates, sensitivity, and response criterion will be described first. The analyses comprised 2 (UnEx median split) × 4 (spatial frequency brackets) mixed ANOVAs, one for each POM performance measure, and are presented in Fig 8. In all cases, Mauchly’s test indicated violations of the assumption of sphericity, so Greenhouse-Geisser corrections (ε = .637, .625, .887, and .804, for hit rates, false alarm rates, Dˈ, and β, respectively) were applied.
Data plotted separately for individuals scoring below and above the median on the UnEx subscale of the O-LIFE (N = 94, error bars represent ±95% confidence intervals). The reference lines in panels a and b represent chance performance (yes-no task), whereas the reference line at β = 1 in panel d represents the point of no response bias for an unbiased responder. A β value less than 1 indicates a bias toward saying a face was present in a noise-only stimulus.
Hit rates decreased significantly with increasing spatial frequency, F(3, 276) = 1247.7, p < .001, η2P = .93, in a significant linear trend, F(1, 92) = 1884.7, p < .001, η2P = .95. Fig 8 indicates that hit rates for the highest spatial frequency bracket of 8 c/deg dropped below chance performance. Similarly, false alarm rates decreased, F(3, 276) = 223.5, p < .001, η2P = .71 in a significant linear trend, F(1, 92) = 328.4, p < .001, η2P = .78, although at no spatial frequency brackets were the mean false alarm rates greater than what would be expected by chance. Sensitivity scores also decreased significantly with increasing spatial frequency, F(3, 270) = 25.4, p < .001, η2P = .68, in a significant linear trend, F(1, 90) = 366.9, p < .001, η2P = .80. Lastly, response criterion scores increased with spatial frequency, F(3, 276) = 265.0, p < 001, η2P = .74, in a statistically significant linear trend, F(1, 92) = 493.4, p < .001, η2P = .84.
Contrary to the findings of Experiment 1, there were no significant positive-psychotic schizotypy × spatial frequency interactions on hit rates, F(2, 276) = .034, p > .05, false alarm rates, F(2, 276) = 1.1, p > .05, sensitivity, F(2, 270) = .046, p > .05, or response criterion scores, F(2, 276) = 0.19, p > .05.
To summarise, the results of Experiment 2 reflect that the increased likelihood of giving a false alarm in subjects with a high UnEx score (Exp 1) is related to a greater bias (β) toward seeing a face and a reduced sensitivity (Dˈ) to detecting a face when present and clarifies the initial result. Both spatial frequency and expectation influence the data but there were no significant interaction effects between schizotypy and these variables.
The work described in this paper examined the effect that personality has upon an individual’s perception of meaning in noisy images.
Vision, and the brain more generally, is a noisy system. The process of deciding that a given signal is meaningful at any point in time, or at any stage in the processing hierarchy, can be considered akin to a correlation in a statistical sense. Furthermore, there are both stimulus-based and task-based factors which interact to influence the degree to which any particular neural activity may be considered to be meaningful in the overall internal representation of the input.
Our work explores how the individual (as defined by the schizotypy personality scales) influences these processes in the context of identifying meaning in a spatially degraded stimulus. The results indicate that certain aspects of personality are related to a reduced sensitivity to a stimulus and to an increased likelihood of seeing something when it is not there. This reduced sensitivity is consistent with an increased internal noise level in some individuals, making it harder to see a near threshold stimulus . The increased rate of false alarms, seeing something when it’s not there, is consistent with increased internal noise if it is also the case that mistakes are made more often when there is more random activity , and those mistakes have a perceptual consequence. This result is congruent with a similar approach taken examining the perception of paranormal believers and skeptics when asked to identify meaning in different configure stimuli and environmental situations [28, 29, 31].
The two experiments presented here showed that strongest predictor of a complex false alarm (Experiment 1) was the UnEx dimension of schizotypy and that both sensitivity and bias correlate with the UnEx dimension only when analysed in terms of signal detection theory (Experiment 2). Put simply, this means that individuals high on this scale are less sensitive to the presence of a meaning in noise, and more inclined to see meaning when none is there.
Our experiments manipulated the spatial frequency content of the images between centre frequencies of 0.5cpd and 16cpd (2 - 8cpd in Experiment 2). When the stimuli were confined to faces embedded in noise (Experiment 2), the effect of spatial frequency was not personality-specific. In other words, making the task harder (shortening the duration) and more objective (requiring a forced-choice response) had the effect of reducing the influence of the individual on the task. Since the role of spatial frequency is probably most obvious relatively early in the visual process, and the factors affecting an individual’s personality will have greater influence on perception later in the process, this is perhaps not such a surprise.
Our manipulation of expectation of the number of images containing something meaningful was analogous to Cella et al’s (2007)  design using a word-detection task. Our results, however, were not entirely consistent with their findings. Both experiments found that raising expectations increased the number of false alarms irrespective of schizotypy scores, but had little effect on accuracy. In the same vein, Smith, Gosselin and Schyns (2012) found that when observers were expecting to see a face in a noisy image then they often did, even if one was never presented. Related to this result, the perceived rotation of an ambiguous stimulus depends upon expectation and, to some degree, belief about the stimulus properties . We did not, however, replicate Cella et al’s (2007) interaction effects between UnEx scores and expectation conditions, and actually observed a non-significant trend in the opposite direction; with the high UnEx group more likely to make false alarms when they were presented with fewer real images than they were expecting. That is, the production of false alarms in our study was congruent with the direction of expectations, whereas Cella and colleagues found that their high UnEx group was particularly more likely to make false alarms when they were presented with more real signal stimuli than they were expecting. The major distinction between the two studies is that our signal stimuli were faces, whereas Cella et al., (2007) used common words, so one explanation for the different findings may be the different neural mechanisms involved in the perception of images and words (e.g. ). While our POM simply involves detection of the signal stimulus (a face), the detection of a real word among non-words involves the added cognitive step of recognition, given that both the signal and noise stimuli are made up of identical letter components with the difference lying only in the order of their arrangement. Arguably, our task gives rise to perceptual false alarms which more closely resemble real-world visual hallucinations than the false alarms elicited during the word-detection task of Cella et al. (2007). Our findings are also more consistent with theoretical models of how expectations contribute to the emergence of hallucinations .
One of the motivating factors for our use of the O-LIFE personality dimensions is its relationship to hallucination and psychosis , and our stimuli were developed to use controlled external noise as a tool to look at the operation of a decision-making system that is inherently noisy in its operation . An effect of increased cortical ‘noise’ has been commented upon in the context of cortical oscillation in a working memory task and concurrent EEG recording both in high schizotypy individuals  and in schizophrenia . While we do not suggest that the task at hand here is directly related to the phase-locking of cortical oscillatory activity, the observation of increased noise can be considered to have more general effects outside that directly related to oscillatory activity. The same authors also commented that increased noise may be a product of dysfunctional top-down control on the activity which prevents a clear signal being shaped and being contextually modulated in an appropriate way for the task at hand . Both of these influences on the resultant percept are, we suggest, affected by the current and ongoing state of the individual as the task is carried out, and are therefore likely affected by personality.
Furthermore, it has been observed that cognitive control of intentional inhibition is reduced in schizophrenia and shows a positive correlation with the severity of auditory hallucination; more severe hallucinations appears related to reduced inhibition . If the dimensional relationship to schizotypy holds then we would expect to see the decrease in D' and increased bias measured in Experiment 2 as a function of reduced control or inhibition of the neural representation of the stimulus.
As mentioned above, it has been recently shown that individuals internal templates of expected stimuli, or overall motivation regarding those stimuli, will affect whether they see something when it is not there [13, 20, 97] or which of two bistable configurations are perceived ; thus an internal template can be thought of as being superimposed onto an activity ‘surface’ to influence what sense may be made of that activity. This is akin to a particular belief system (acting as a template) mediating the perception of meaning in meaninglessness [28, 29, 31]. Although our stimuli were different in terms of the noise structure and, importantly, the random location of the face within the image frame [13, 20, 97], the idea of internal expectation both in terms of frequency and particular spatial structure having an influence on the decision is consistent with the current data. Furthermore, as an image becomes more ambiguous, as in the case of a bistable representation of face/vase or the necker cube, there appears to be a progressively more activity in higher brain areas, measured using multivariate pattern analysis, outside those generally associated with perception . This activity outside visual cortex is also correlated to the degree of delusional belief in the particular stimulus properties which in turn affect the percept of an otherwise ambiguous rotating stimulus . These results further support the suggestion that personality may well have an opportunity to alter or enhance the resultant percept, particularly when the stimulus itself does not facilitate a clear decision.
The principal result of this work is that the likelihood of a given individual to see meaning in a noisy image is measurably related to their personality. The particular novelty of the current result is that we have shown that this individual difference is a not a product of suggestibility, but a genuine and consistent bias in some people toward saying a stimulus is present when there is only noise. This bias is correlated to a reduced sensitivity to the actual presence of a noisy stimulus leading to the suggestion that this mistaken perception of meaning is the product of a noisier system and the measurable consequence of a false correlation of that noise at an early stage in the system. We further suggest that this may provide the basis for the development of an hallucination, and may also explain why some abstract art can be so compelling for some, and yet leave others cold.
S1 Appendix. File containing details for the 2x2 Anova illustrated in Fig 2, and Bayesian Analysis of the critical data presented in the manuscript.
S1 Dataset. Raw data and figures in manuscript.
We wish to thank Ophélie Favrod and Christine Mohr for considered, insightful and constructive comments on the original submission, which significantly improved this paper. Conversations with Dan Little, Maggie Webb, Steven Dakin, Daniel Bennet and Olivia Carter have also contributed significantly to this work.
Conceived and designed the experiments: SJC TP DR. Performed the experiments: SJC TP. Analyzed the data: TP SJC. Contributed reagents/materials/analysis tools: SJC. Wrote the paper: SJC TP DR.
Cropper SJ (2014) Nature makes abstract art more captivating. The Conversation. Available: https://theconversation.com/nature-makes-abstract-visual-art-more-captivating-24723: https://theconversation.com.
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