Bias and discriminability during emotional signal detection in melancholic depression
© Hyett et al.; licensee BioMed Central Ltd. 2014
Received: 5 September 2013
Accepted: 8 April 2014
Published: 27 April 2014
Cognitive disturbances in depression are pernicious and so contribute strongly to the burden of the disorder. Cognitive function has been traditionally studied by challenging subjects with modality-specific psychometric tasks and analysing performance using standard analysis of variance. Whilst informative, such an approach may miss deeper perceptual and inferential mechanisms that potentially unify apparently divergent emotional and cognitive deficits. Here, we sought to elucidate basic psychophysical processes underlying the detection of emotionally salient signals across individuals with melancholic and non-melancholic depression.
Sixty participants completed an Affective Go/No-Go (AGN) task across negative, positive and neutral target stimuli blocks. We employed hierarchical Bayesian signal detection theory (SDT) to model psychometric performance across three equal groups of those with melancholic depression, those with a non-melancholic depression and healthy controls. This approach estimated likely response profiles (bias) and perceptual sensitivity (discriminability). Differences in the means of these measures speak to differences in the emotional signal detection between individuals across the groups, while differences in the variance reflect the heterogeneity of the groups themselves.
Melancholic participants showed significantly decreased sensitivity to positive emotional stimuli compared to those in the non-melancholic group, and also had a significantly lower discriminability than healthy controls during the detection of neutral signals. The melancholic group also showed significantly higher variability in bias to both positive and negative emotionally salient material.
Disturbances of emotional signal detection in melancholic depression appear dependent on emotional context, being biased during the detection of positive stimuli, consistent with a noisier representation of neutral stimuli. The greater heterogeneity of the bias across the melancholic group is consistent with a more labile disorder (i.e. variable across the day). Future work will aim to understand how these findings reflect specific individual differences (e.g. prior cognitive biases) and clarify whether such biases change dynamically during cognitive tasks as internal models of the sensorium are refined and updated in response to experience.
KeywordsBayesian analysis Decision-making Depression Melancholia Signal detection
Melancholia is frequently conceptualised as a biological disorder encompassing disturbances of mood, motor function, thinking, cognition and perception [1, 2]. Whilst cognitive impairments in melancholia have been investigated in detail [3, 4], definitive identification of selective neurocognitive impairments has not been achieved. Given the pressing need to examine underlying perceptual and inferential processes in heterogeneous illnesses such as depression , it is increasingly recognised that a range of methodological approaches should be utilised in the analysis of neurocognitive data to more accurately capture the nature of disturbances across differing depressive syndromes. Such refined approaches have direct utility in enhancing understanding of group-specific psychophysical processes across sub-types of depression.
There is typically great inter-subject variability on tests of neuropsychological function in the major psychiatric illnesses . Meaningful interpretations of brain function in specific disorders is difficult given such variability. This is further compounded by summarising an individual’s position on a performance continuum (as with summing errors on a task) in order to infer the presence or absence of cognitive impairments. Furthermore, commonly utilised neuropsychological tests in those with depressive disorders typically rest upon broad construct-level approaches (e.g. tests of ‘executive function’ or ‘attentional control’) that do not facilitate the development of theories regarding specific psychophysical disturbances in individuals. Despite such drawbacks in assessing cognition in psychiatric illnesses, significant advances have been made over the past 20 years in explaining human perceptual inference and action [7–9] using probabilistic statistical principles such as those developed through a Bayesian-based approach . The Bayesian statistical modelling approach has been applied to individual and group cognitive data across multiple cognitive domains, including signal detection that is viewed as encompassing the processes of attention, decision-making and executive functioning [11, 12]. Formally, the signal detection capacity of an individual can be influenced by prior beliefs (or internal models of the world) and the incoming sensory stream, generating that individual’s response profiles. This, in turn, provides an ideal platform through which to measure perception and inference. In the analysis of cognitive data, signal detection theory or SDT  allows modelling of the optimal detection of stimuli, through estimating discriminability and bias . SDT gives rise to measures of discriminability – how easily signal (response) and noise (non-response) trials are distinguished – and bias, reflecting how well the decision-making criterion relates to the optimal criterion. Both constructs reflect an individual’s internal model of the sensorium and their prior contextual beliefs. Signal and noise trials of a task can be represented along a perceptual strength construct in SDT, referring to the strength of inference made to a particular stimulus – that is, the probability that a conclusion (decision/action) is true given its premises. Inferences during streams of trials are continuously monitored through sensory experience and evaluation, and may then be used to update decision criteria for subsequent task performance. Rouder and Lu  suggest it is reasonable to expect that on such tasks there will be significant participant-level variability in signal detection sensitivity, creating a need for statistical models that capture individual processes.
Inter-subject variability is rarely modelled in neuropsychological studies of depressed individuals. Moreover, commonly used aggregation methods have the potential to lead to statistical effect estimates that may poorly represent group heterogeneity . Bayesian statistics offer the ability to pre-specify prior knowledge through the specification of priors . A Bayesian approach to data analysis is also appealing in the setting of decision- making in the face of uncertainty because it embodies the same type of assumptions – and hence represents the same constructs – as emerging models of human decision-making [17, 18]. When considering group data using SDT, individual subject variability can be modelled using hierarchical Bayesian techniques , allowing estimation of data-driven posteriors of mean bias and discriminability as well as their variance or precision (the inverse of variance) [11, 12]. When cognition is variably disrupted, as arguably is the case in depression, inter-subject estimates of bias and optimal judgement may be influenced, which can ideally be modelled through hierarchical Bayesian SDT analyses. There are several reasons as to why such an approach may offer significant benefit.
In health, cognitive ‘priors’ can be viewed as personal beliefs that are optimised towards the most likely value of a given percept . In depression, however, such processes may be suboptimal in different ways across individuals, extending variously across perceptual, inferential and performance domains. It has been suggested that depression is associated with distorted inference (e.g. “arbitrary inference”) at certain levels of severity (e.g. psychotic depression ), yet despite recent theoretical research with Bayesian modelling in depression [5, 21] no studies have employed Bayesian statistics to model cognitive capabilities in depressive illnesses such as melancholia. Most studies to date have attempted to delineate underlying mechanisms of negative cognitive biases  based on the notion that depressed individuals have a characteristically negative view of the self, world and future [20, 23]. Several studies have shown that attention is selectively drawn to negative information (e.g. ), and that memory of negative information is enhanced . However, few studies have provided a formal quantitative framework for modelling individual level disturbances from empirical psychophysical data. While some studies (e.g. ) have established evidence for neurobiological correlates of response bias, it remains to be seen whether cognitive biases extend across depression as a whole or whether they are specific to given individuals or sub-set diagnostic groups. From the findings to date it is evident that there is an unmet need in elucidating basic mechanisms of neurocognitive dysfunction across individuals with depression.
We propose that biases in emotional stimulus processing in depression can be accurately captured through investigation of different depressive sub-types using a hierarchical Bayesian emotional SDT framework. Employing an emotional word ‘go/no-go’ task, which requires responding and inhibition of responding to serially presented, randomly sequenced positive, negative and neutral words, we hypothesised that each depressed sub-set would show less optimal responding (poorer discriminability) across emotional signal conditions as compared to the control group, but that the melancholic sub-set would show more difficulty in detecting true signal trials from noise trials, particularly on emotional signal conditions (i.e. lower sensitivity) compared with non-melancholic and control participants.
Participants consisted of 20 melancholic and 20 non-melancholic depressed individuals, recruited through a specialist depression clinic at the Black Dog Institute in Sydney, Australia. A healthy control group of 20 participants was recruited through the community. The study was approved by the University of New South Wales Human Research Ethics Committee and all study participants gave informed consent prior to taking part.
Psychiatric and neurological screening
Exclusion criteria for healthy controls included a lifetime history of a mood and/or psychotic disorder as screened by the MINI . Depressed participants were considered eligible if they had a current major depressive episode, but no (hypo) mania or psychosis identified on the MINI. Those with depression were additionally required to meet a current (past 7 days) level of depression severity of 11 or more on the QIDS-SR16, indicative of at least moderate depression severity. All participants were required to be fluent in English, and the age range for inclusion was between 18 and 75 years. Exclusion criteria for all participants consisted of current or past drug or alcohol dependence, current or past history of neurological disorder (i.e. neurodegenerative conditions, stroke, central nervous system infection, tremor), a history of brain injury with significant impairment (i.e. neurotrauma from haemorrhage, oedema, hypoxia), invasive neurosurgery and/or an estimated full scale IQ (WAIS-III)  score of below 80 as assessed by the WTAR . An additional exclusion criterion for depressed participants was having received electroconvulsive therapy within the preceding six months. Current medication was recorded. In addition to the above screening, all participants completed the Global Assessment of Functioning (GAF)  and the State-Trait Anxiety Inventory (STAI) . Patient groups were assessed for observable psychomotor disturbance using the CORE measure . Screening was conducted by trained research assistants.
Delineation of depressive sub-types (melancholic versus non-melancholic depression) proceeded according to the clinical criteria presented by Parker et al. . These criteria are based upon characteristic clinician rated scores (by trained psychiatrists in the current study) across a number of domains and include presenting clinical features (e.g. symptoms as well as signs of psychomotor disturbance), previous response to drug and non-drug treatments, developmental factors, personality factors and family history [1, 2]. The focus of the current study on perceptual accuracy but not reaction time tempered circularity between diagnostic assignment (e.g. cognitive slowing in melancholia) and signal detection performance. Previous research  has shown the prototypic diagnostic approach used in the current study (involving symptom and non-symptom data) to be more strongly differentiating of melancholic and non-melancholic depression than use of the DSM-derived  melancholic specifier criteria which consider symptoms only.
Neuropsychological testing procedures
All study participants took part in a brief neuropsychological assessment administered by a trained research assistant, with tests taken from the CANTAB , that included the Stockings of Cambridge (SOC), Intra/Extra-Dimensional Shift (IED), Rapid Visual Information Processing (RVP) and Affective Go/No-Go Task (AGN). All testing took place in a sound-attenuated room that housed a desktop computer running CANTAB eclipse version 3.0 software. Additional computer hardware (touch screen and response/press pad) allowed recording of behavioural responses to the stimuli. The focus on the present report is on the AGN.
Words appear for 300 milliseconds one at a time in the centre of the computer screen, followed by a 900 millisecond inter-stimulus interval (ISI). Each block hence lasts for 22 seconds. Participants rest between blocks for five seconds, allowing preparation for the following block. Analysis variables from the AGN consisted of hits (correct responses to signal trials), false alarms (incorrect responses to noise trials), misses (incorrect rejections to signal trials) and correct rejections (to noise trials).
Hierarchical Bayesian modelling of AGN data
A hierarchical Bayesian graphical model for SDT (as detailed in [11, 12]) was used for the AGN data. As a statistical technique, such modelling – with the use of Markov chain Monte Carlo (MCMC) sampling – allows for integration of a prior distribution (prior beliefs/knowledge) with data from the behavioural task to obtain approximations of the posterior distributions of the outcome parameters. AGN blocks were categorised by emotional signal condition (positive, negative, neutral): thus, three specified models were used for the current analysis. Alternating noise conditions were pooled together for each of the signal conditions. For example, a positive signal distribution in the current study had a noise distribution that included both negative and neutral stimuli. We modelled individual participant responses to the task (counts of hits and false alarms) to generate posterior estimates of discriminability and bias from hit and false alarm rates, separately for each of the emotional signal conditions, with uniform prior distributions hence assigning equal probabilities to all possible states.
For bias estimates, the optimal criterion is centred at zero between two equal-variance Gaussian distributions representing signal and noise distributions. A negative bias value relative to zero indicates a preference towards more ‘yes’ responses (as it is nearer the noise distribution), whereas higher positive values reflect a preference for ‘no’ responses. The location of the response criterion (positioned along a unidimensional strength construct of perceptual accuracy) is derived from a participant’s estimate as to whether a stimulus constitutes a signal or a noise trial. For instance, a participant whose ‘yes rule’ is further from the noise distribution requires a stronger signal to permit detection – thus, the strength of the signal required is determined by the strength of the participant’s internal representation of that signal. In such cases, the available perceptual evidence needs to be substantially greater than the criterion rule to say ‘yes’ . Discriminability is an estimate of the ability to differentiate between signal and noise trials and indicates how well a signal trial can be detected, with higher values indicating an increased capacity to distinguish between signal and noise trials. The previously developed implementation of hierarchical SDT , as shown in Additional file 1, was modified and implemented in WinBUGS . Posterior distributions of bias and discriminability were estimated using MCMC sampling (10,000 samples), using hit and false alarm rates over uniform (reference) priors (i.e. where all responses are equally likely). The posterior means of bias and discriminability, taken as the joint emotional signal detection capacity of individuals in each group, is the focus of our analyses. Convergence of all chains was assessed using R̂ (obtained by comparing two parallel chains in WinBUGS ) and using Geweke’s method , which compares the first 10 percent of each chain with the last 50 percent. All chains were found to be at convergence after 10000 iterations using R̂ (all <1.1). However, the MCMC samples for the positive condition in the non-melancholic group did not converge using the criteria of Geweke  and, thus, a burn-in of 5000 samples (i.e. where the first 5000 samples are discarded, followed by a further 10,000 samples being drawn) for all positive chains across all groups was used.
The modelling approach allows for inspection of a range of posterior distribution statistics. The 95% credible interval (CI) estimates are reported for each of the individual distributions of bias and discriminability, which are compared according to a 95% highest posterior density (HPD) interval difference . A 95% HPD group difference estimate (HPDd) that does not contain zero is considered “significantly different”. This latter approach is similar to that suggested by Lindley . We also visualise the violin plots across modelled parameters in each group for each signal condition (using the MCMC distributions) (see Additional file 2). Violin plots marry the traditional box plot, representing the interquartile range, with smoothed distributional characteristics of the samples .
Clinical and demographic characteristics of melancholic (Mel), non-melancholic (N-Mel) and control groups
§ t = -0.19, p = 0.85 ‡ t = 0.68, p = 0.85 † t = 0.96, p = 0.34
§ χ 2 = 0.00, p = 1.00 ‡ χ 2 = 0.42, p = 0.52 † χ 2 = 0.42, p = 0.52
Years of education
§ t = 0.43, p = 0.41 ‡ t = -2.66, p <0.01 † t = -3.00, p <0.01
§ t = -0.46, p = 0.65 ‡ t = -1.91, p = 0.06 † t = -1.70, p = 0.10
§ t = 0.00, p = 1.00 ‡ t = 16.92, p <0.01 † t = 15.39, p <0.01
§ t = 0.19, p = 0.85 ‡ t = 5.28, p <0.01 † t = 7.00, p <0.01
§ t = -1.20, p = 0.24 ‡ t = 8.17, p <0.01 † t = 11.55, p <0.01
§ t = 4.28, p <0.01
§ t = 3.00, p <0.01
§ t = 2.38, p < 0.05
§ t = 4.14, p <0.01
§ t = -3.23, p <0.01 ‡ t = -11.43, p <0.01 † t = -12.17, p <0.01
SSRI% yes (n)
§ χ 2 = 9.69, p <0.01
Other med% yes (n)
§ χ 2 = 27.22, p <0.01
Frequencies of hits (H), misses (M), false alarms (FA) and correct rejections (CR) across signal valence conditions and group on the go/no-go task
False Alarm Rate
False Alarm Rate
False Alarm Rate
Visual inspection of these frequency tables suggests higher hit rates in the non-melancholic and control groups compared with the melancholic group across positive and neutral conditions. The d′ statistics (indexing the separation of the signal and noise response distributions) also point to a reduction in signal detection sensitivity across all signal conditions in the melancholic group compared to the non-melancholic and control groups. To examine AGN task performance more formally we next report on the hierarchical Bayesian modelling.
Group effects of mean bias and discriminability
In terms of mean discriminability, there was a significant difference between melancholic and control groups during neutral trials (HPDd = -1.020 – -0.042). This difference in posterior estimates of discriminability is consistent with impaired discrimination capacity for neutral signals in the presence of both positive and negative noise trials. The non-melancholic group appeared slightly less optimal than the control group in terms of discriminability to neutral signals, but this effect did not reach significance. Hierarchical analyses of the mean bias for negative and neutral signal conditions, and mean discriminability for positive and negative signal conditions did not reveal any differences across groups.
Comparing standard deviation model estimates
Posterior estimates of the standard deviations for bias and discriminability across all stimulus conditions are also shown in Figure 3. Significantly increased standard deviation values were found in the melancholic group compared to non-melancholic and control groups on positive signal trials. A similar pattern was found for the negative signal condition, with larger standard deviation estimates found in the melancholic group compared to the non-melancholic group. No group effects were found for neutral bias or for any of the signal conditions for discriminability. The increased standard deviations on the emotional signal blocks in the melancholic group is indicative of greater variability of mean bias values across participants, thus reflecting a significantly broader distribution of bias values compared to those values observed in the other groups.
Sensitivity and robustness analyses of model posteriors
We conducted a robustness check of the results using narrower priors on mean and gamma (precision) of bias and discriminability and, additionally, a sensitivity analysis by uncollapsing noise conditions. These additional analyses are presented in Additional file 3. Briefly, for the hierarchical model of positive and neutral signal conditions, differences in mean bias and discriminability were more robust to changes in prior distributions than were the standard deviation differences. The majority of effects were robust when the noise conditions were unpooled. The loss of some significant effects is consistent with the loss of power that arises when trials are split and not pooled. Nonetheless, these additional analyses do highlight that bias to positive signal trials, and discriminability to neutral signal trials, may be influenced by differing noise conditions.
The hierarchical Bayesian SDT model implemented in this paper revealed that signal detection processes in melancholic and non-melancholic depression are significantly influenced by stimulus type and individual subject variability. Our modelling approach allowed interrogation of the neuropsychological data at two levels: the mean results across individuals in specific groups, and the heterogeneity of the groups themselves, across the psychophysical constructs of bias and discriminability. In terms of mean differences, we observed that the melancholic participants overall were less sensitive to detecting emotional signals, while non-melancholic participants displayed more liberal responses to emotional signal blocks. This provides support for our predictions that the melancholic group would display difficulty in detecting signal trials from noise trials on emotional word blocks. Also, optimal responding was found to be reduced in the melancholic group compared to the control group, as evidenced by decreased mean discriminability on neutral signal blocks. In terms of subject heterogeneity, we found that there was greater inter-subject variability of the bias estimates for the emotional signal conditions in the melancholic group, which indicates divergent bias estimates across individuals. Visualising the range of individual participant responses (Figure 5) argues against this effect being driven by outliers. Further, changes to the precision of prior distributions had little impact on the observed mean difference findings, suggesting these findings are highly robust. Despite this, however, when differing noise conditions were examined there was a moderate effect, with some previously significant differences for specific signal conditions no longer remaining significant. The observed impact of differing noise conditions thus warrants further consideration in future psychophysical studies using differing emotional and non-emotional stimuli. The main findings allow for specific neurocognitive models to be advanced with regard to depression and its sub-typing, namely the potential to gain insight into underlying psychophysical mechanisms across individuals and whether the depression is melancholic or non-melancholic in type, and highlight several important issues in the analysis and interpretation of neurocognitive data.
Our findings align with the commonly held notion (e.g. ) that those with melancholic depression exhibit cognitive deficits that are observable during task performance. However, we add the observation that those with non-melancholic depression may also be impaired in their ability to perform ‘optimally’ on cognitive tasks such as the AGN. The observed trend of less optimal responding in non-melancholic depression did not, however, reach significance but may benefit from a focus in future studies. While research using the AGN task in depression  claims it as a measure of ‘inhibitory control’, the analytic methods previously employed often prevent interpretation beyond a continuum of impairment (e.g. number of errors on a task). The current study is the first, to our knowledge, to utilise an affective go/no-go task in sub-types of depression. In doing so – and through analysis of the data using hierarchical Bayesian SDT – the findings offer an increased understanding of the sensitivity and discriminability capacity of individuals with differing types of depression, and highlight the importance of examining for apparent dysfunction with more refined models. Recently, Schulz and colleagues  examined the convergent validity of emotional and non-emotional go/no-go tasks and concluded that, together, they offer “moderate capacity” for probing the neuropsychological construct of behavioural inhibition. Those authors also emphasized the need for testing emotional and non-emotional signal detection mechanisms in affective disorders to clarify underlying cognitive-emotional contributions. The diverging sensitivities across emotional and non-emotional conditions in the depressed groups in the current study, along with a lack of discrimination to neutral signals in melancholia, suggests that a range of cognitive mechanisms may be involved in responding to differing stimuli.
Across neuropsychological studies of depression it is evident that no single cognitive deficit model can be applied to specific groups, due to the inherent heterogeneity of the depressive domain. However, in light of the current findings of discrepancies in bias between signal conditions, it might be possible that set-shifting impairments – as previously reported in depression , and more specifically in melancholic depression  – play an important role. While not explicitly assessed in the current study, it is conceivable that neuropsychological constructs such as disrupted attention set-shifting and perseveration underlie the observed effects. The melancholic sub-type has been shown to be differentiated from non-melancholic depression on the basis of response selection performance , where performance on compatible and incompatible trial types (e.g. stimulus–response compatibility tests) reflect cognitive strengths and weaknesses. As a rule these studies have not specified psychophysical functions of stimulus sensitivity and discrimination capacity, and have tended to report broader metrics of performance such as numbers of hits and misses across subjects. From a cognitive standpoint there is likely to be significant benefit in modelling performance-related psychophysical mechanisms (i.e. through SDT and similar analyses) in depressive disorders and then next establishing whether this provides insight towards any neurocognitive disease mechanisms. We argue that the cognitive deficits observed in different types of depression can be conceptualised in such a way so as to explain impairments in emotion-bound optimal decision-making.
Prior research on sensory processing offers further insight into the findings of decreased sensitivity to emotional signals and poorer discrimination to neutral signals in melancholia. Knill and Pouget  suggest that perception of one’s environment is influenced by the likelihood of the presence or absence of relevant stimuli given an individual’s past experience (i.e. perceptual priors) with that stimuli. These factors contribute to the relative uncertainty over one’s environment, and allow inference regarding the causes of percepts. We propose that the low sensitivity to emotional signals and lack of discriminability observed across melancholic participants may be a result of inefficient sensory integration – possibly resulting from constructs such as inefficient cognitive control mechanisms (see ). This in turn may be a function of ‘inflexible’ priors (e.g. negative cognitive biases) and unsuccessful updating (e.g. such as perseveration due to a failure of emotional inhibition ). The observation that the non-melancholic participants responded more frequently to noise trials on emotional signal blocks also suggests that they too are less sensitive to fluctuations in the emotional environment. Such erroneous judgements could be due to emotional processing biases in depression, a factor that has been acknowledged in accounting for decision-making impairments . Research into the probabilistic nature of decision-making [21, 49, 50] suggests diverse mechanisms underlying optimal judgement. Neurobiologically, probabilistic learning paradigms have been used to examine human cognition , with the findings pointing to distinct roles of serotonin and noradrenaline in learning and inhibition. Both neurochemicals have long been implicated in depressive disorders  and may be of relevance to understanding the differences observed between and within depressive sub-types.
In addition to the behavioural changes within individuals, research using Bayesian inference has also highlighted the importance of perceptual variation between individuals. Recent theoretical work on perceptual uncertainty advocates the utility of modelling trial-by-trial updating across individuals in a Bayesian framework , which is argued to be of significant benefit in conceptualising the current findings from the signal detection task. The hierarchical modelling using MCMC in the current study yielded estimates of the standard deviation of both bias and discriminability performance (i.e. the extent of the differences between measured individuals). The increased standard deviations in the melancholic group on emotional bias suggests differential individual performance profiles when compared to non-melancholic and control groups. This could be due to a range of non-cognitive factors in an otherwise homogeneous group or may alternatively reflect divergent cognitive strengths and weaknesses, which we now consider.
Several lines of research have indicated that melancholic depression is associated with diurnal variation of mood , with such variation thought to impact on neuropsychological performance across the day . Clinical depression with diurnal variation has also been found to result in differential performance on accessibility and recall of positive and negative (self-related) experiences , with positive memories more likely to be retrieved when depression is less severe in the afternoon/evening. Varying biological influences such as cortisol hypersecretion – shown to be specific to melancholia  – may play a pivotal role in modulating cognitive function in depression as previously suggested . Such factors are important considerations with respect to the current findings given study participants were not all tested at the same time of day. Furthermore, inconsistent medication regimens across individuals within and between groups may contribute to individual differences in emotional processing biases , thus possibly dampening the association between the depressed state and cognitive impairments. If such factors were found to be unrelated – and individual differences were indeed evident upon replication – it is conceivable that melancholia (due to the observed variation) may be able to be portrayed as comprising several distinct sub-types as suggested by Parker and Hadzi-Pavlovic  (e.g. functional and structural melancholia). Factors such as family history, age-of-onset, presence/absence of neuropathological changes and cardiovascular disease would need to be clarified for any such sub-typing model to be advanced within the current context. Given the increased age of our sample, neuropathological changes in some individuals cannot be excluded. Despite these possibilities, the utility of the current findings lie first and foremost in their ability to inform psychophysical models of depression, with several caveats.
As indicated above, there were several study limitations. Firstly, the analysis did not interrogate trial-to-trial variability. Thus, the supposed dynamics of sensory integration (stimulus–response updating), as previously put forward , could not be quantified in this sample. In addition, the signal detection task used did not allow for further analysis of aspects of emotional decision-making (i.e. specific decision-making rules) beyond bias and discriminability functions. Such specific limitations, if overcome in future studies, would provide a more refined model of decision-making and clinical conditions themselves. It is therefore proposed that future work should attempt to examine the utility of dynamic models of decision-making in light of changing emotional environments, along with key clinical variables, to further establish the mechanisms by which perception and action interact in depression.
There has been an upsurge of interest in framing cognitive function in psychiatric conditions in probabilistic terms [5, 60], precipitated by research in cognitive and computational sciences that, in health, humans respond optimally in their environments. The signal detection approach used in the current study offers insight into the optimal response parameters of those with depression, and extends previous suggestions of ‘emotional response biases’ in depression through psychophysical modelling. The hierarchical models in the current paper allowed estimation of the most probable response distributions, and is an advance on previous (e.g. frequentist) attempts that aim to elucidate neuropsychological dysfunction in depressed groups through group averaging approaches. Future studies should attempt to clarify how different cognitive processes operate across different individuals. Such work should also aim to provide a more detailed characterization of perceptual (probabilistic) sensory updating across changing environments in depression, whilst recognising the fundamental role pre-existing cognitive biases play in response to environmental demands.
Affective Go/No-go Task
Cambridge Neuropsychological Test Automated Battery
The CORE Assessment of Psychomotor Change
Global Assessment of Functioning
Highest Posterior Density
Highest Posterior Density Difference
Markov chain Monte Carlo
Mini-International Neuropsychiatric Interview
16-item Quick Inventory of Depressive Symptomatology
Rapid Visual Information Processing
Signal Detection Theory
Stockings of Cambridge
Serotonin-Noradrenaline Reuptake Inhibitor
Selective Serotonin Reuptake Inhibitor
State-Trait Anxiety Inventory
Wechsler Adult Intelligence Scale – Third Edition
Windows Bayesian inference Using Gibbs Sampling
Wechsler Test of Adult Reading.
This study was supported by grants from the National Health and Medical Research Council of Australia (Program Grant 1037916), a NSW Health Infrastructure Grant and Queensland Health. The views expressed are those of the authors and not those of the granting bodies. The authors wish to thank those who have made useful comments during preparation of this manuscript.
- Parker G, Hadzi-Pavlovic D: Melancholia: A Disorder of Movement and Mood. A Phenomenological and Neurobiological Review. 1996, Cambridge, UK: Cambridge University PressView ArticleGoogle Scholar
- Taylor MA, Fink M: Melancholia: The Diagnosis, Pathophysiology and Treatment of Depressive Illness. 2006, New York, NY: Cambridge University PressView ArticleGoogle Scholar
- Austin M-P, Mitchell P, Goodwin GM: Cognitive deficits in depression: possible implications for functional neuropathology. Br J Psychiatry. 2001, 178: 200-206. 10.1192/bjp.178.3.200.View ArticlePubMedGoogle Scholar
- Bench CJ, Friston KJ, Brown RG, Scott LC, Frackowiak RS, Dolan RJ: The anatomy of melancholia: focal abnormalities of cerebral blood flow in major depression. Psychol Med. 1992, 22 (3): 607-615. 10.1017/S003329170003806X.View ArticlePubMedGoogle Scholar
- Paulus MP, Yu AJ: Emotion and decision-making: affect-driven belief systems in anxiety and depression. Trends Cog Sci. 2012, 16 (9): 476-483. 10.1016/j.tics.2012.07.009.View ArticleGoogle Scholar
- Franzen MD: Reliability and Validity in Neuropsychological Assessment. 2000, New York, NY: Plenum Publishers, 2Google Scholar
- Dayan P, Hinton GE, Neal RM, Zemel RS: The Helmholtz machine. Neural Comput. 1995, 7 (5): 889-904. 10.1162/neco.19126.96.36.1999.View ArticlePubMedGoogle Scholar
- Friston K: A theory of cortical responses. Philos Trans R Soc Lond B Biol Sci. 2005, 360 (1456): 815-836. 10.1098/rstb.2005.1622.View ArticlePubMedPubMed CentralGoogle Scholar
- Knill DC, Pouget A: The Bayesian brain: the role of uncertainty in neural coding and computation. Trends Neurosci. 2004, 27 (12): 712-719. 10.1016/j.tins.2004.10.007.View ArticlePubMedGoogle Scholar
- Bayes T: An essay towards solving a problem in the doctrine of chances. Phil Trans Roy Soc Lond. 1763, 53: 370-418. 10.1098/rstl.1763.0053.View ArticleGoogle Scholar
- Lee MD: BayesSDT: software for Bayesian inference with signal detection theory. Behav Res Methods. 2008, 40 (2): 450-456. 10.3758/BRM.40.2.450.View ArticlePubMedGoogle Scholar
- Lee MD, Wagenmakers E-J: Bayesian Cognitive Modeling: A Practical Course. 2014, Cambridge, UK: Cambridge University PressGoogle Scholar
- Green DM, Swets JA: Signal Detection Theory and Psychophysics. 1966, New York, NY: WileyGoogle Scholar
- Wickens TD: Elementary Signal Detection Theory. 2002, Oxford, UK: Oxford University PressGoogle Scholar
- Rouder JN, Lu J: An introduction to Bayesian hierarchical models with an application in the theory of signal detection. Psychon Bull Rev. 2005, 12 (4): 573-604. 10.3758/BF03196750.View ArticlePubMedGoogle Scholar
- Lee MD, Wagenmakers E-J: Bayesian statistical inference in psychology: comment on Trafimow (2003). Psychol Rev. 2005, 112 (3): 662-668.View ArticlePubMedGoogle Scholar
- Behrens TE, Woolrich MW, Walton ME, Rushworth MF: Learning the value of information in an uncertain world. Nat Neurosci. 2007, 10 (9): 1214-1221. 10.1038/nn1954.View ArticlePubMedGoogle Scholar
- Karim M, Harris JA, Langdon A, Breakspear M: The influence of prior experience and expected timing on vibrotactile discrimination. Front Neurosci. 2013, 7: 255-View ArticlePubMedPubMed CentralGoogle Scholar
- Griffiths TL, Tenenbaum JB: Optimal predictions in everyday cognition. Psychol Sci. 2006, 17 (9): 767-773. 10.1111/j.1467-9280.2006.01780.x.View ArticlePubMedGoogle Scholar
- Beck AT, Alford BA: Depression: Causes and Treatment. 2009, Philadelphia, PA: University of Pennsylvania Press, 2Google Scholar
- Huys QJ, Dayan P: A Bayesian formulation of behavioral control. Cognition. 2009, 113 (3): 314-328. 10.1016/j.cognition.2009.01.008.View ArticlePubMedGoogle Scholar
- Mathews A, MacLeod C: Cognitive vulnerability to emotional disorders. Annu Rev Clin Psychol. 2005, 1: 167-195. 10.1146/annurev.clinpsy.1.102803.143916.View ArticlePubMedGoogle Scholar
- Beck AT: Cognitive Therapy of Depression. 1979, New York, NY: Guildford PressGoogle Scholar
- Mathews A, Ridgeway V, Williamson DA: Evidence for attention to threatening stimuli in depression. Behav Res Ther. 1996, 34 (9): 695-705. 10.1016/0005-7967(96)00046-0.View ArticlePubMedGoogle Scholar
- Gilboa-Schechtman E, Erhard-Weiss D, Jeczemien P: Interpersonal deficits meet cognitive biases: memory for facial expressions in depressed and anxious men and women. Psychiatry Res. 2002, 113 (3): 279-293. 10.1016/S0165-1781(02)00266-4.View ArticlePubMedGoogle Scholar
- Elliott R, Rubinsztein JS, Sahakian BJ, Dolan RJ: The neural basis of mood-congruent processing biases in depression. Arch Gen Psychiatry. 2002, 59 (7): 597-604. 10.1001/archpsyc.59.7.597.View ArticlePubMedGoogle Scholar
- Sheehan DV, Lecrubier Y, Sheehan KH, Amorim P, Janavs J, Weiller E, Hergueta T, Baker R, Dunbar GC: The Mini-International Neuropsychiatric Interview (M.I.N.I.): the development and validation of a structured diagnostic psychiatric interview for DSM-IV and ICD-10. J Clin Psychiatry. 1998, 59: 22-33.PubMedGoogle Scholar
- Rush AJ, Trivedi MH, Ibrahim HM, Carmody TJ, Arnow B, Klein DN, Markowitz JC, Ninan PT, Kornstein S, Manber R, Thase ME, Kocsis JH, Keller MB: The 16-Item Quick Inventory of Depressive Symptomatology (QIDS), clinician rating (QIDS-C), and self-report (QIDS-SR): a psychometric evaluation in patients with chronic major depression. Biol Psychiatry. 2003, 54 (5): 573-583. 10.1016/S0006-3223(02)01866-8.View ArticlePubMedGoogle Scholar
- Wechsler Adult Intelligence Scale®: Third Edition (WAIS®–III). 2001, San Antonio, TX: Pearson AssessmentsGoogle Scholar
- Wechsler Test of Adult Reading™ (WTAR™). 2001, San Antonio, TX: Pearson Assessments
- American Psychiatric Association: Diagnostic and Statistical Manual of Mental Disorders, Fourth Edition, Text Revision (DSM-IV-TR). 2000, Arlington, VA: American Psychiatric PublishingView ArticleGoogle Scholar
- Spielberger CD: Manual for the State-Trait Anxiety Inventory (Form Y). 1983, Menlo Park, CA: Mind GardenGoogle Scholar
- Parker G, Hadzi-Pavlovic D, Wilhelm K, Hickie I, Brodaty H, Boyce P, Mitchell P, Eyers K: Defining melancholia: properties of a refined sign-based measure. Br J Psychiatry. 1994, 164 (3): 316-326. 10.1192/bjp.164.3.316.View ArticlePubMedGoogle Scholar
- Parker G, Fink M, Shorter E, Taylor MA, Akiskal H, Berrios G, Bolwig T, Brown WA, Carroll B, Healy D, Klein DF, Koukopoulos A, Michels R, Paris J, Rubin RT, Spitzer R, Swartz C: Issues for DSM-5: whither melancholia? The case for its classification as a distinct mood disorder. Am J Psychiatry. 2010, 167 (7): 745-747. 10.1176/appi.ajp.2010.09101525.View ArticlePubMedPubMed CentralGoogle Scholar
- Parker G, Fletcher K, Hyett M, Hadzi-Pavlovic D, Barrett M, Synnott H: Measuring melancholia: the utility of a prototypic symptom approach. Psychol Med. 2009, 39 (6): 989-998. 10.1017/S0033291708004339.View ArticlePubMedGoogle Scholar
- Robbins TW, James M, Owen AM, Sahakian BJ, McInnes L, Rabbitt P: Cambridge Neuropsychological Test Automated Battery (CANTAB): a factor analytic study of a large sample of normal elderly volunteers. Dementia. 1994, 5 (5): 266-281.PubMedGoogle Scholar
- Lunn DJ, Thomas A, Best N, Spiegelhalter D: WinBUGS - a Bayesian modelling framework: concepts, structure, and extensibility. Stat Comput. 2000, 10: 325-337. 10.1023/A:1008929526011.View ArticleGoogle Scholar
- Gelman A, Rubin DB: Inference from iterative simulation using multiple sequences. Stat Sci. 1992, 7: 457-511. 10.1214/ss/1177011136.View ArticleGoogle Scholar
- Geweke J: Evaluating the accuracy of sampling-based approaches to calculating posterior moments. Bayesian Statistics 4: Proceedings of the Fourth Valencia International Meeting. Edited by: Bernardo JM, Berger JO, Dawid AP, Smith AFM. 1992, Oxford, UK: Clarendon PressGoogle Scholar
- Plummer M, Best N, Cowles K, Vines K: CODA: Convergence Diagnosis and Output Analysis for MCMC. R News. 2006, 6 (1): 7-11.Google Scholar
- Lindley DV: Introduction to Probability and Statistics from a Bayesian Viewpoint. Part 2: Inference. 1965, Cambridge, UK: Cambridge University PressView ArticleGoogle Scholar
- Hintze JL, Nelson RD: Violin plots: A box plot-density trace synergism. Am Statistician. 1998, 52 (2): 181-184.Google Scholar
- Murphy FC, Sahakian BJ, Rubinsztein JS, Michael A, Rogers RD, Robbins TW, Paykel ES: Emotional bias and inhibitory control processes in mania and depression. Psychol Med. 1999, 29 (6): 1307-1321. 10.1017/S0033291799001233.View ArticlePubMedGoogle Scholar
- Schulz KP, Fan J, Magidina O, Marks DJ, Hahn B, Halperin JM: Does the emotional go/no-go task really measure behavioral inhibition? Convergence with measures on a non-emotional analog. Arch Clin Neuropsychol. 2007, 22 (2): 151-160. 10.1016/j.acn.2006.12.001.View ArticlePubMedPubMed CentralGoogle Scholar
- Michopoulos I, Zervas IM, Pantelis C, Tsaltas E, Papakosta VM, Boufidou F, Nikolaou C, Papageorgiou C, Soldatos CR, Lykouras L: Neuropsychological and hypothalamic-pituitary-axis function in female patients with melancholic and non-melancholic depression. Eur Arch Psychiatry Clin Neurosci. 2008, 258 (4): 217-225. 10.1007/s00406-007-0781-8.View ArticlePubMedGoogle Scholar
- Rogers MA, Bellgrove MA, Chiu E, Mileshkin C, Bradshaw JL: Response selection deficits in melancholic but not nonmelancholic unipolar major depression. J Clin Exp Neuropsychol. 2004, 26 (2): 169-179. 10.1076/jcen.188.8.131.52086.View ArticlePubMedGoogle Scholar
- Ridderinkhof KR, van den Wildenberg WP, Segalowitz SJ, Carter CS: Neurocognitive mechanisms of cognitive control: the role of prefrontal cortex in action selection, response inhibition, performance monitoring, and reward-based learning. Brain Cogn. 2004, 56 (2): 129-140. 10.1016/j.bandc.2004.09.016.View ArticlePubMedGoogle Scholar
- Hauser MD: Perseveration, inhibition and the prefrontal cortex: a new look. Curr Opin Neurobiol. 1999, 9 (2): 214-222. 10.1016/S0959-4388(99)80030-0.View ArticlePubMedGoogle Scholar
- Glimcher PW: Decisions, Uncertainty, and the Brain: The Science of Neuroeconomics. 2003, Cambridge, MA: The MIT PressGoogle Scholar
- Yu AJ, Dayan P, Cohen JD: Dynamics of attentional selection under conflict: toward a rational Bayesian account. J Exp Psychol Hum Percept Perform. 2009, 35 (3): 700-717.View ArticlePubMedPubMed CentralGoogle Scholar
- Chamberlain SR, Muller U, Blackwell AD, Clark L, Robbins TW, Sahakian BJ: Neurochemical modulation of response inhibition and probabilistic learning in humans. Science. 2006, 311 (5762): 861-863. 10.1126/science.1121218.View ArticlePubMedPubMed CentralGoogle Scholar
- Schildkraut JJ: The catecholamine hypothesis of affective disorders: a review of supporting evidence. Am J Psychiatry. 1965, 122 (5): 509-522.View ArticlePubMedGoogle Scholar
- Mathys C, Daunizeau J, Friston KJ, Stephan KE: A Bayesian foundation for individual learning under uncertainty. Front Hum Neurosci. 2011, 5: 39-View ArticlePubMedPubMed CentralGoogle Scholar
- Paykel ES: Classification of depressed patients: a cluster analysis derived grouping. Br J Psychiatry. 1971, 118 (544): 275-288. 10.1192/bjp.118.544.275.View ArticlePubMedGoogle Scholar
- Moffoot AP, O'Carroll RE, Bennie J, Carroll S, Dick H, Ebmeier KP, Goodwin GM: Diurnal variation of mood and neuropsychological function in major depression with melancholia. J Affect Disord. 1994, 32 (4): 257-269. 10.1016/0165-0327(94)90090-6.View ArticlePubMedGoogle Scholar
- Clark DM, Teasdale JD: Diurnal variation in clinical depression and accessibility of memories of positive and negative experiences. J Abnorm Psychol. 1982, 91 (2): 87-95.View ArticlePubMedGoogle Scholar
- Carroll BJ: The dexamethasone suppression test for melancholia. Br J Psychiatry. 1982, 140: 292-304. 10.1192/bjp.140.3.292.View ArticlePubMedGoogle Scholar
- Rubinow DR, Post RM, Savard R, Gold PW: Cortisol hypersecretion and cognitive impairment in depression. Arch Gen Psychiatry. 1984, 41 (3): 279-283. 10.1001/archpsyc.1984.01790140069008.View ArticlePubMedGoogle Scholar
- Harmer CJ, Goodwin GM, Cowen PJ: Why do antidepressants take so long to work? A cognitive neuropsychological model of antidepressant drug action. Br J Psychiatry. 2009, 195 (2): 102-108. 10.1192/bjp.bp.108.051193.View ArticlePubMedGoogle Scholar
- Montague PR, Dolan RJ, Friston KJ, Dayan P: Computational psychiatry. Trends Cog Sci. 2012, 16 (1): 72-80. 10.1016/j.tics.2011.11.018.View ArticleGoogle Scholar
- The pre-publication history for this paper can be accessed here:http://www.biomedcentral.com/1471-244X/14/122/prepub
This article is published under license to BioMed Central Ltd. This is an Open Access article distributed under the terms of the Creative Commons Attribution License (http://creativecommons.org/licenses/by/2.0), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly credited. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.