dataesr/scientific-paragraphs-categorization huggingface dataset:
A summary of key drug interactions is provided in Table  3. The use of lifestyle substances such as caffeine, nicotine, alcohol, cannabis, and other drugs should be assessed and discussed with the patient, and appropriate therapeutic recommendations made. Prior to diagnosis, many patients use caffeine excessively to improve alertness the general stimulation effects are not pleasant even when and patients readily give up or reduce caffeine use when on a specific medication for alertness. Case reports suggest that nicotine may mask or relieve symptoms of narcolepsy, including EDS and even cataplexy  [114, 115]. Such an interaction is supported by limited data suggesting that nicotine addiction may be mediated by hypocretin pathways  [116]. Although narcolepsy symptom relief may be viewed as a benefit of nicotine and may thus be a barrier to smoking cessation in narcoleptics, the act of smoking is itself of concern because of the risk of falling asleep while smoking resulting in injury and damage  [114].
In either case, the experience of synesthesia should induce neural activity in the regions normally involved in the experience of the concurrent (the induced association). That is, color centers should be activated when grapheme-color synesthetes read achromatic letters or words (the inducers), imagine them or listen to them. Rouw et al. (2011)  reviewed the studies that have searched for the neural correlates of synesthesia. They gathered the data interpretations proposed in neuroimaging studies on synesthesia, in search of an emergent consistent pattern. The logic behind such a meta-analysis is correctly based on the assumption that when effect sizes are small, they should not reach significance in every study because of sampling error, especially when tested groups are small, as is the case in the field of synesthesia.
However, metaanalyses may be biased when the reported "significant" results are questionable. A quantitative meta-analysis of this magnetic resonance imaging (MRI) literature (e. g. ,  Yarkoni et al. , 2011)  would require not only that similar protocols were used (that was not the case), but also to have access to effect sizes at each voxel, in order to include also the studies that did not find significant results. While several initiatives promote data sharing in open data sources (e. g. ,  Poline et al. , 2012; Keator et al. , 2013; Sternberg et al. , 2013) , currently, in most studies information is given only about the coordinates of voxels that pass an arbitrary, often disputable, statistical threshold. Here, we followed an approach quite different from usual metaanalyses of MRI data, adopting a systematic skeptical point of view in order to first deconstruct the results from the interpretation proposed by their authors, and then evaluate every dataset with similar and robust criteria.
However, superior performance when present seems, in fact, related to the ability to actually identify the letter (failure of crowding on some trials:  Ward et al. , 2007) , not to the strength or quality of synesthetic associations. Hubbard et al. (2005a)  also measured the performance of synesthetes in a visual search task, which they had promoted as an objective measure of the synesthetic experience. Surprisingly, they did not report the correlation value between the scores measured for this task and the BOLD response in V4 ([6, Selective reporting]). We computed this correlation using the data points of their Figure  3 , and found r = 0. 12 (p = 0. 82). Such a result should have led the authors to reject their hypothesis on the role of V4 in synesthesia. Our conclusion: this study did not demonstrate any correlation between brain signals and individual differences related to 3 One could argue that the stronger response to letters than false fonts for this synesthete is all the more convincing because the developing coloring of false-fonts should have weakened the contrast for synesthetic colors.
Sinke et al. (2012)  proposed that the absence of difference in V4 between synesthetes and controls could be due to their matching of VVIQ scores in both groups. However, evidence of any correlation between VVIQ scores and V4 activity does not exist, and whether VVIQ scores did differ between groups in the other studies was not tested. 2013 ) compared the BOLD responses (3T) to graphemes and false-fonts in 13 synesthetes and 11 controls in a block design. The group analysis revealed significant interactions between stimulus and group in 14 regions (Afni 5  software, cluster-extent statistics, pFWE = 0. 01 computed with Monte-Carlo simulation, images were thresholded at p < 0. 0005 6  ; significant clusters had a minimal extent of 134 mm 3 or voxels; 7 mm FWHM smoothing). Interactions were, however, not due in any area to a stronger response to graphemes in synesthetes but not controls.
They performed cluster-extent statistics (SPM5, voxel threshold p < 0. 001; minimal extent was 41 voxels, corresponding to pFWE < 0. 05 as estimated "based on permutation analyses of sub-samples of a large dataset"; 8 mm FWHM smoothing). They detected no cluster of increased connectivity in controls. They detected significant clusters of increased connectivity in synesthetes between the right AC and the left and right motor cortex, as well as between the left IPC and both the left primary AC and the right primary visual cortex. There was no increased connectivity between the visual and AC. They considered that these results supported the disinhibited feedback model of synesthesia. Our conclusion: we agree with the authors that these results are more compatible with the disinhibited feedback theory than the cross-activation theory.
7] [8]  Another study has suggested that agomelatine may have a more beneficial effect on anhedonia than venlafaxine. 9 ith regard to motivation, few data are available on the effects of antidepressants. The Multidimensional Assessment of Thymic States (MAThyS) scale is a useful patient-reported outcome measure with which to assess motivation in patients with depression in the clinical setting. The MAThyS scale was developed and validated to define mood states dimensionally. 10, 11 It was originally designed to assess levels of activation or inhibition in different mood states in bipolar disorder with a single tool and to determine whether a clinical description in terms of activation/inhibition can improve definition of mixed bipolar states associating both manic and depressive symptoms. 10 This scale provides a measure of the degree of inhibition or activation on five a priori dimensions representing cognitive speed, motivation, emotional reactivity, psychomotor function, and sensory perception.
Treatment, follow up, and data collection Patients were evaluated at an inclusion visit (Week 0), when eligibility criteria were verified, data on demographic and clinical variables at baseline documented, and treatment with agomelatine 25 mg was initiated. Patients then returned for two follow-up visits at Week 2 and Week 6, when clinical response was evaluated with a number of rating scales completed by the physician and by the patient. At Week 2, the dose of agomelatine could be increased to 50 mg at the discretion of the investigator.
Outcome measures At each study visit, depressive symptoms were rated with the clinician-rated 16-item quick inventory of depressive symptoms (QIDS-C 16 ),  21  and overall clinical status was rated with the Clinical Global Impression scale. 22 Levels of activation and inhibition were assessed using MAThyS. 10 ther secondary outcome measures included the Patient Global Impression -Improvement Questionnaire,  22  the Sheehan Disability Scale,  23  and the Leeds Sleep Evaluation Questionnaire;  24  these data have been discussed previously  20  and will not be presented in this article. The MAThyS consists of a 20-item set of visual analog scales. 10, 11 Although the MAThyS is designed to be self-rated, it is recommended that a clinician assists in order to explain how the scoring is performed.
Patients From the initial sample of 2,351 patients, the QIDS-C 16 and the MAThyS scores were available at each study assessment for 1,565 subjects (66. 6% of the sample). These constituted the analysis population for this study. Given the relatively high numbers of patients for whom complete data was unavailable, the baseline characteristics of analysis population were compared with those of the patients evaluated in the primary analysis of the study (Table  1 ). The two populations were not significantly different (P. 0. 10), with a marginally shorter disease duration, younger age, and lower number of women in the MAThyS analysis population.
Disclosure This study was supported by a research grant from  Euthérapie, Paris, France. The present analyses and the preparation of the manuscript were performed by the authors independently of the sponsor. These results have been presented in part at the  European Psychiatric Association Congress 2014. PG received research grants from  Eli Lilly and Servier ; honoraria for presentations in congresses from  AstraZeneca ,  Bristol-Myers Squibb ,  Janssen ,  Lundbeck , and Servier; participated on advisory board of  AstraZeneca ,  Janssen ,  Roche , and Servier; has a paid position at  University of Paris-Descartes and Sainte-Anne Hospital , and no shares. FJB has received consulting fees within the last 4 years from  Servier ,  Lundbeck ,  Eli Lilly, Bristol-Myers Squibb , and  Janssen. GV received research grants from  AstraZeneca ; honoraria for presentations in congresses from  AstraZeneca ,  Bristol-Myers Squibb ,  Janssen ,  Lundbeck ,  Eli Lilly , and Servier; participated on advisory board of  Janssen, Lundbeck , and Servier; has a paid position at  University of Lille 2 and Lille University Hospital , and no shares.
Algo-Block is another interface that is somewhat similar to Slot Machine. It consists of a set of physical blocks that connect to one another to form a program  (Suzuki and Kato, 1993). Each block corresponds to a single command in the LOGO programming language. The term tangible programming language was invented by Suziki and Kato in order to describe the AlgoBlock collaborative programming environment  (Suzuki and Kato, 1993 ). Topobo is another example of this kind of interfaces that was designed to learn programming thinking  (Raffle, 2004) , it consists of a set of active and passive blocks which can be combined together to assemble and animate robotic structures. The active blocks are embedded with a kinetic memory which allows recording and playback of physical motion of the constructed assembly.
This may be an advantage for strengthening mispronunciation effects. The impact of filtering out trials where the child does not know both the target word and the distracter will be evaluated in the current study. The criteria used to select the attended trials is also variable, with some considering only long enough fixations to the images (1500 ms in each phase,  Bailey & Plunkett, 2002) , or fixation to both images in the pre-naming phrase or at least, throughout the trial  (Mani & Plunkett, 2007). Finally, data cleaning is achieved by excluding participants not contributing to all experimental conditions  (Fernald et al. , 2006 ; second analysis in  Styles & Plunkett, 2008) , or whose data points fall outside normality  (Fernald et al. , 2006 ; see also  Mani & Plunkett, 2007). Although all these types of pre-processing or filtering allow for cleaner datasets, comparability across experiments would benefit from consistent practice, preferably on the measures that are the most conservative.
For each experiment, we evaluated how the degree of visual noise, together with the different criteria for data selection, modified the different dependent variables. Here, the stimuli were comparable to those in  Mani and Plunkett (2007) , in which 15-to-24-month-olds were presented with two images on both sides of a screen and heard, mid-trial, correctly pronounced in a carrier sentence such as "Look, dog!" for half of the trials, or as a mispronounced version of the target word ("Look, bog!") in the other half of trials. If children recognize lexical entries of familiar words only if they are pronounced correctly (as is expected from the age of 18 months, e. g. ,  Mani & Plunkett, 2007) , a naming effect should be observed in correctly pronounced trials, but not (or significantly less) in mispronunciation trials resulting in an interaction between naming and pronunciation -the key result in these studies.
Stimuli The stimuli were 32 monosyllabic consonant initial words taken from the OCDI (see Appendix B), half targets and half distracters. All are imageable nouns. Target words were judged as known by at least 40% of 20-month-olds (database from the Oxford Babylab), and they were paired with a distracter sharing the same onset consonant and phonemic structure (e. g. , dog and duck). Out of the 16 targets, participants heard 8 labels that were correctly pronounced and 8 that were mispronounced. Following  Mani and Plunkett (2007) , mispronunciations were obtained by changing one phoneme on one or more dimension, either on the onset consonant or the vowel (4 trials each), leading to a pseudoword or a very rare word in infant-directed speech (e. g. , bud). The speech stimuli were recorded in an enthusiastic child friendly manner by a female native speaker of British English.
Scoring The digital scoring system developed by  Meints and Woodford (2008)  was used to synchronize videos with trial onsets. Eye movements (left image, right image, middle or away) frame by frame (40 ms) were scored by skilled coders trained by the first author and naïve to the items being presented to the participants. Each eye fixation was coded, and an independent skilled coder scored 10% of the pool of data randomly for each group. Agreement between coders was high with an intraclass correlation coefficient of 0. 936  (Shrout & Fleiss, 1979). Looking times on each image were then automatically extracted for the pre-and post-naming phases, providing the proportions of looks to the target and the distracter in the pre-and post-naming phases, as well as longest look measures and frame by frame eye position for the time-course analysis.
Again, no significant difference was obtained in the No fixation condition (all t-tests reveal ps >. 05). In the Fixation condition a cluster between 2420 and 2460 ms post word onset was identified but was, however, non significant (cluster t statistics = 4. 33, Monte Carlo p =. 96). For the Fixation Plus condition, we found a significant difference window which was comparable to the first series of analyses, with more looks to the correctly pronounced target from 740 to 1940 ms after stimulus onset (cluster t statistic = 105. 34, Monte Carlo p =. 002). The same analyses conducted on the dataset selected with the strict criterion reveal rather comparable results, with perhaps more sensitivity. On the whole duration of the trial, the No Fixation condition reveals difference cluster between 980 and 1700 ms after the word onset, but Monte Carlo simulations failed to confirm that this difference is significant (cluster t statistics = 12.
Acknowledgment Part of the study was funded by an  ESRC  grant  2009/2011 RES-000-22-3596  and one from the  Nuffield Foundation , both awarded to the fourth author. The authors thank  William A. Simpson  for his advice on saliency measures. Samantha Durrant is a Post-Doctoral Research Associate in the  International Centre for Language and Communicative Development (LuCiD) at the University of Liverpool. The support of the  Economic and Social Research Council  [ ES/L008955/1 ] is gratefully acknowledged.
g. Ourebia ourebi: Brashares & Arcese 1999; Propithecus verreauxi:  Benadi et al. 2008 ; Canis simensis: Sillero-Zubiri & Macdonald 1998; Saguinus mystax:  Gosling & Roberts 2001)  while in the core of the territory they can be involved as a signal of social dominance towards subordinates  (Ralls 1971; Jordan et al. 2010). For example scent marking is used to establish and maintain social dominance in yellow-bellied marmot  (Armitage 1976 ) and its social function directly depends on where the behaviour is performed  (Brady & Armitage 1999). In this study we used data collected on a population of free living Alpine marmots (Marmota marmota) to 1) verify the function of scent marking behaviours, 2) estimate the helper role in territorial task, and 3) perform a comparative test of the rRHP and the GA hypotheses in a cooperative breeding species.
Field data collection We used two observation points (one per study area) located at a minimum distance of 100 meters from the closest group to avoid potential disturbance arising from the presence of the researchers  (Crofoot et al. 2010). We collected 2454 spatial locations for 58 individuals (i. e. 21 females and 37 males), belonging to 9 different groups in 2009 (mean fixes per group = 266; range = 101-390) and 2374 spatial locations for 56 individuals (i. e. 21 females and 35 males) belonging to 10 different groups in 2010 (mean fixes per group = 229; range = 48-432), using the scan sampling method  (Altmann 1974; Martin & Bateson 1993)  and the Animal Locator tool  (Pasquaretta et al. 2012 ) which allows the collection of accurate distance, angle and inclination of an individual in respect to a fixed observation point.
Observations were always conducted by two observers: one who was responsible for locating the individuals by using binoculars and the Animal Locator tool and the other who identified each marmot using a spotting scope thanks to the unique ear tag colour combination for each individual. We recorded the current activity of each individual (i. e. foraging, looking around, looking from the burrow, greeting, grooming, playing, marking, fighting, general movement, and other, see  Barash 1989). We collected the data every 45 minutes and we tested independence of the data applying a Moran autocorrelation test  (Gittleman & Kot 1990)  to 435 individual matrices where positions of each individual were at least collected for 3 consecutive scans (i. e. 1 hour and an half). Time needed to collect spatial data for all aboveground marmots in view was 15 ± 3 min (± s.
Data analysis Territory size: We calculated the territory size and shape using the kernel. area and the kernelUD functions in the R package "adehabitat"  (Calenge 2006; R Development Core Team 2011). We used the Kernel Density Estimator (KDE), representing the intensity with which a given area is used  (Fieberg & Kochanny 2005) , because it allows for the estimation of multiple centres of activities  (Worton 1989; Kernohan et al. 2001). However, KDE is sensitive to the choice of the smoothing parameter h  (Fieberg 2007). The most often used method for selecting the h parameter is the Least Square Cross Validation (LSCV) method. Nevertheless it suffers from large possible biases when applied to clumped data such as those collected for animals with a central burrow system  (Hemson et al. 2005).
Scent marking: To test for seasonal variation in the frequencies of scent marking behaviour we divided each active season into three sub-periods corresponding to 1) post-hibernation (from mid-May to emergence of the first pup i. e. : 26th of June), 2) pup emergence (from the 27th to the first of August) and 3) pre-hibernation (from mid-August to mid-September). For each period and each group, we also calculated the distance between scent marking locations and both the geographic centre and boundaries of the group. We collected 207 scent marking behaviours during the study using the scan sampling procedure described above; we only recorded the first occurrence of the marking behaviour to avoid collecting repeated measures during the same behavioural display. Groups contributed differently to the dataset collected having a mean of 10 scent marking activities per group each year ranging from 0 to 21 marking behaviours.
Space use: To evaluate the effect of helpers on the overlap areas, we estimated the proportion of area shared by each group calculating the ratio between their overlap area and territory size  (Fieberg & Kochanny 2005)  using the kerneloverlap function in the "adehabitat" R package. Territorial aggressive interactions usually occurred between animals of two different social groups  (Pasquaretta pers. obs. ). We consequently used family dyads as case units, and we removed from the analysis data collected when more than two groups were involved in the interaction. We obtained a relative Index of Overlap as the differences between the overlap areas of the two groups involved in the dyad applying the following formula: It should be noted that Overlap (i,j) is a common area of intersection for the two groups in the dyad.
We then used a Chi-squared test to evaluate whether scent-marking behaviour usually occurred close to the territory boundaries rather than to the centre. Moreover we tested differences in scent marking behaviour between sexes and among ages and seasonal periods by running three Bayesian Markov Chain Monte Carlo models for categorical data using individual identity nested in group and year as random effects (package MCMCglmm in R,  Hadfield 2010). In order to test for the Group Augmentation (i. e. influence of total number of individuals) and the RHP hypotheses (i. e. influence of the helper category) we performed multi-model selection on two different linear mixed models: one having the relative Overlap Index and the other the relative mean area available for individual exclusive use for each dyad as response variables.
Multi-model inference is a statistical technique used to compare candidate models and rank them according to the Akaike Information Criterion  (Akaike 1985)  corrected for small sample sizes (AICc) and their normalized Akaike weights (AICw)  (Burnham & Anderson 2002). When the candidate models differed in AICc by 2 units, we accepted the one with the lowest AICc as the best fitting model but considered other acceptable models in the discussion. Multimodel selections were run using the R Package MuMIn  (Barton 2009). We used balanced Male Index, Group Index, their interaction, Young Index and study site as fixed effects in both models. Because we had partially nested data (e. g. 8 groups occupied the same area during two following years while others changed), and because we had repeated measures during the same year (i.
Acknowledgments Acknowledgements -we are grateful to:  N. Martinet  for helping us collect data in 2009. We thank  B. Bassano  for his constant support to the long term Alpine marmot research project in the  Gran Paradiso National Park. We are grateful to the  Surveillance Service  of the park for logistc support and in particular to park wardens W. Vallet and  M. Nicolino  for their help during field work. This research was made possible thanks to funds from the  Gran Paradiso National Park , the  Department of Earth and Environmental Sciences  (Zoology section),  University of Pavia , the  Natural Sciences and Engineering Research Council , and the  Canada Research Chair Committee  to D. R. C. P. was financially supported by a Doctoral grant from  University of Pavia (Italy). C. F. was supported by a  "Bourse d'excellence pour les cycles supérieurs de l'Université du Québec à Montréal (Canada) ".
Dear Editor, Erectile dysfunction (ED) currently affects 152 million men worldwide and this number is likely to reach 322 million by 2025. 1  Penile prostheses (PP) placement remains a last-resort option in cases where organic ED has not been cured by previous medications, notably intracavernosal injection and oral phosphodiesterase type-5 inhibitor. 2 rance ended 2013 with a population of 66 million inhabitants. In our study, we obtained data through the French national code registry database programme de médicalisation des systèmes d'information and from the patient-information forms filled out by the surgeon at the time of the implant. For claim purposes, this system comprehensively records information concerning every surgical procedure that is performed in a private or public hospital in France.