dataesr/scientific-paragraphs-categorization huggingface dataset:
Therefore, investigating real-time decoding with state-of-the-art models is essential to move toward practical BCI decoding in real-world applications. Assessing the real-time performance of these decoding methods will require more extensive evaluation methods than those used in the current article. For example, to evaluate model performance on data that was not involved in the optimal parameter selection process, a separate test set should be acquired. Another crucial aspect that becomes an added concern with real-world BCI applications is the design of the control system. As we decode single-joint movements, these could be used to trigger discrete actions beyond the coordinated movements of regular gait cycles. For example, detection of ankle dorsiflexion could be used to press and release the clutch of a car with a prosthesis during driving.
This suggests that one could build a decoding pipeline for prosthetic device control using data from non-disabled individuals. However, more research is needed on various aspects to confirm these hypotheses and determine the most appropriate decoding methods. for real-life situations. AM and UM gratefully acknowledge funding from the European Union's Horizon 2020 Research and Innovation Program under grant agreement no. 952401 (TwinBrain-TWINning the BRAIN with machine learning for neuro-muscular efficiency).
Acknowledgments The authors thank  Denis Steckelmacher  for his advice on general ML and benchmarking and  Dasa Gorjan  for her assistance in determining the methods for this study. This research was made possible thanks to the  Strategic Research Program Exercise  and the  Brain in Health and Disease: The Added Value of Human-Centered Robotics  and the  EUTOPIA cotutelle Ph. D. project  Brain-computer interface applications.
Following a systematic review of the literature, we found 17 reports of differences between self and other stimuli in reaction times (RT) and percentage of errors for implicit self-recognition tasks, and 9 for explicit tasks. For implicit tasks, the differences ranged from a selfadvantage of 133 ms to a self-disadvantage of 4 ms, while errors ranged from an 11% advantage to a 2% disadvantage. Explicit tasks were less consistent, ranging from a 61 ms and 16% advantage to a 270 ms and 15% disadvantage. The present study was originally designed (in 2005) to compare the hand self-recognition ability of healthy adults to that of brain-damaged participants, making both implicit (left-versus-right) and explicit (self-versus-other) hand recognition judgements. Since insufficient and highly variable data were collected from the neurological group, the overall study was not written-up in detail.
There is, however, now a substantial literature on hand self-recognition in healthy participants, so the data from healthy participants have been re-analysed and accompanied by a systematic review and meta-analysis. The present study asks, experimentally and meta-analytically: is there a self-advantage in the recognition of hand images in implicit and explicit tasks? Following  Keenan et al. 's (2000)  hemispheric dominance hypothesis, we also designed experiments to ask whether performance is better when our left hand responds to self and right hand to other images, as compared to the opposite mapping. Finally, we assessed the influence of task difficulty (operationalised in terms of stimulus duration), and the effect of informing participants about the proportions of self-images that would be presented.
Participants Three groups of healthy adult participants completed a range of tasks across five experiments. Participants were recruited in 2005-2006 from the local population of staff and students in Lyon; all participants were (likely) white/ Caucasian Western Europeans, although this information was not requested or recorded. Handedness was assessed with the 20-item version of the Edinburgh Inventory (Oldfield 1971), but no additional data were collected about how often participants worked or how skilled they may be with their hands. Details of participants and experimental design for all experiments are given in Table  1. All participants gave their written informed consent. Some were financially compensated for their time, others participated without.
Analysis The mean correct reaction times (RT) and the proportion of errors were recorded for each condition. RT distributions were positively skewed, so raw RT data were log10transformed before averaging. Mean RTs were transformed back before statistical analysis. A small number of extreme datapoints were removed-in all cases, these were due to technical failures or missed responses (e. g. , RT < 100 ms, RT ≥ 2000 ms). The main question was whether performance was better for self than other hands, for which data were averaged over all other conditions, and paired t tests were used. The selfadvantage effect should result in better performance (shorter RTs, fewer errors) for self than other hands, particularly in implicit (left vs. right) tasks. For Experiments 1b, 2b, 3 and 5, data from each participant were fit with log-transformed (RT) or logistic (error) regression.
Four further studies were excluded, because no self-versus other analysis was possible. Of the 20 included studies (33 experimental groups), 7 involved full colour photos and 13 greyscale. Of the 13 greyscale studies, 4 included a mix of non-face body parts (e. g. , hands, legs). Within these mixed studies, the authors reported no between-body-part differences, so the data were pooled with all other exclusively hand studies. The full list of 1135 articles screened, along with a classification and more extensive notes for all 67 potentially relevant reports is provided in the supplementary spreadsheet file (meta_analysis. ods), specifically in the 'DETAILS' tab. A PRISMA flowchart is given in the supplementary materials. Effect sizes for self-versus-other comparisons were calculated from the included studies, using information from figures and text, and converting statistical results where necessary.
2 • C/min. Pilot studies showed that this temperature (-3 • C) was sufficient to induce chill coma within a few minutes with full survival upon returning to room temperature (data not presented). Following the HKDT procedure, the individuals were observed and provoked using light flashes and gentle taps, and the temperature at which individuals first moved any body part was noted as their chill coma recovery temperature (T recovery ). A low T recovery is interpreted as high cold tolerance.
We used one-way ANOVAs to examine if individual metabolite concentrations within each day differed according to collection time. The concentrations of all quantified metabolites were then scaled and mean centered. For each sampling day, between-class PCA (R-package "ade4"), were run to explore the daily temporal structure of the metabolomic profiles. Monte Carlo tests (1000 permutations) were used to examine the significance of differences in metabolite profiles among classes of individuals from the four sampling times. Further, the metabolites that contributed the most to separation of groups were identified and ranked by their correlation to the principal components that described most of the inertia in the data. All analyses were carried out using the software "R" (R Core Team, 2020). Raw temperature and GC-MS files used for the analyses are available in the Supplementary Material.
Results In this work, we prepared several crystals of a triple mutant of bacteriorhodopsin  44  (tmBR), proton-pumping rhodopsin MAR  45  and sodium pump KR2  46  (monomeric form); these rhodopsins, despite sharing a similar fold, are of different origins and, therefore, are naturally surrounded by different lipids (which makes the MPs quite different in the landscapes of hydrophobic surfaces). All crystals were derivatised with krypton under the pressure of 130 ± 5 bar using the "soak-and-freeze" methodology at the ESRF high-pressure facility for MX  47  ; additionally, tmBR crystals were also derivatised with argon under 2000 ± 10 bar using the highpressure freezing method developed at the facility  48. Native datasets were also collected from crystals of the same batch for tmBR and MAR at ambient pressure (Table  1 ).
Krypton/argon atoms (Fig. 1 ) were located using anomalous difference Fourier electron density maps (see Methods). Datasets of the highest resolution for each derivative were then chosen for refinement (Table  1 ). In contrast to previously reported studies  31, [39] [40] [41] [42] 49  , most of the noble gas atoms were observed on the outer hydrophobic surface (buried in the membrane) of the MPs and only a small portion of the atoms were identified in internal cavities. An explicit correlation can be established between the number of noble gas positions found in the structures and the resolution of diffraction data. In total, 47, 35, 11 and 19 noble gas atoms were identified as partially occupying positions in the four crystal structures (tmBRargon, tmBR-krypton, KR2-krypton, MAR-krypton, respectively, see Table  2 , Fig.
Crystallographic data collection, structure solution, and refinement. X-ray diffraction data were collected at the European Synchrotron Radiation Facility (ESRF), on beamlines ID23-1  63  and ID29  64  (Table  1 ). Prior to data collection, crystals mounted on the goniometer were located and characterised using X-ray mesh scans analysed by Dozor-MeshBest  65, 66. The X-ray beam size at sample position was chosen in the range from 10 to 50 μm FWHM in accordance with Dozor-MeshBest analysis. The experimental parameters for optimal data collection were designed using the program BEST  67. Structure factor amplitudes and anomalous differences of krypton derivatives were measured at 14. 3-14. 4 keV (f"=3. 8e, Table  1 ), above the krypton K-absorption edge (which is 14. 3256 keV, Table  1 ); the anomalous difference data of tmBR-Ar derivative were measured at lower energy, 6.
7 keV (f″ = 1. 21e); the two native datasets of MAR and one of tmBR were collected at the energy of 12. 75 keV, at which another dataset of tmBR-Ar derivative was also collected to obtain higher resolution. For native crystals, standard cryogenic sample mounting was used. Each dataset was collected on a different single crystal. Some low-resolution datasets were discarded. Finally, the anomalous difference data were merged from three crystals of each of MAR-Kr and tmBR-Kr derivatives. One anomalous difference dataset was used for KR2-Kr. Two datasets were used for tmBR-Ar: one with anomalous difference data was used to identify argon positions and the other one of higher resolution was used to refine the structure. Diffraction images were processed with XDS 68 and XSCALE  68. Structure factor amplitudes and anomalous differences were generated using programs POINTLESS and AIMLESS  69.
Native KR2 structure (PDB code: 4XTL) was used as a starting model for KR2-Kr structure solution. Native MAR structure was refined based on the PDB code 5JSI. Native structure of tmBR was solved by molecular replacement using wild-type structure as starting model (PDB code 1QHJ). Final structural models (see Table  2 ) were obtained by alternating cycles of manual building in Coot 70 followed by refinement in REFMAC5  71. Omit (F o -F c ) maps were used to verify the presence of lipid fragments, ions, and water molecules initially found in the native structures. Anomalous difference Fourier maps were calculated with fast Fourier transform (FFT, CCP4) using DANO and (α calc + 90°) as coefficients (α calc = calculated phases from the final refined models). Noble gas atoms were placed in the coinciding peaks of the anomalous difference maps (above 5 r.
The latter included a single bead per each amino acid located at its C α atom. All beads separated by less than 15 Å were considered connected by uniform harmonic potentials, i. e. "springs". Apart from that, noble gas resolved by the MX was also included into the elastic network and modelled as similar particles similarly to an ENM-based method for identification of "essential" binding sites, ESSA  83. We used the ProDy package to calculate normal modes and mean-square fluctuations of the coarse-grained beads estimating the fluctuations of atoms  84  for proteins with and without bound noble gases. Since the absolute values of fluctuations depend on the selection of the force constant in the harmonic potentials of the elastic network, with this latter being an arbitrary value, the resulting fluctuations are given in the arbitrary units.
Acknowledgements This study used the infrastructure of the  Applied Genetics Resource Facility of MIPT  (support grant  075-15-2021-684 ). The work was supported by the  Ministry of Science and Higher Education of the Russian Federation  No. 075-15-2021-1354  (X-ray data collection and treatment) and  Russian Science Foundation  No. 21-64-00018  (protein preparation). V. B. and I. O. acknowledge the  Ministry of Science and Higher Education of the Russian Federation  (agreement no. 075-00337-20-03 , project  FSMG -2020-0003 ).
Study design The study was approved on December 14, 2013 by the Institutional Review Board of Sud-Est V, Grenoble, France (N 6705). Written informed consent was obtained from all participants prior to enrolment. The study was registered with clinicaltrials. gov (NCT02120326). This patient-assessor blinded, randomized sham-controlled trial with two parallel arms (active versus sham a-tDCS) was conducted between May 5, 2014 and December 18, 2019 at the Pain Centre of the Grenoble Alpes University Hospital. The study consisted of 3 phases (Fig. 1 ): an assessment of the frequency of migraine attacks for one month before treatment with a-tDCS (Baseline); after randomization, a 2-month period of active or sham a-tDCS, including an induction phase and a maintenance phase for a total of 11 sessions (Month 1, 2); a 3-month follow-up post-treatment phase (Month 3, 4, 5).
15), these variables were included as fixed covariates at each of the models. The most appropriate covariance structure for the residual correlation matrix was selected. For categorical variables, we used the Chi-square or Fisher's exact test to compare between-group differences at each time point of the follow-up period. Data were analysed using Stata 16. 0 software (StatCorp, College Station, TX, USA). The statistician was blinded to the treatment groups. A two-sided P value < 0. 05 was considered statistically significant and no adjustments for multiple testing were performed.
Stimuli Because the experiment was run on an online platform, exact control of stimulus size was not possible. Testable. org displays stimuli as images centered on observers' personal computer screens, adjusted for each participant's screen resolution but without distorting the image proportions (i. e. the same adjustment in width and height). Observers were instructed to sit 60 cm (arm's length) from their screen. All stimuli were 1024x768 pixel images; stimulus sizes below are given for a typical laptop screen, but because of individual screens the values can vary from 0. 7 to 1. 2 in proportion. Stimuli were generated using Psychtoolbox for Matlab  ((Brainard, D. , 1997; Kleiner, M et al. , 2007; Pelli, G. , 1997) ) and saved as images. A black dot, 0. 25 degrees of visual angle (dva) in diameter and presented at screen center, served as a fixation point.
Data analysis To quantify performance, psychometric functions were fit on individual response data using the quickpsy package developed for R by (  (Linares & López-Moliner, 2016) ). Two parameters are of interest: the slope of the psychometric function, and the point of subjective equality (PSE), i. e. the stimulus level for which subjects selected each response option 50% of the time. Average psychometric functions shown in figures were obtained by bootstrapping individual fits. Serial dependence was calculated as a percentage by considering error trials (i. e. trials in which the shape value was less than 0. 5 in which observers reported seeing a square, and trials in which the shape value was greater than 0. 5 in which observers reported seeing a circle). The number of trials in which the response erred towards the previously presented shape was divided by the total number of errors.
Green: single shapes in blocked and interleaved designs. Red: double shape trials in which subjects reported only one of the two shapes, serial dependence on the previous shape on the same side for all double-shape trials (data from Exp. 1 & 2); SD on previous shape on the same side when it was cued (Exp. 1); SD on previous shape on the same side when it was uncued (Exp. 1); SD on previous cued shape on the opposite side (Exp. 1); SD on the average of the two previous shapes (Exp. 1 & 2). Purple (Exp. 2): double-shape trials in which subjects reported the average of the two shapes: SD on the average of the two previous shapes; SD on the previously cued single shape. Figure  5. Psychometric functions (probability of responding "square" as a function of physical shape value), in the ensemble experiment (Exp.
Searching the literature The literature search was performed in the PubMed, Embase and Lilacs databases in December 2020, and a complementary search on Google Scholar was also performed. A manual search was performed in the references of the selected articles to find other potentially eligible articles. The keywords used were: intracranial electroencephalography; iEEG; medial temporal lobe; hippocampus; oddball; evoked potentials; event-related potentials; P300; P3; ERP; and MTL-P300. The search was performed systematically in the same way for all online databases adapting the strategy.
Eligibility criteria and selection of studies Articles published in English from 1985 to December 2020 were included. Articles published before 1985 were not included because they use a different methodology than the current ones. Observational studies in humans were considered for inclusion: case series, cohort studies, and cross-sectional studies. The identified titles, abstracts, and full-text articles were read and blindly selected by two independent reviewers. In the event of disagreement, a third reviewer resolved the impasse. We excluded studies with EEG recordings on the surface of the skull to concentrate the research only on results through the iEEG recordings. In the following steps, studies that did not correlate MTL-P300 to the EZ were excluded. Regarding the articles found that were written by the same group of authors, those with a greater number of patients were included, to the detriment of those with a smaller number of patients, as long as the article provided the necessary baseline data to calculate the accuracy of the MTL-P300 in lateralizing the EZ.
Data collection and analysis The data of the articles were extracted and classified using a data extraction spreadsheet (Microsoft Excel, Microsoft Corp. , Redmond, WA, United States) created based on the relevant information at the beginning of the research and improved according to the inclusion of the studies. Two independent researchers read the full text of the selected studies and extracted the data in pairs. The analysis of the results was based on the agreement between the abnormal response of the MTL-P300 in the oddball paradigm and the EZ defined through the clinical and electrographic diagnosis from the recordings with depth electrodes (iEEG), which is considered the gold standard method in patients with unilateral TLE. The sensitivity of the method to separately define the laterality of the EZ in TLE ( left or right), as well as in relation to the presence or absence of hippocampal sclerosis was investigated and discussed in the articles.
RESULTS From the total of 608 articles, the search resulted in 308 citations in the databases represented in the flowchart shown in ►Figure 1. The complementary search on Google Scholar resulted in 300 articles, and no study was added based on the manual searches. After the exclusion of duplicate citations, 196 citations were submitted to a selection  process based on the title and abstracts, and 12 citations remained. The full text of these 12 selected citations was examined in more detail. ] [17] [18]  Two articles  10, 11  by the same authors of one of the included articles  19  were excluded, despite having a larger number of patients, because it did not contain the sample specifications that would enable us to calculate the accuracy of MTL-P300 in defining the EZ, and it was not possible to recover these data.
Three studies  7, 19, 20  were chosen because they met the inclusion criteria and were evaluated according to the JBI scale as containing the data required for a good analysis of internal quality (►Table 1). The included works comprised a total sample of 112 patients. In two studies, 7,20 a consecutive series of patients who had the MTL-P300 registered using depth electrodes was included. In another study,  19  a series of patients who had the MTL-P300 and AMTL-N400 cognitive potentials recorded through stereo-EEG were included. The gender distribution was 52 women and 60 men; 59 patients had left TLE and 53, right TLE, and the average age was of 28. 9 (range: 16-56) years. In the study by Puce et al. ,  7  there were 33 cases of left TLE and 24 of right TLE in a sample of 32 men and 25 women with a mean age of 27.
Chromatographic separation was achieved using a Zorbax Eclipse XDB-C18 column (length 150 mm, internal diameter 3. 0 mm, particle size 3. 5 μm; Agilent). Analytes were measured in scheduled multiple reaction monitoring. For quantification of amino acids, a 10-point calibration was performed, using a mixture containing all amino acids in the measurement (A9906 amino acid standards, Sigma-Aldrich, Taufkirchen, Germany). For quantification of acylcarnitines, area ratios of analyte to internal standard were calculated and multiplied with the internal standard concentration. Data analysis was done using Analyst 1. 7. 0 software (AB Sciex). In line with earlier studies  [28]  , the concentration of AAs was related to the TP.
Statistical Analysis To analyze the relationship between leptin and BCS, and between FT and BCS, a linear regression analysis (GraphPad PRISM 8, Version 8. 3. 1, GraphPad Software, LCC) was performed after testing for normality. A linear regression analysis was likewise performed to study the relationships between the metabolic hormone's leptin, insulin, adiponectin and IGF-I. The regressions were carried out on the average hormone concentrations for each individual for each of the seven consecutive samples collected prior to uterine flushing. To test for differences between groups in the FA and AA composition, we used Mann-Whitney-U test (SPSS, Version 26. 0. 0. 0, IBM.
Data Acquisition and Processing Due to technical constraints from EEG signal processing (minimum recording length of 60 s), six different phases of recordings were selected for further analyses [(1) baseline parked (BasP-first 120 s), (2) baseline straight road (BasS-first 120 s), (3) the first round trip (RTstart-60 s), (4) the highest-rated round trip (RT + + -60 s), (  5 ) the last round trip (RTstop-60 s), (  6 ) recovery (Recov-the middle 120 s) (Figure  1B )]. The total amount of extracted recordings thus corresponded to 9 min for each participant. Each round trip was considered as two consecutive slaloms (back and forth, excluding the U-turns, as the latter events did not respect the car dynamics investigated in the study). Reference measurements were obtained from the baseline parked period.