dataesr/scientific-paragraphs-categorization huggingface dataset:
M. ) and a Fellowship through the  Graduate School of Quantitative Biosciences Munich (QBM)  supports D. M. B. H. P. , V. T. and J. A. M. are supported by  EU   FP7 Mitochondrial European Educational Training Project  ( 317433 ). C. M. , R. K. , J. G. and H. P. are supported by  EU   Horizon2020 Collaborative Research Project SOUND  ( 633974 ). R. W. T. is supported by the  Wellcome Centre for Mitochondrial Research  ( 203105/Z/16/Z ) and the  MRC Centre for Neuromuscular Diseases  ( G0601943 ). D. G. is supported by  Telethon-Italy  ( GGP15041 ). We thank the  Pierfranco and Luisa Mariani Foundation  and the  Cell lines and DNA Bank of Paediatric Movement Disorders and Mitochondrial Diseases of the Telethon Genetic Biobank Network  ( GTB09003 ).
Unfolding and experimental uncertainties Fluctuations in jet response from the jet p T resolution of the detector can cause low-energy jets to be misidentified as leading jets. Such fluctuations can produce bin-to-bin migrations in both χ dijet and M jj. The measured distributions are corrected for these migrations and unfolded to the particle level using the D'Agostini iteration method  [58]  implemented in the ROOUNFOLD package  [59]. The unfolding corrections are determined using a two-dimensional response matrix mapping the generator-level M jj and χ dijet distributions onto the measured values. This matrix is obtained using particle-level jets from the PYTHIA8 MC event generator that are smeared in p T using a double-sided Crystal-Ball parameterization  [60]  of the response. This parameterization takes into account the full jet energy resolution including non-Gaussian tails.
For calculating the CI terms, as well as the interference between the CI terms and QCD terms at leading order (LO) and NLO in QCD, the CIJET 1. 0 program  [79]  is employed. For the ADD model, two parameterizations for virtual graviton exchange are considered, Giudice-Rattazzi-Wells (GRW)  [80]  and Han-Lykken-Zhang (HLZ)  [81]. In the GRW convention, the sum over the Kaluza-Klein graviton excitations in the effective field theory is regulated by a single cutoff parameter Λ T. In the HLZ convention, the effective theory is described in terms of two parameters, the cutoff scale M S and the number of extra spatial dimensions n ED. The parameters M S and n ED are directly related to Λ T  [82]. We consider models with 2-6 EDs. The case of n ED = 1 is not considered since it would require an ED of the size of the order of the solar system; the gravitational potential at these distances would be noticeably modified and this case is therefore excluded by observation.
Weather and predation constitute the two main factors affecting the breeding success of those Arctic waders whose productivity is highly variable over the years. We tested whether reproductive success is associated with the post-breeding condition of adults, in which in 'good' years (with warm weather, plentiful food and low predation pressure) the condition of breeders and their productivity is high. To verify this hypothesis, we used a 10-year dataset comprising 20,792 dunlins Calidris alpina, trapped during migration at a stopover site on the southern Baltic Sea shore. Males were consistently in a slightly worse condition than females, likely due to male-biased parental investment in brood rearing. Annual productivity indices were positively correlated with the respective condition indices of breeders from the Eurasian Arctic, indicating that in 'good' years, despite great effort spent on reproduction, breeders leave the breeding grounds in better condition.
On the other hand, in years with plentiful food and low predation, both productivity and the condition of breeders might be high. Given both that waders are commonly studied birds and the availability of large datasets on multiple species, it remains surprising that a relationship between yearly indices of productivity and the post-breeding condition of breeders has not yet been addressed. In the present work, we investigate this relationship in the dunlin, a long-distance migrant, wader species breeding in the high Arctic. We used a 10-year dataset of dunlins, trapped at the stopover site during their southward migration, to test if the condition of breeders correlates with productivity. Additionally, we attempt to identify factors responsible for the variation in condition, by answering the following questions: (i) do males have a poorer post-breeding condition, due to their higher investment in raising broods; (ii) are immatures in worse condition compared to older birds due to being unexperienced; and (iii) is there any effect of origin-i.
Material and methods We used data of migrant dunlins trapped at the stopover site in the Vistula Mouth, Poland (54˚22'N, 18˚57'E) between 1990 and 2000. The year 1997 was excluded because a flood during the migration peak in July resulted in most birds being missed, as trapping had to cease. Birds were stopping over to feed on flat, sandy beaches and annually trapped with walk-in traps between the 12 th July and 25 th September (exact dates of the beginning and ending of trapping differed by 1-3 days). Birds were removed from the traps by professional ornithologists and volunteers at two-hour intervals each day (from 05:00 to 23:00 CET) and transported to the ringing station located outside the feeding areas, at a distance of up to some hundred meters from the trapping area. Each bird was measured, weighted, ringed and released immediately after processing.
A male-biased sex ratio was evident in non-juveniles (immatures-68. 5%, adults-65. 7%) and is well known in dunlin at the chicks stage (61,1%,  [54] ), at the stopover during migration (immatures-60,3%, adults-59,4%,  [55] ) and at various winter quarters (Portugal-75%  [56] , Pacific Coast-61% and 65%  [57] ). The measurement data were carefully checked prior to analysis and all individuals with missing measurements, and a further 17 birds with extreme measurements, most probably due to observer errors, were excluded. We divided our analysis into two steps: first, we focused on estimating the population-level, mean annual condition indices of migrants; secondly, we assessed how these estimates relate to productivity indices. Although it is possible to directly assess the effect of productivity on condition by including the former as a predictor of condition in the model, we preferred a more conservative, although less powerful, approach: condition indices were estimated for a given year, origin, sex and age groups, but were not modelled as a function of productivity.
In our dataset, correlations between the residual body mass of non-juveniles calculated using bill and tarsus lengths were strongly correlated for any single year (>0. 92, which means these two variables share ~80% of variability). We used additive linear mixed effects models (GAMMs) with normal error distribution for their flexibility in capturing non-linear patterns via smoothers and where the optimal amount of smoothing is obtained via cross-validation  [59, 60]. The fixed factors included sex, age, origin and their interactions. Variation due to year was allowed to differ between birds of 'western' and 'eastern' origin and was addressed with the two smoothers, estimated separately for the origin groups. Alternatively, models with just a single smoother, common to both origin groups and the remaining fixed effects as described above, were also fitted, reflecting the hypothesis that the annual condition varies similarly in 'western' and 'eastern' dunlins.
34 and 3. 54 AIC units). We applied the best-supported structure in all the models; this choice is further supported by the fact that models with the same fixed and random parts and different correlation structures produced nearly identical results in terms of parameter estimates, t-statistics, P-values and predictions (in line with  [61] ). We first fitted the global model with age, sex, origin and their interactions as fixed factors and the two smoothers (one estimated for 'western' and another one for 'eastern' birds). After fitting the global model, using the mgcv R-Package  [62] , we proceeded with fitting simpler, nested models with all the remaining combinations of explanatory variables manually. 28 models were fitted in total, including 14 models with the two smoothers, 14 with a single smoother and two 'null' models with smoothers only (one or two) and no other explanatory variables; 'true null' models, with no smoothers, were not considered.
Results Across the entire dataset, in non-juveniles, the mean yearly body condition varied significantly over the years (Fig  1 ), with the lowest mean for 1996 (-1. 74), the highest for 1992 (1. 87) and the grand mean very close to zero (mean -1. 33e-15 ± 4. 01 SD, median -0. 66, 95% CI: -6. 10 to 9. 61). The wide min-max range for any given year indicated the presence of birds in very poor and very good condition regardless of year. The top four models (ω AIC between 0. 20 and 0. 24) included a single smoother, and fixed sex, origin and (in two models) age effects, with interactions between sex and origin or age and origin (Table  2 ). Further models with some support were similar in that they included a single smoother and either missed various fixed effects or did not (Table  2 ). The best-supported model with two smoothers had AIC weight < 0.
We found it surprising that there was little support for the age effect. Immature dunlins undertake breeding in their second year of life  [15, 25, 26]  and due to their low experience and late arrival to the breeding grounds  [21]  might bear higher costs of this attempt. Apparently, in our dataset, the signal for the age effects on condition was too weak to gain substantial support. Dunlin subspecies overlap in morphological characters, which makes it difficult to determine the origin of migrant birds observed at stopover sites and wintering grounds  [34, 75]. There are only a few ringing recoveries between the Vistula Mouth stopover site and the breeding grounds, indicating that dunlins migrating through the Baltic region originate from the Eurasian Arctic, including Siberia  [76, 77]. At the same time, it is known that birds from the easternmost part of the nominate subspecies alpina breeding range (east from Yamal Peninsula) annually migrate through the region in lower numbers than their western counterparts  [33, 35, 77].
The effect of extreme climatic events Our dataset included the year 1992, when an aerosol cloud originating from the 1991 eruption of Mount Pinatubo in the Phillipines led to severe weather conditions and heavily affected avian reproduction over most of the Arctic  [12]. In consequence of the eruption, aerosol clouds caused significant cooling in the spring and summer of 1992 over almost the entire Arctic. In 1992 spring was late, snow-melt delayed and summer started two-three weeks later than in average years, which caused the reduction of potential nesting area and food availability for waders  [85]. Severe weather conditions resulted in a higher than usual proportion of nonbreeders and a delay in breeding initiation in many species  [12]. That the volcano eruption could also affect the condition of birds breeding in the Arctic seems logical, but it has not been shown so far.
Acknowledgments We are thankful to all ringers and volunteers who participated in fieldwork at the Vistula Mouth ringing station. We thank  Daniel O'Connell  for linguistic help. The authors also thank  David Hyrenbach  and three anonymous reviewers for their constructive comments on the earlier draft of the manuscript. The field research in the 1990s was supported and coordinated by  Ornithological Station ,  Polish Academy of Sciences. Data analysis was financially supported by the  Research Grants of the National Science Centre  no. 2012/07/B/NZ8/02810.
This work was supported by  Research Grants of National Science Centre (Poland)  no. NCN2012/07/B/NZ8/02810-LP GN PZ , https:// www. ncn. gov. pl/?language=en; Ornithological Station,  Museum and Institute of Zoology, Polish Academy of Sciences -JG , http://www. stornit. gda. pl/index_en. php. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
The QM region corresponds to the photoswitch, while all methanol molecules compose the surrounding MM region. As already conducted elsewhere by some of the authors, comparison of the two approaches gives valuable structure and spectroscopic insights  [31, 33, 34]. The latter strategy requires the accurate parameterization of the photoswitch force field. Especially, charges have been obtained by the standard Restrained Electro-Static Potential (RESP) procedure  [54] , while all of the parameters are based on the generalized amber force field (gaff)  [55]. Both the charges and the parameters have been refined by QM/MM calculations, as explained below. As for MD, the DASA model was surrounded by 480 methanol molecules (parameters of methanol taken from the solvent library available in AMBER 2016 program  [56] ) in an octahedral box and applying periodic boundary conditions.
Concerning software, all TD-DFT calculations were performed with Gaussian09 (Gaussian Inc. , Wallingford, CT, USA)  [58]  except for the TPA calculation, which was conducted with Dalton2016 (University of Oslo, Oslo, Norway)  [59]. For B3LYP/AMBER optimizations, a Gaussian09/Tinker (Washington University, Saint Louis, Missouri, USA)  [60]  protocol was applied, based on electrostatic embedding. CASPT2 and NEVPT2 computations were performed with the Molcas8 (Lund University, Lund, Sweden)  [61]  and Orca3 (Max-Planck-Gesellschaft, Mülheim an der Ruhr, Germany)  [62]  suite of programs, respectively. The Wigner distribution was realized with the Newton-X program (University of Vienna, Vienna, Austria and University of Pisa, Pisa, Italy)  [63] , while MD was performed with the Amber 2016 software (University of California, San Francisco, California, USA)  [56].
A search for narrow resonances in dielectron and dimuon invariant mass spectra has been performed using data obtained from proton-proton collisions at √ s = 13 TeV collected with the CMS detector. The integrated luminosity for the dielectron sample is 2. 7 fb -1 and for the dimuon sample 2. 9 fb -1. The sensitivity of the search is increased by combining these data with a previously analysed set of data obtained at √ s = 8 TeV and corresponding to a luminosity of 20 fb -1. No evidence for nonstandard-model physics is found, either in the 13 TeV data set alone, or in the combined data set. Upper limits on the product of production cross section and branching fraction have also been calculated in a model-independent manner to enable interpretation in models predicting a narrow dielectron or dimuon resonance structure.
For tt, tW, diboson, and DY τ + τ -production, the produced number of eµ final states should be equal to the sum of ee and µµ final states. This feature is used to compare the eµ spectrum with suitably scaled MC predictions. The resulting scale factors are all consistent with unity and are not applied in the analysis. The background from jets misidentified as electrons is evaluated from multijet data control samples. The method is the same as that described in Ref. [9] , except that data sidebands, rather than MC predictions, are used to evaluate the contributions to the control samples from genuine electrons and photons misidentified as electrons. The method takes into account the different ways in which one or two misidentified jets, in possible conjunction with other particles, can satisfy the selection criteria for dielectron events.
Combination of 8 and 13 TeV data sets The 13 TeV data set is combined with the 2012 data set at √ s = 8 TeV  [9] , corresponding to integrated luminosities of 19. 7 and 20. 6 fb -1 for the dielectron and dimuon channels, respectively. For the combination, these luminosities must be rescaled to match the equivalent 13 TeV luminosities. This scaling depends on the mass of the resonance, with the effective luminosity of the 8 TeV data sample decreasing with increasing resonance mass. The scaling was determined by comparing Z and G KK cross sections calculated by PYTHIA using the NNPDF2. 3LO PDF set at √ s = 8 and 13 TeV. This cross section ratio depends on the PDF set used and different choices of PDF set can change the resulting limits by a few per cent. The scaling also depends on the production mechanism of the new boson, and therefore the value used to combine the data sets depends on the properties of the particular model under consideration.
The 95% CL lower limits on the masses of the Z SSM and Z ψ bosons are presented in Table  1 , along with the expected results. Table  2  presents the corresponding limits for an RS graviton with coupling parameters 0. 01 and 0. 10. In each case the limit appropriate to the width of the boson is used. For example the Z SSM boson mass limits are calculated using a width of 3%. The cross section as a function of mass is calculated at LO using the PYTHIA 8. 2 program with the NNPDF2. 3 PDFs. As the limits in this Letter are obtained on the on-shell cross section and the PYTHIA event generator includes off-shell effects, the cross section is calculated in a mass window of ±5% √ s centred on the resonance mass, following the advice of Ref. [34]. The validity of this procedure for the Z SSM and Z ψ bosons was explicitly checked in Ref.
Summary A search for narrow resonances in dielectron and dimuon invariant mass spectra has been performed using data obtained from proton-proton collisions at √ s = 13 TeV. The integrated luminosity for the dielectron sample is 2. 7 fb -1 and for the dimuon sample 2. 9 fb -1. The sensitivity of the search is increased by combining these data with a previously analysed set of data obtained at √ s = 8 TeV and corresponding to a luminosity of 20 fb -1. No evidence for non-standard-model physics is found, either in the 13 TeV data set alone, or in the combined data set. Upper limits at 95% confidence level on the product of production cross section and branching fraction have also been calculated in a model-independent manner to enable interpretation in models predicting a narrow dielectron or dimuon resonance structure.
Acknowledgments We congratulate our colleagues in the CERN accelerator departments for the excellent performance of the LHC and thank the technical and administrative staffs at  CERN  and at other  CMS institutes  for their contributions to the success of the CMS effort. In addition, we gratefully acknowledge the computing centres and personnel of the Worldwide LHC Computing Grid for delivering so effectively the computing infrastructure essential to our analyses. Finally, we acknowledge the enduring support for the construction and operation of the LHC and the.
The activity of the same neural population was recorded when the animals were engaged in the task, and when they passively listened to the same stimuli. Both single cell and population analyses showed that task-engagement decreased the accuracy of encoding the physical attributes of stimuli. Population, but not single-cell, analyses however revealed that task-engagement induced a shift towards an asymmetric representation of the two stimuli that enhanced target-evoked activity in the subspace of optimal decoding. This shift was in part enabled by a novel mechanism based on the change in the pattern of spontaneous activity during task engagement. Performing identical analyses developed on this task to independent data sets collected in A1 during other behavioral discrimination tasks demonstrated that these findings can be well generalized, independently of the type of stimuli, behavioral paradigm or reward contingencies.
a. Schematic of the approach used to identify lick responsive units to eliminate from population analysis. First, we reconstructed licks using optimal filters as with click reconstruction (Fig 1). To test whether this reconstruction allows to detect lick events, the filter is applied during licks and also during randomly selected time points with no licks (top left) to all units. Each event (lick or no-lick) can therefore be represented by a population vector constituted of the peak reconstruction values for all neurons. We evaluated the accuracy of classifying lick and no-lick time events using a linear decoder applied to this population vector (black distribution, middle panel). The same procedure was applied to randomized data (top right and purple distribution, middle panel) to test the significance of decoding and calculate a p-value (percentage of random data cross validations larger than real data cross validations).
Enhanced representation of target stimuli in A1 is a general feature of auditory Go/No-Go tasks To determine whether the task-related increase in asymmetry between target and reference was a more general feature of primary auditory cortex responses during auditory discrimination, we applied our population analysis to other datasets collected during different tasks. All of these tasks used Go/No-Go paradigms (see Fig. S11a, e ,i and Methods), in which the animals were presented with a random number of references followed by a target stimulus. In these different datasets, animals were required to discriminate noise bursts vs. pure tones (tone detect tasks), or categorize pure tones drawn from low, medium or high-frequency ranges (frequency range discrimination task). Contrasting datasets were obtained from two groups of ferrets that were separately trained on approach and avoidance versions of the same tone detect task.
We therefore set out to tease apart the respective contributions of the two mechanisms in this novel set of tasks. As in Fig. 6 , we compared the distance of target and reference passive and engaged projections to either engaged or passive baseline activities. Out of the three additional datasets, we observed an increase in spontaneous firing rates only in the aversive tone detect task (Fig. 8g ). In this latter paradigm, taskinduced modulations of spontaneous activity patterns explained the change in asymmetry during sound presentation, similar to what was observed in the click rate discrimination task (compare Fig. 8d  and 8h ). The other two tasks showed no global change of spontaneous firing rate (Fig. 8k, o ), and consequently, during the task engagement, the enhancement of the target representation was solely due to the second mechanism, the changes in the target-evoked responses themselves (Fig.
65. Tone detect task -Appetitive conditioning. 4 ferrets were on an appetitive version of the tone detect task previously described  30. On each trial, the number of references presented before the target varied randomly from one to four. Animals were rewarded with water for licking a water spout in a response window 0. 1-1. 0 s after target onset. False alarms were punished with a timeout when ferrets licked earlier in the trial before the target window. The average DR during experiments was 0. 76. This data set contained sessions with different trial durations, therefore we analysed separately data from the first 200ms after stimulus onset and 200ms before stimulus offset. For this task, the passive data was not structured in the format of successive reference and target trials as in the engaged session but instead the animal was presented with a block of reference only trials followed by a block of target only trials separately.
Acoustic stimuli All sounds were synthesized using a 44 kHz sampling rate, and presented through a freefield speaker that was equalized to achieve a flat gain. Behavior and stimulus presentation were controlled by custom software written in Matlab (MathWorks). Click rate discrimination task. Target and reference stimuli were preceded by an initial silence lasting 0. 4 s followed by a 1. 25 s-long broadband-modulated noise bursts (temporal orthogonal ripple combinations, TORC  66  ) acting as a neutral stimulus, without any behavioral meaning (Fig. 1A ). Click trains all had the same duration (0. 75 s, 0. Tone detect task. Reference sounds were TORC instances. Targets were comprised of pure tone with frequencies ranging from 125-8000 Hz. Target and reference stimuli were preceded by an initial silence lasting 0.