dataesr/scientific-paragraphs-categorization huggingface dataset:
Mineralogical analysis 3. 4. 1. X-ray powder diffraction (XRPD). Five silica phases from immature, noncrystalline opal-A and opal-A/ CT, to paracrystalline opal-CT and opal-C+quartz, to mature microcrystalline quartz are present in varying amounts in TVZ siliceous sinter deposits (Fig. 10 ). XRPD is the principal technique used to determine the silica phase present and to compare the degree of lattice order among samples. XRPD analysis of samples was undertaken in the School of Environment (UOA) with a Phillips diffraction goniometer fitted with a graphite monochromator, with acquisition controlled by Sietronics (1993) VisXRD software. XRPD operating conditions were 40 kV and 20 mA, using CuKa radiation (ka1 = 1. 54051 A ˚). Dry, untreated samples were scanned at 0. 6°2h/min, with a step size of 0.
Molecular characterization of modern microbial mats Clone library-based 16S rRNA gene analysis of samples from modern dark brown-green microbial mats, with feltlike palisade textures, revealed that all (KP1-4, KP7, 2KP1, 3OK4; Table  1 ) were dominated by a shared member of the mesophilic cyanobacterial genus, Calothrix (Fig. 7 ). This prevailing OTU was present in libraries at 34-74% relative abundance and shared 99% sequence identity with Calothrix sp. CCMEE5093 (GenBank accession AY147029). Other cyanobacterial sequences variably present across these samples were related to an unclassified subsection III cyanobacterium  (Tomitani et al. , 2006) , Leptolyngbya, Anabaena, and Synechococcus species, and Calothrix desertica (93% identity). In contrast, the dark brown, conical tufted mat sample 3KP2 was dominated by 2 OTUs related to Oscillatoria (22% abundance, 98-99% identical to Oscillatoria sp.
Acknowledgments Financial support was provided by the  Royal Society of New Zealand's Marsden Fund  to K. A. C. , a  National Geographic Society  field grant to D. M. G. and K. A. C. , and by a research fellowship to K. A. C. from the  LE STUDIUM Institute for Advanced Studies, France. Andres Arcila ,  Louise Cotterall ,  Catherine Hobbis ,  Bryony James ,  Michel Nieuwoudt , and  Ritchie Sims  kindly furnished laboratory analyses, technical support, and/or fruitful discussions.
Study design A multicentre, prospective, non-interventional, observational study was conducted in 34 sites in France, Germany, Italy, The Netherlands, Spain, Turkey and the UK from December 2011 to November 2012. The primary objective of the study was to finalize and validate the newly developed PKU-specific Quality-of-Life questionnaire (PKU-QOL). The results related to this primary objective are reported elsewhere  [24]. A secondary objective of the study, which is reported here, was to describe HRQoL as measured for the first time by instruments designed to be sensitive to the particular and sometimes subtle issues characteristic of the PKU population. As this was the secondary objective, this paper presents exploratory analyses performed posthoc on data collected primarily for the purpose of validating the PKU-QOL.
HRQoL of PKU patients: generic questionnaires All patients and parents completed age-specific generic HRQoL questionnaires (PedsQL, Child Health Questionnaire PF28, SF36). The children and adolescents reported PedsQL scores comparable to the US normative data sample, confirming previous study reports of consistently normal scores on generic questionnaires in patients with PKU  [17] [18] [19] [20]. On the SF36 questionnaire the adult group presented higher mean scores on the physical domains, but slightly lower mean scores on the mental domains compared to the US norm scores. Higher physical scores have been reported before by patients with PKU  [22]  and may be attributed to the fact that adult patients included in PKU studies are likely to be younger than adults in the reference group from the general populationsthe mean age of adults recruited in this was 25.
Acknowledgements We want to thank the physicians who participated in the study: France:  Jean-Baptiste Arnoux ,  Pierre Broué ,  Karine Mention ,  François Feillet ,  François Maillot ; Germany:  Skadi Beblo ,  Peter Burgard ,  Anibh Das ,  Jürgen Herwig ,  Franck Rutsch ,  Peter Freisinger ; Italy:  Milva Orquidea Bal ,  Alessandro Burlina ,  Maria Teresa Carbone ,  Roberto Cerone ,  Vincenzo Leuzzi ; Netherlands:  Francjan van Spronsen ,  Floris Hofstede ; Spain:  Maria Luz Couce Pico ,  Maria García Jiménez ,  Maria Bueno Delgado ; Turkey:  Mubeccel Demirkol ;  United Kingdom :  Peter Galloway ,  Andrew Morris ,  Germaine Pierre ,  Yusof Rahman. We are also extremely grateful to the children and parents who have contributed to this study. We want to address a very special thanks to  Pr.
Observation data Observation data of H. axyridis were collected by the 'observatoire permanent pour le suivi de la Coccinelle asiatique en France' (Permanent observatory for the monitoring of the harlequin ladybird in France), a network composed of regional coordinators compiling the observations made by about 1800 voluntary participants from all over the French territory  (Ternois et al. 2012). A total of 5206 observations of H. axyridis individuals or populations and their given locations were reported between 2004 and 2011. We divided the surface of France into a regular grid with square cells of 8 by 8 km, corresponding to the grid cell of the meteorological data SAFRAN from Meteo France (the French national meteorological service). The final partition of the studied area included 9891 cells.
axyridis in France. The disturbance of natural habitats by human activities (mainly agriculture and urbanization) is also thought to facilitate bioinvasions, for instance by homogenising the environment over large geographical scales  (Hufbauer et al. 2012). To test for this hypothesis we included covariates of humanaltered habitats where H. axyridis has been found: in crops  (Vandereycken et al. 2013) , in vineyards  (Koch 2003)  and in urban areas  (Adriaens et al. 2008). All these covariates were quantified by their surface within a cell, this information being provided by Corine Land Cover data (< www. eea. europa. eu/data-and-maps >). The different environmental and anthropogenic covariates used in our modeling are summarized in Table  1.
Model validation and forecasting H. axyridis's distribution We used observation data from 2004 to 2010 to estimate the different parameters of the models and to perform model selection. Data of year 2011 was kept apart and used to measure model performance using the following approach: starting from the observations of 2004, we projected the probability of presence in each cell and for each year until 2010, the last year of data used in the model. We then predicted the distribution of H. axyridis over the period 2011-2020. We compared the predictions for 2011 with the observations for the same year. We calculated the area under the receiver operating characteristic curve, known as AUC and the Kappa statistic, two standard methods used to estimate the predictive accuracy of distributional models derived from presenceabsence data.
Comparison with classical niche modeling approaches We compared the above measures of model performance with the same ones estimated from a classical (and hence static) approach of niche modelling (also called species distribution modeling; SDM). For this we used Boosted Regression Trees (BRT)  (Elith et al. 2008)  with the same environmental and anthropogenic covariates pooled over the 2004-2010 period. We then estimated the same indices of model validation (respectively AUC BRT and Kappa BRT ) by comparing predictions of H. axyridis' distribution in 2011 with the observations of 2011. Data available from the Dryad Digital Repository:  http://dx. doi. org/10. 5061/dryad. jg613   (Veran et al. 2015). It is worth stressing that here we assumed the absence of local extinction. In other words, once a cell has been colonized it remained occupied for the following years.
This pattern of low to null local extinction is often observed in invasive populations during the diffusion stage  (Facon and David 2006)  and is confirmed by our own experience of recurrent annual collection in the field of H. axyridis in France for the last five years. Raw observation data compiled in the analyzed database also supported this assumption to a large extent. As a matter of fact, we found that when a cell was first colonized, it remained colonized the following years. We note however that for a few cells, observations were not continuous over time. Those few years without observations were likely due to a lack of report rather than to a local extinction. As a matter of fact, once a given observer had reported a colonized site, he/she was unlikely to report the same site the following year but reported new sites instead.
This bias is to a large extent compensated by the presence of multiple observers within a cell. We used the software PRESENCE (< www. mbr-pwrc. usgs. gov/software/presence. html >) to perform model selection and estimate the different parameters of the models using a maximum-likelihood approach. Two covariates, density of human population and surface of urbanization, were highly correlated between them (r  0. 726). Including both of them in the analysis would have increased instability when estimating regression coefficients  (Graham 2003). Therefore, we first compared full models incorporating either density of human population or surface of urbanization, and kept for the following steps of model selection the covariate from the model with lowest AIC. In a second step, we selected among models considering different sizes of neighborhood (p i ), from one layer of cells (p 1 ) to five layers of cells (p 5 ).
This is one of the reasons why the SDM literature has been dominated by this type of indices. Here we used our models to predict values for a single year, 2011, as our validation procedure, which will inevitably have more stochasticity in it as compared to occurrence data grouped over decades. Because it allows relaxing the assumption of equilibrium, applying a dynamic approach when modeling the invasion process represents a powerful tool to prioritize management strategies of invasions. Indeed a majority of studies on species range shifts use statistical species distribution models (SDMs) even if they seriously violate the assumption of equilibrium  (Elith and Leathwick 2009, Elith et al. 2010). While range shifting taxa are often the species for which predictions of potential distributions are needed the most for prioritizing mitigation measures, their usefulness for guiding policy making and planning has been questioned  (Araújo and Guisan 2006).
This could be due to major driver(s), whether environmental or anthropogenic, not included in our model, although we took special care to include the relevant factors known to affect the biology of the species and the habitats where H. axyridis has been found  (Koch 2003 , Adriaens et al. 2008 , Roy and Wajnberg 2008). Another factor which might also explain the limited performance of the modeling could be the data of presenceabsence itself. We assumed absence of species when no presence was recorded. This assumption is probably partially true.
Model selection results for the H. axyridis dataset. The probability of colonization g is decomposed into environmental covariates and/or anthropogenic covariates and an autologistic component. Models are arranged following the different hypothesis tested: acontribution of urban areas versus density of population, b -number of layers of the autologistic component (p ˆi: effect of i layers of cells), c -contribution of the different covariates, d -time varying autologistic component -(p ˆi  t). Models are compared with ΔAIC and Akaike weight (w). k indicates the number of parameters of the model. Abbreviations of the different covariates are explained in Table1. Square power indicates a quadratic response.
Acknowledgements -We thank  Eric Lombaert ,  Thomas Guillemaud ,  Jean-Pierre Rossi ,  Emmanuelle Jousselin ,  Armelle Coeur-d'Acier ,  Marc Kenis  and  Gilles San Martin  for fruitful discussions. This work was funded by a grant from the  French Agropolis Fondation (RTRA, Montpellier ,  BIOFIS  project # 1001-001 ). This paper is Contribution no. XXXX of the Virginia Inst. of  Marine Science, College of William and Mary.
Statistical analysis All statistics were performed using the software Statistica 7 (Statsoft, USA). As the normality of data was not guaranteed, no-parametric tests were used (Spearman correlation analysis) to investigate the relation between gross efficiency and absolute or relative changes in muscle skin temperature (∆T). Friedman rank-repeated measures test, Wilcoxon rank-sum test and Mann-Whitney U were also used to study the effect of workload on the skin temperature (paired samples) and to determine the differences between the quadriceps and calf muscles (two independent samples). The level of significance was set at p < 0. 05 for all tests. Descriptive data are presented as median and Interquartile Range (IQR) except where describes otherwise.
At low ǫ, only the larger angle setting was possible. The kinematic settings are summarized in Table  I. For each Q 2 , ǫ setting, the electron spectrometer angle and momentum, as well as the pion spectrometer momentum, were kept fixed. The HMS magnetic polarity was reversed between π + and π -running, with the quadrupoles and dipole magnets cycled according to a standard procedure, then set to the final values by current (in the case of the quadrupoles) or by NMR probe (in the case of the dipole). Kinematic offsets in spectrometer angle and momentum, as well as in beam energy, were previously determined using elastic ep coincidence data taken during the same run, and the reproducibility of the optics was checked  [14]. For the deuterium data sets studied here, elastic runs on 1 H were used to check the validity of the HMS and SOS corrections for several momentum ranges.
4 MHz. The tracking efficiency is defined as the ratio of the number of events for which an actual track is found, to the 'events' that pass through the drift chambers. This ratio is extracted from events in a fiducial area where it is extremely likely that the scintillator hits are due to particles that also traversed the chambers. The tracking efficiency depends on both the drift chamber hit efficiency and the tracking algorithm used in finding the track. In order to accurately calculate the tracking efficiency, tight particle identification (PID) requirements were applied to select a pure data sample. These requirements are stricter than those used in the regular analysis. In the HMS, the particle identification requirements used to select pions in the tracking efficiency calculation consisted of cuts on the gas Cerenkov and the calorimeter for F π -1 data, while for F π -2 an additional cut on the aerogel Cerenkov was applied.
Unfortunately, no luminosity scans on carbon target were taken at different beam currents in the F π -1 experiment, so any conclusions obtained from the F π -2 study have to be applied also to the F π -1 data. Since the probability of a second particle traversing the HMS during the event resolving time is greater at high rates, a tight electron PID cut might introduce its own deadtime not due to tracking efficiency, causing the rate-dependence to be underestimated. Therefore, only HMS fiducial acceptance cuts were applied in this study. Normalized yields from the carbon target were computed from the number of events passing cuts, the integrated beam charge, the electronic and CPU data acquisition livetimes and the HMS tracking efficiency. They are plotted versus rate in Fig. 2. The error bars include statistical uncertainties and an estimated systematic uncertainty of 0.
After implementing the pion punch-through events in SIMC, the M X cut upper limit was determined by the value where the missing mass peak is no longer well reproduced by a quasi-free Monte Carlo simulation including all known detector effects, indicating the presence of additional backgrounds, such as two pion production. The missing mass cut was taken to be 0. 875≤ M X ≤1. 03 GeV. It is wider than the one used in the analysis of the hydrogen data because of Fermi motion in the deuteron. Compared to hydrogen, the backgrounds from target windows and random coincidences are generally larger due to the wider M X cut.
C. Determination of Separated Structure Functions The SIMC model cross section and the final separated structure functions were determined in the same (iterative) procedure. The model cross section was taken as the product of a global function describing the Wdependence times (a sum of) Q 2 and t dependent func- tions for the different structure functions. For the LT and T T parts, their leading order dependence on sin(θ CM ) was taken into account  [5]. The W -dependence was taken as (W 2 -M 2 N ) -2 , where M N is the struck nucleon mass, based on analyses of experimental data from Refs. [6, 27]. For the parts depending on Q 2 and t, phenomenological forms were used and the parameters were fitted. For all t-bins at every (central) Q 2 setting, φ-dependent cross sections were determined both at high and low ǫ for chosen values of W , Q 2 (and corresponding values of θ π and ǫ) according to Eqn.
D. Systematic Uncertainties due to Missing Mass Cut and SIMC Model Dependence Since the extracted separated cross sections depend in principle on the cross section model, there is a "model systematic uncertainty. " This uncertainty was studied by extracting σ L and σ T with different cross section models. There is a second, related uncertainty due to the modeling of the missing mass distribution. The combined systematic uncertainty due to both effects was estimated by modifying the missing mass cuts and SIMC model parameters p i and investigating the resulting differences on the separated cross sections. To estimate the missing mass cut dependence, the experimental and simulated data were analyzed with two tighter missing mass cuts, M X < 0. 98, 1. 00 GeV. A detailed comparison of the separated cross sections for each t-bin indicated that the π -separated cross sections for higher -t at Q 2 =0.
electroproduction data in the canonical resonance region (W < 2 GeV). This model incorporates Breit-Wigner fits to nucleon resonances and also includes (unitarized) non-resonant backgrounds. Originally introduced in 1998  [37] , MAID has undergone incremental improvements. Shown here are the results of the most recent version of the MAID model from 2007  [38]. For these calculations, we have used the MAID07 standard parameter set, although some parameters (such as relative strengths of resonances, the charged pion form factor, etc. ) can be adjusted. Finally, note that we apply the MAID model to some kinematics with W > 2 GeV. Strictly speaking, the model is not constrained in this regime and the results plotted represent an extrapolation of a calculation fit at lower W. For σ L , the MAID07 predictions are slightly higher than the VGL, KM and VR models, while the σ T predictions are midway between the purely Regge-based VGL and the VGL+DIS KM and VR.
In terms of π -/π + ratios, MAID07 provides by far the best description of R L , providing further evidence that the disagreement between the pion-pole dominated models and the R L data is due to small resonant contributions in the longitudinal channel. MAID07 also provides a fairly good description of R T at Q 2 =1. 6 GeV 2 , although it undershoots the R T at Q 2 =0. 6, 1. 0 GeV 2. The overshoot at Q 2 =2. 45 GeV 2 is probably due to the significant extrapolation from the optimized parameter region W < 2 GeV. We further investigated the impact of resonances in the MAID07 model on the π -/π + ratios. With all resonances turned off (Born term and meson exchange contributions on), the model gives R L ≈ 1 and R T far below the data (R T ≈0. 5 at Q 2 =0. 6, 1. 0 GeV 2 , R T ≈0. 2 at Q 2 =1. 6, 2.
45 GeV 2 ). Even though the data are acquired near W = 2 GeV or higher, turning on only the P 33 (1232) resonance has a significant effect on R T (increasing it to ≈1. 5 at Q 2 =0. 6, 1. 0 GeV 2 , and ≈0. 8 at Q 2 =1. 6, 2. 45 GeV 2 ), but it has only a small effect on R L. Progressively turning on the other resonances yields no clear trend in the behavior of either ratio. Curiously, turning off only the highest three resonances, F 37 (1950), P 31 (1910), F 35  (1905) , results in virtually no change from the nominal case. In summary, no clear single resonance seems to account for the global behavior of the separated ratios in the MAID07 model. It would be extremely interesting to see the result if the model parameters could be optimized for higher W. The Goloskokov-Kroll (GK) GPD-based model  [10, 12]  is a modified perturbative approach, incorporating the full pion electromagnetic form factor (as determined by fits to our F π data  [29] ) in the longitudinal channel and the H T transversity GPD dominating the transverse channel.
V. SUMMARY We present L/T /LT /T T separated cross sections for the 2 H(e, e ′ π ± )N N s reactions, at Q 2 =0. 6-1. 6 GeV 2 , W = 1. 95 GeV and Q 2 =2. 45 GeV 2 , W = 2. 2 GeV. The data were acquired with the HMS+SOS spectrometers in Hall C of Jefferson Lab, with the exclusive production of a single pion assured via a missing mass cut. The separated cross sections have typical statistical uncertainties per t-bin of 5-10%. The dominant systematic uncertainties are due to HMS tracking at high rates (π -), HMS Cerenkov blocking (π -), cryotarget boiling at high current (π + ), spectrometer acceptance modeling, radiative corrections, pion absorption and decay. These data represent a substantial advance over previous measurements, which were either unseparated at Q 2 =0. 7 GeV 2  [6] , or separated but over a limited kinematic range in the resonance region  [24, 30].
ACKNOWLEDGMENTS The authors thank  Drs. Goloskokov  and  Kroll  for the unpublished model calculations at the kinematics of our experiment, and  Drs. Guidal ,  Laget , and  Vanderhaeghen  for modifying their computer program for our needs. This work is supported by  DOE  and  NSF (USA) ,  NSERC (Canada) ,  FOM (Netherlands) ,  NATO , and  NRF (Republic of Korea). Additional support from  Jefferson Science Associates  and the  University of Regina  is gratefully acknowledged. At the time these data were taken, the  Southeastern Universities Research Association (SURA)  operated the  Thomas Jefferson National Accelerator Facility  for the  United States Department of Energy  under contract  DE-AC05-84ER40150.
Caroline Bertoneche and Charlotte Ribeyrol As to the Jason of the Louvre, one asks at first sight of him, as he stoops to make fast the sandal on his foot, whether the young man can be already so marked a personage. Is he already the approved hero, bent on some great act of his famous epopée; or mere youth only, again, arraying itself mechanically, but alert in eye and soul, prompt to be roused to any great action whatever? The vaguely opened lips certainly suggest the latter view; if indeed the body and the head (in a different sort of marble) really belong to one another. Ah! the more closely you consider the fragments of antiquity, those stray letters of the old Greek aesthetic alphabet, the less positive will your conclusions become, because less conclusive the data regarding artistic origin and purpose.
rubrum sequences. For all contigs which could not be annotated by this method, we performed blastp searches against the UniProt protein database  (Altschul et al. 1990; The UniProt Consortium 2013). An e value cut-off of 10 -5 was applied and we reported only the best hit of each query sequence. Among these Uniprot hits, we listed the non metazoan hits to avoid the bias of contaminations in our analysis. In all cases, we used the UniProt identifier to assign each contig to Gene Ontology biological process categories  (Ashburner et al. 2000)  associated to the predicted protein. Annotation results were summarized using Generic GO-Slim, a cut-down version of Gene Ontology containing a small number of relevant functional categories (http://www. geneontology. org/ontology/subsets/goslim_generic.