dataesr/scientific-paragraphs-categorization huggingface dataset:
Growth was observed in BWF2A/SW3C cultures with both yeast extract and polysaccharide substrates; however, we detected no increased levels of growth, indicating that in isolation our C. proteolyticus strains may require specific undefined cofactor(s) or collaborative microbial partners to support the activity encoded by their acquired CAZymes. In lieu of axenic C. proteolyticus cultivation data to support a saccharolytic lifestyle, we biochemically interrogated the GH16 encoded in region-A (Fig. 4 ). The catalytic domain was synthesized and expressed in E. coli, followed by protein purification. As expected the GH16 demonstrated endoglucanase activity on β-1,3 (pachyman, curdlan, laminarin) and β-1,3-1,4 (Barley) substrates (Figure  S2A ), which supports our hypothesis that the CAZymes in region-A have transferred the ability of BWF2A or SW3C to degrade polysaccharides.
Acknowledgements We are grateful for support from The  Research Council of Norway  ( FRIPRO program , P. B. P. : 250479 /NorZymeD , V. G. H. E. : 221568), as well as the  European Research Commission Starting Grant Fellowship  (awarded to P. B. P. ;  336355-MicroDE ). The sequencing service was provided by the  Norwegian Sequencing Centre  (www. sequencing. uio. no), a national technology platform hosted by the  University of Oslo  and supported by the  "Functional Genomics" and "Infrastructure" programs of the Research Council of Norway  and the  Southeastern Regional Health Authorities.
The purpose of this study is to account for the increase in non-regular workers, namely, part-time and dispatched workers, in the Japanese econ¬omy from the early 2000s. Our contribution is that we use a firmlevel panel dataset extracted from an administrative survey and distinguish between the short-run and long-run determinants of non-regular labor de¬mand. Using the estimated parameters of the labor demand function, we decompose the rate of increase in the macroeconomic non-regular worker ratio into determinant factor contributions. Our major results can be summarized as follows. First, the firm-level determinants of the demand for part-time and dispatched workers significantly differ. Second, our re¬sults suggest that the non-regular job creation stimulated by the increased female labor supply plays an essential role relative to direct demand-side factors.
To investigate individual firms' non-regular labor demand behavior, a panel dataset containing information on both employed (or accepted) non-regular workers and firms' management is indispensable. However, such datasets are scarce in Japan. On one hand, corporate finance data based on securities re ports, which are widely used in empirical studies on firm behavior in Japan, contain insufficient information on non-regular workers. On the other hand, several government labor surveys at the establishment level contain rich in formation on the types and numbers of non-regular workers but contain very limited information on firms' management and corporate finance. Currently available survey data with sufficient information on both non regular workers and their workplaces can be found in the BSBSA conducted by the Ministry of Economy, Trade, and Industry (METI).
The BSBSA is an annual survey that contains data on the diversification, globalization, and in formatization of Japanese firms, and it is generally used by the METI to inform and learn from its own economic policymaking. The survey's scope covers firms with 50 or more employees whose paid-up capital or investment is higher than 30 million yen in industries including mining, manufacturing, wholesale and retail trade, food services, and many other service industries. Although the BSBSA does not include data from micro-enterprises, it addresses a large range of firms and has a sample size of around 30,000 firms in each year. This feature pro-vides a strong advantage in the context of our research, and the survey is used throughout this study. The BSBSA reports the number of workers classified by their employment types.
This BSBSA part-time worker ratio is higher by a few percentage points than the economy-wide ratio based on the published government data mentioned at the beginning of this section. Government surveys generally distinguish part-time workers as those working below 35 hours in a week. On the other hand, the BSBSA's definition of part-time workers, as mentioned above, is broader and includes those with more than 35 weekly working hours but fewer than full working hours. This difference might be a reason for the gap between the part-time worker ratios in the BSBSA and those found using other representative government statistics. In addition, since the BSBSA does not cover small firms, this gap suggests that the employment of part-time workers is mildly biased toward larger firms. By comparison, the aggregate dispatched worker ratio is much lower and more stable; it varies from three to seven percent and peaks in 2007.
5 percent in the 2010s. The aggregate ratio of the number of temporary workers to total workers is also very small and rapidly decreasing. Specifically, this ratio is 2. 3 percent in 2000, 1. 0 percent in 2005, and 0. 8 percent in 2014. Thus, temporary workers are not frequently employed, at least among firms in the BSBSA sample, and, thus, we concentrate our analysis on the other two types of non-regular workers. 4. The BSBSA asks firms to answer questions based on the conditions in the settlement terms for the previous year. Thus, we use data from the survey conducted in a given year (on June 1 until 2006 and on March 31 from 2007) to represent the previous years' business and financial conditions. 5. Note that normal, dispatched, and temporary workers do not overlap according to the BSBSA definitions.
For example, the economy-wide share of workers in firms whose part-time worker ratios exceed 50 (75) percent was about 26 (13) percent in 2000 and about 35 (24) percent in 2014. 8 7. The BSBSA data have many missing values for some fields, including the number of non-regular workers. We assign zeros to some of missing values when we can conclude that the respondents left the question unanswered not because they refused to answer but because those values were actually zeros. For the standards for this interpolation, see Section 2. 8. Referring to a government survey,  Kalantzis et al. (2012)  point out that part-time workers are concentrated in very large and very small firms, the latter of which are not included in the BSBSA sample. Since large firms' worker weights are large, the assertion of Kalantzis et al.
Estimation Model and Explanatory Variables In the following analysis, we estimate the non-regular worker share determina tion by short-run and long-run factors using BSBSA panel data. The data are annual, and the sample period is from 2000 to 2014. We consider two types of non-regular workers: part-time workers and dispatched workers. The total number of workers is the sum of normal, dispatched, and temporary workers, as explained in Section 2. The explained variable is the individual non-regular worker ratio, which is defined as the ratio of the number of non-regular work ers to the total number of workers in a firm. Hereafter, it is simply called the non-regular worker ratio (specifically, the part-time or dispatched worker ratio) unless otherwise mentioned. The explanatory variables are divided into two groups: short-run and long run determinants.
The relatively large variation in the non-regular ratio around 2007 and 2008 shown in Section 2 might also provide supporting evidence for this assumption. This treatment makes the long-run determinants time variant and allows us to use panel fixed-effect estimation. Thus, the sub-sample periods are set to be  2000-2008 and 2009-2014. The long-run determinants are the sample means of the variables explained below in each sub-period. In the BSBSA dataset, not all surveyed firms necessarily have full time-series observations of the variables. One reason is appearances or disappearances of sampled firms. Another is that respondent firms did not answer some questions. Since too few observations imply that statistical relia bility cannot be ensured, firms with variables with fewer than three observations in each sub-period are dropped from the sample.
Since firms with bad financial condi tions face high probabilities of bankruptcy, it is difficult for them to commit to long-term employment contracts with regular workers. Thus, bad financial conditions are found to lead to less stable employment relations. For example,  Lechevalier et al. (2014)  argue that firms' high indebtedness might translate into pressure to downsize or hire more non-regular workers in the estimation of the labor adjustment speeds of Japanese firms. Caggese and Cu˜nat (2008)  examine two opposite effects of financing frictions on the composition of permanent and fixed-term workers. Current financial constraints increase the demand for more productive permanent workers, and future financial constraints increase the de mand for flexible fixed-term workers. Using a database of Italian firms, they find that financially constrained firms use fixed-term contracts more intensively.
They commonly find positive correlations between the level of uncertainty and the scale of non-regular worker use. In particular, using the same dataset as ours,  Morikawa (2010)  separately considers three types of non-regular workers, part-time, dispatched, and temporary workers, and finds that the elasticity of the number of dispatched workers is largest among non-regular workers. Following these studies, we add the measure of demand volatility as a long-run determinant. However, our volatility measure is the standard deviation of observed sales growth (variability hereafter) instead of that of unexpected sales growth (i. e. , uncertainty). If firms adjust their workers for demand fluctuations, they should respond to all demand fluctuations irrespective of whether they were expected in advance.
Nevertheless, one possible factor is ICT improvement. Asano et al. (2013)  show that firms' ICT use increases their part-time worker employment. Although we use the same dataset, we cannot incorporate this effect since the BSBSA termi nated its inquiry concerning ICT use in 2006. Thus, we cannot test the effect of ICT diffusion on non-regular employment by using the BSBSA data. Fur ther investigation into the relationship between ICT use and non-regular worker demand using other data sources is necessary. Moreover, ICT progress might influence firm-level non-regular demand from the outside though externality eff ects. Therefore, some aggregate indicators representing ICT improvement may be useful to explain the trend in non-regular worker demand beyond the female labor supply increase. These issues remain for future research.
The present article deals with the way in which, in Brazilian society, the relations of alterities are translated in the current discourse of the present day, with respect to race relations. These discourses reveal not only the existence of a deeply rooted theoretical base, but also a lack of awareness of the concrete reality of racial discrimination in Brazil, and the persistence of the idea that Brazilian society is not racist. The qualitative analysis developed, part of the vision of Brazilian Afrodescendants, studied through a questionnaire googledoc, treated by the Iramuteq Program and based on the theories of Bakhtin's circle, in dialogue with Bourdieu. The study points out in what way language influences personal relationships, especially how the word and its values potentiate the tensions experienced between groups increasingly antagonistic.
The EBUS off Peru is one of the most productive systems, accounting for 10 % of the world's fisheries  (Pennington et al. , 2006; Chavez et al. , 2008) , with the shallowest oxycline and one of the most intense  OMZs (Fig. 1a-b; Paulmier et al. , 2009). Thus, it provides perfect conditions for investigating the relative importance of the aforementioned mechanisms. In order to examine the particle fluxes and their variability, this study focusses on the analysis of a time series compiled from moored sediment traps deployed in the Peruvian OMZ (Fig. 1c ). This dataset is part of the AMOP ("Activities of research dedicated to the Minimum of Oxygen in the eastern Pacific"; see Sect. 2) project.
(a) PON           3a  and S1  for details). samples representing the variability over the total dataset (AMOP summer + AMOP winter-spring ) or a given subset of data (e. g. corresponding to high, intermediate or low T eff ranges) has also been indicated in Tables  1, 2 , 3, S1, S2, S3, S4 and S5). The different present relative SD values are higher than the total uncertainties (TU = accuracy + reproducibility) for all considered parameters. T effPON POP T effPOP BSi T effBSi mgN m -2 d -1 % mgP m -2 d -1 % mgSi m -2 d - (±85 %) (±87 %) (±89 %) (±91 %) (±63 %) (±53 %) (±78 %) (±72 %) ( ±32 (±46 %) (±56 %) (±27 %) (±33 %) (±50 %) (±47 %) (±54 %) (±58 %) (±25 %) Low T eff 41. 23 0. 91 2 4. 93 0. 53 14 495. 00 9. 47 3 (±61 %) (±18 %) (±47 %) (±64 %) (±98 %) (±81 %) (±105 %) (±81 %) (±119 %) (b) C : N T effC (±14 %) (±14 %) (±16 %) (±38 %) (±32 %) (±54 %) (±36 %) (±32 %) ( ±46 (±11 %) (±22 %) (±16 %) (±22 %) (±66 %) (±68 %) (±15 %) (±62 %) ( ±67 (±52 %) (±57 %) (±24 %) (±46 %) (±59 %) (±37 %) (±60 %) (±45 %) ( ±44 (±50 %) (±54 %) (±10 %) (±54 %) (±65 %) (±18 %) (±60 %) (±58 %) ( ±47 (±56 %) (±67 %) (±79 %) (±51 %) (±83 %) (±96 %) (±51 %) (±69 %) (±51 %) (c) δ 13 C T eff 13 C δ 15 N T eff 15 N CaCO 3 T effCaCO 3 ‰ % ‰ % mgCa m -2 d - (±3 %) (±8 %) (±6 %) (±20 %) (±9 %) (±22 %) (±131 %) (±88 %) (±170 %) Data are available at different time resolutions: 15 min (O 2 , density from temperature and salinity), 30 min (fluorescence), 1 day (satellite ASCAT wind), 7 or 11 days for AMOP summer and AMOP winter-spring datasets, respectively.
(2007) , defined as T eff = POC 149 POC 34 × 100. (1) The transfer efficiency allows the determination of the ability of the system to preserve OM quantity and to foster the export of carbon from the productive layer. The higher the transfer efficiency, the higher the proportion of particles reaching the deeper trap. Therefore, T eff is an index of the relative amount of carbon that reaches the deeper trap. The mean transfer efficiency appears to be relatively similar for both datasets (T eff ∼ 45 %). However, T eff values present a strong temporal variability, with T eff being more than 3 times more variable for AMOP winter-spring than for AMOP summer (Fig. 2 ; Table  1 ). T eff can be higher than 100 %, referring to particle accumulation between both traps. T eff > 100 % is potentially attributable to advection of particles or to primary or secondary production between traps.
Note that the vertical profile of POC flux is assumed to follow a power law  (Suess, 1980; Martin et al. , 1987). (2) The b coefficient represents the attenuation of the curve and therefore an index for OM respiration during sinking. Fitting b on the AMOP dataset reveals temporally varying b values (between 0. 23 and 2. 97, Table  1   1 ) are in line with those generally observed in the equatorial Pacific OMZ (between 0. 63 and 0. 9,  Berelson, 2001) , in the Mexican OMZ (about 0. 36,  Devol and Hartnett, 2001) , in the Peruvian OMZ (0. 66±0. 24,  Martin et al. , 1987)  and in the Arabian Sea OMZ (0. 22,  Roullier et al. , 2014; 0. 59 ± 0. 24: Keil et al. , 2016). The temporal modulation of b is comparable to that associated with the spatial switch from the coast to the open ocean off Peru  (Packard et al.
Thus, particle production is considered to be related to higher trophic levels only, in particular zooplankton (e. g. detritus due to excretion and mortality). Zooplankton can also induce active vertical trans-port of particles not directly considered here. However, zooplankton production should be pointed out for AMOP summer -S1. AMOP summer -S1 is characterised by an oxygen event (> 10 µmol kg -1 , Fig. 4a ) but with an unexpectedly high T eff (71 %) suggesting preferential OM preservation. This sample is different from the others previously mentioned, the number of swimmers collected being 3 times higher than the average of the AMOP summer dataset, especially in the lower trap. This AMOP summer -S1 specificity is raising the influence of the active transfer between both traps and potentially secondary production.
In this study, we assume that (a) similar particles are collected in the upper and lower traps for each sampling period; (b) all particles collected in the deep trap are, for each sampling period, subject to a comparable time in the OMZ layer. Note that all the AMOP summer samples in summer and the first six AMOP winter-spring samples (from AMOP winter-spring -S1 to AMOP winter-spring -S6) in winter appear to be subject to a comparable trophic level effect. Indeed, samples are composed of around 60 %-70 % faecal pellets, therefore spending a similar amount of time in the OMZ. However, for the last six AMOP winter-spring samples (from AMOP winter-spring -S7 to from AMOP winter-spring -S12) in late winter-early spring, the proportion of faecal pellets and marine snow inverts. For the AMOP winter-spring dataset, low T eff (from AMOP winter-spring -S7 to AMOP winter-spring -S12) can be explained by the higher proportion of small particles (as marine snow), which is potentially easily degradable.
3. 1. 2). In these cases, T eff remains interme-diate (20 < 50 %), associated with a potentially balanced co-limitation in O 2 and OM on OM degradation. Qualitatively, the evolution of elemental fluxes at 34 m should be considered in investigating whether the composition of a more or less labile OM can affect transfer efficiency (T eff ) in addition to the OM availability. For both datasets, POC and PON fluxes show a strong linear correlation with the total particle mass fluxes at the upper trap as well as for the lower trap (R 2 = 0. 98 for both traps; Fig. S2a, b ). To study the influence of particle quality on transfer efficiency, the composition was averaged for the three main ranges of T eff. Also, as the matter collected in the trap is mainly organic, only the four main components (POC, PON, POP and BSi) were considered here.
The AMOP winter-spring -S4 CaCO 3 upper flux exhibits a maximum at this date compared to other intermediate and high T eff (Table  3c ) and about 5 times higher (20 % of the total mass flux) than the average for the entire dataset (Table  S5 ). A difference in the phytoplankton community could be at the origin of this distinction. Indeed, at the beginning of the AMOP winter-spring dataset and up to this sample, the MLD is relatively stable. No strong MLD deepening is observed as a consequence of wind intensification. As the surface productivity is mainly due to diatoms, this long period with no strong mixing events can induce silica depletion at the surface, limiting diatom growth. This hypothesis is supported by the analysis of the phytoplankton functional types around the mooring location using MODIS data and the algorithm developed by  Hirata et al.
In addition, the depth and oxygenation of the oxycline should play an important role in explaining the differences among low, intermediate and high T eff ranges. However, one should be cautious with these results, as the variability in δ 15 N for the entire dataset does not allow strict differentiation among the ranges. Therefore, in the OMZ, short-term [O 2 ] fluctuations and particle loading appear to be significant. They should be considered for further studies on OM fate, carbon sequestration, nutrient regeneration, and the production or consumption of greenhouse and toxic dissolved gas. These effects call for the development of variable molar ratio models for OM production mechanisms, and OMZ remineralisation processes, and for the revised interpretation of palaeo-proxies.
Acknowledgements. We would like to thank the crew of the  German R/V Meteor  for the deployment as part of the DFG-funded SFB754 fieldwork, the crew of the  Peruvian R/V Olaya  for the visit and the crew of the  French R/V Atalante  for the recovery of the fixed AMOP mooring. We would like to thank  Stefan Sommer  and  Marcus Dengler  for providing the METEOR wind dataset. We would also like to thank  Miriam Soto ,  Anne Royer  and  Emmanuel De Saint Léger  for general logistics and administrative support. We are grateful to  Vincent Rossi  for discussions regarding the processes affecting the sinking speed of the particles. We are finally also grateful to  Christophe Lerebourg , from  ACRI-ST , for his support during the course of this study. This work was supported by the  AMOP ("Activity of research dedicated to the Minimum of Oxygen in the eastern Pacific")  project supported by  IRD ,  CNRS/INSU, DT-INSU  and LEGOS, and by a  GIS COOC (UPMC, INSU/CNRS ,  CNES ,  ACRI-ST)  PhD grant.
Models show chloroplast capture is more likely in plant populations with high levels of inbreeding following a reduction in selfing rate after hybridisation; we suggest that this is a possible explanation for the massive amount of chloroplast exchange seen in our phylogeny, as Begonia species often exist as small isolated populations and may be prone to inbreeding depression. Our data also indicate a level of nuclear genetic exchange between species. The high prevalence of hybrid events in Begonia is potentially an important factor in driving genomic change and species evolution in this mega-diverse genus.
Diversification may be further driven by as yet poorly understood characteristics of the Begonia genome, which may have an underlying genetic instability as evidenced by the highly variable chromosome number in the genus. This is suggestive of hybridisation followed by polyploidisation, with frequent chromosome fission and fusion leading to the observed dysploid variation in chromosome number in Begonia  [14]. The extent of hybridisation in Begonia, at least in some clades, is only starting to become apparent from phylogenetic evidence. A majority of previous phylogenetic studies of Begonia have relied on a single genome for their data, usually the chloroplast  [8, 11, 12, 15]  or nrITS  [10, [16] [17] [18] [19]. Some studies have analysed combined datasets, using nrITS and various chloroplast loci  [20] [21] [22] [23] [24].
Some of these studies did highlight incongruence between the combined loci, either significant incongruence according to an ILD test  [22]  or topological but unsupported or moderately supported incongruence  [20, 24]. Only two studies did not uncover any significant incongruence between nuclear and chloroplast datasets  [21, 23] ; however these both used the trnL intron from the chloroplast which tends to give low resolution in Begonia phylogenies. Two studies have presented phylogenies from two different genomes which showed considerable amounts of supported phylogentic incongruence in Begonia. Goodall-Copestake et al. [25]  found incongruence between the chloroplast and mitochondrial phylogenies in a genus-wide study, and Hughes et al. [3]  between nrITS and chloroplast phylogenies in a study of Begonia sect.
Voucher and GenBank accession information is listed in S1 Table. The DNA extraction, PCR and sequencing were carried out as in Hughes et al. [3]. The following bases were excluded from the chloroplast alignment because of missing data at the ends of regions, or alignment uncertainty due to long mononucleotide repeats: 1-10, 1390-1540, 2510-3050, 4530-4645, 4746-4910, 4943-4997, 5720-5810, 6970-7125, 8050-8089; and from the nuclear alignment bases 494-548 were excluded. Appropriate models of DNA sequence evolution for the aligned datasets were assessed with the program jModeltest 2. 1. 3 [28]  using the corrected Akaike information criterion (AICc) to estimate the model with the closest fit to the data. For both the chloroplast and nuclear alignment, the GRT+G+I model was the most probable (AIC weight 1.